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TRANSCRIPT
Network Effect and Multi-Network Sellers’ Dynamic Pricing:
Evidence from the US Smartphone Market
Rong Luo ∗
Department of Economics, University of Georgia
October 23, 2016
Abstract
The utility a consumer realizes from owning a smartphone increases with its oper-ating system (OS) network size. The OS network effect influences the dynamic pricingstrategy of multi-OS telecom carriers, who can internalize the competition across OSs.In this paper, I first study the carriers’ pricing strategy in a two-period, two-OS the-oretical model. I then estimate a structural model of consumer demand and telecomcarriers’ dynamic pricing game for two-year contract smartphones, using product leveldata from August 2011 to July 2013 in the US. From both the theoretical model andthe estimates, I find that multi-OS carriers choose lower prices for large OSs than smallOSs, while single-OS sellers would do the opposite in equilibrium. The estimate of theOS network effect in consumer utility is positive and significant. Counterfactual anal-yses show that, if the carriers specialized in different OSs or if the two-year contractswere eliminated, consumer surplus and smartphone penetration would decrease, andthe big carriers’ profits would increase. This paper is the first to study multi-networksellers’ dynamic pricing problem and to estimate a model of dynamic continuous choicegame among asymmetric multi-product firms.
Keywords: OS Network Effect, Carrier Dynamic Pricing Game, Two-Year Contract,Asymmetric Multi-OS Sellers, Value Function Approximation, MPEC.
∗University of Georgia Terry School of Business, 310 Herty Drive, Athens, GA 30602, USA. Email:[email protected]. This paper is previously circulated as The Operating System Network Effect and the Carri-ers’ Dynamic Pricing of Smartphones in US. I am very grateful to Mark Roberts and Paul Grieco for theirconstant support and very helpful comments. I would also like to thank Ying Fan, Gautam Gowrisankaran,Martin Hackmann, Hiroyuki Kasahara, Kenneth Judd, Robin Lee, Huihui Li, Yue Liu, Charles Murry, PeterNewberry, Kathleen Nosal, Joris Pinkse, Marc Rysman, Philipp Schmidt-Dengler, John Turner, Daniel Xu,and participants in PSU IO workshop, 13th Annual International Industrial Organization Conference, 2015CEPR-JIE School and Conference, and 2016 SHUFE IO summer school for their thoughtful comments. Allerrors are my own responsibility.
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1 Introduction
In markets with network effects, such as the computer and smartphone markets, consumers
value the size of the installed consumer base. Due to the network effect, the price of a
product affects its network size and thus future demand. This leads the sellers to make
dynamic pricing decisions. However, while the literature has studied the pricing strategy
of single-network sellers, little attention has been paid to multi-network sellers’ dynamic
pricing strategy, who can price differently across networks and internalize the network
competition.
I study the multi-network sellers’ pricing game in the US smartphone industry. Smart-
phones are subject to a network effect that arises through the operating systems (OS) for
two reasons. First, application stores of the OSs generate an indirect network effect. Ap-
plication developers choose to launch apps on large OSs. In return, more consumers adopt
large OSs because of more variety and better quality of applications.1 Second, a direct
OS network effect exists. Friends and family members prefer adopting the same OS. The
benefits of doing so include convenient communication, the ease of sharing files and app
purchases, and lower learning costs.
Telecom carriers act like multi-network sellers due to two facts. First, all four of the
biggest carriers — Verizon, AT&T, Sprint, and T-Mobile — have been selling smartphone
models with iOS, Android, Blackberry, and Windows Phone operating systems. Second,
the two-year contract model of selling smartphones provides the carriers a channel to price
differently across OSs. Both the availability of smartphones with different OSs from a
carrier and the two-year contract policy have important impacts on consumer surplus, the
carriers’ profits, and the smartphone industry growth.
To provide the intuition of the multi-OS carriers’ pricing strategy, I first study a two-
period, two-OS theoretical model. I find that a multi-OS seller chooses a lower price for
the large OS than the small OS in the first period, while the opposite happens in the
equilibrium of the single-OS sellers’ price competition. Single-OS sellers can’t internalize
the OS competition. The large OS seller has stronger market power and chooses a higher
price. In contrast, a multi-OS seller is able to internalize the OS competition, and it prefers
OS concentration to close OS competition, because a large OS can increase both future
demand and prices due to strong network effect. Thus, the multi-OS seller chooses a lower
1There is great variation in the numbers of applications across OSs. The correlation between the numberof applications and the number of users for an OS is 0.85, according to monthly data from 2011 to 2013.
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price for the initially larger OS to achieve concentration.
Data show that the carriers’ pricing of smartphones is consistent with the multi-OS
seller’s differentiated pricing strategy. To measure the impacts of the carriers’ pricing on
their profits and consumer surplus, I develop a structural model of consumers’ demand
and carriers’ dynamic pricing game over smartphones bundled with two-year contracts. I
assume that consumers make static discrete purchase decisions, where the OS network sizes
affect consumers’ utility, and the carriers choose smartphone prices to maximize long-run
profits. I estimate the model using product level data from 2011 to 2013.
It is a challenge to estimate the model of the carriers’ dynamic pricing game because
it features continuous choices, asymmetric multi-product firms, and high dimension state
space. Existing estimation methods for dynamic games can not be used in this paper.
I deal with this challenge by combining the value function approximation approach and
mathematical programming with equilibrium constraints (MPEC) to find equilibria of the
game in the estimation. Multiple equilibria of the game may exist and present issues to the
estimation. I explain the assumptions needed for identification, the continuity of the GMM
objective function of the estimation, and the implications on the counterfactual results in
the corresponding sections.
I use instrumental variables to identify the OS network effect and the price coefficient.
The estimation results show that the OS network effect is positive and significant, and
adding 19.41 million users for an OS increases a consumer’s utility by the same amount
as cutting the price by $100. Consistent with the results in the theoretical model, I find
that the carriers’ estimated markups on the large OSs (Android and iOS) are lower than
on small OSs (Blackberry and Windows Phone). Nonetheless, 38.25% of the four carriers’
profits are from Android model and 55.71% from iOS models due to their high volume of
sales.
With the estimates, I study two counterfactual cases. In the first case, I find that if each
carrier specialized in one OS and no two carriers specialized in the same OS, the prices of
the Android and iOS models would increase; the profits of Verizon (specialize in Android)
and AT&T (iOS) would increase by 48.31% and 74.45%, while Spring (Blackberry) would
and T-Mobile (Windows Phone) would each lose profits by more than 60%. The large
profit changes are due to OS specialization and price adjustments. The OS market would
be less concentrated, and the smartphone penetration rate by October 2013 would drop
from 78.36% in the data to 62.53%. Consumer surplus would decrease by $0.14 billion
during the sample period.
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In the second case, I find that if the two-year contracts were eliminated, AT&T’s profit
would increase by 18.25% because it would no longer offer high discounts on iPhones but
still have strong iPhone demand; Verizon’s profit would drop by 8.69% because of lower
demand of Android models, and more than half of Verizon’s customers bought Android
models in the data; and the profits of Sprint and T-Mobile would decrease by 44.32%
and 40.18%. The smartphone penetration rate would decrease from 78.36% in the data to
58.31%. Consumer surplus would decrease by $0.86 billion.
This paper contributes to the network effect literature by studying the multi-network
sellers’ dynamic pricing strategy, which hasn’t been analyzed either theoretically or em-
pirically. Theoretical research on network effects has focused on the competition between
single-network sellers, but not the prices of multi-network sellers. Katz and Shapiro (1985),
Farrell and Saloner (1986), Katz and Shapiro (1992), Katz and Shapiro (1994), Shapiro and
Varian (1999), Rochet and Tirole (2003), Armstrong (2006), Rochet and Tirole (2006) Zhu
and Iansiti (2007), Rysman (2009), and Weyl (2010) all study the impact of the network
effect on the prices of either monopolistic or oligopolistic single-network sellers. In this
paper, I find that the dynamic pricing strategy of multi-network sellers is opposite to the
equilibrium strategies of single-network sellers.
The empirical literature on network effects has studied markets in which single-network
manufacturers set retail prices, including papers that study the network effect in the yellow
page industry (Rysman (2004)), the VCR industry (Park (2004)), the PDA industry (Nair,
Chintagunta, and Dube (2004)), the ACH banking industry(Ackerberg and Gowrisankaran
(2006)), the video game industry (Dube, Hitsch, and Chintagunta (2010), Lee (2013)), and
the DVD player industry (Gowrisankaran, Park, and Rysman (2014)). In these markets,
manufacturers can’t internalize competition across networks. However, in this paper, I am
interested in the multi-OS carriers’ dynamic pricing strategy.
This paper also makes a contribution to the literature on the estimation of dynamic
games. Aguirregabiria and Mira (2007), Pakes, Ostrovsky, and Berry (2007), Pesendor-
fer and Schmidt-Dengler (2008), Kasahara and Shimotsu (2012) have proposed estimation
approaches for dynamic discrete choice games, which are based on conditional choice proba-
bilities. Since the pricing game in this paper is a continuous choice game, these approaches
can not be used. Bajari, Benkard, and Levin (2007) propose a two-step method that
can estimate dynamic games with continuous choices. The first step estimates the policy
functions, and the second step estimates the full model using the method of simulated min-
imum distance. If I use this two-step method in this paper, the first stage results would
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be very inaccurate, because there aren’t enough observations for each product due to the
high-dimension state space and the large number of products. In addition, this method
requires monotonicity of the policy functions on shocks, and linearity of the value functions
in parameters is assumed to reduce computation time. It is hard to prove monotonicity
of prices in shocks under the differentiated pricing strategy, and the value functions are
nonlinear in model parameters. Therefore, the two-step method can not be applied to this
paper either.
Several papers have studied the dynamic pricing problems of single-product firms.
Benkard (2004) use static estimates to solve a dynamic oligopoly model with four single-
product aircraft firms. Liu (2010) and Dube, Hitsch, and Chintagunta (2010) analyze the
dynamic decisions of two oligopolistic video game console manufacturers. They assume
parametric forms of the policy functions instead of solving for equilibrium. Goettler and
Gordon (2011) analyze the dynamic investment and pricing problem of two single-product
microprocessor firms. Sweeting (2012) tests how accurately dynamic pricing models de-
scribe sellers’ behavior in secondary markets for event tickets. Since the telecom carriers in
this paper are asymmetric multi-product firms, value function iteration or policy function
iteration would be difficult to implement and inaccurate.
Instead of using the two-step methods or policy function iteration, I solve the multi-
network carriers’ dynamic pricing game in the estimation. To do so, I approximate the
carriers’ value functions with basis functions to derive the carriers’ first order conditions
and develop an efficient algorithm to find equilibria.2 I estimate the model using Gener-
alized Methods of Moments (GMM) with MPEC, which was introduced by Su and Judd
(2012). The moment conditions are based on the orthogonality between unobserved shocks
and exogeneous variables and instrumental variables. The carriers’ Bellman equations are
imposed as constraints on the value function approximation. Ai and Chen (2003) and
Chen (2007) propose a minimum distance estimator with sieve approximation and show
efficiency. Barwick and Pathak (2015) use sieve approximation and MPEC method to
estimate a model of dynamic optimization problem.
This paper also contributes to the literature on the smartphone industry. Parker and
Van Alstyne (2010) analyze innovation and the platform openness control. Zhu, Liu, and
Chintagunta (2011) and Sinkinson (2014) study the incentives and the effects of the exclu-
sive contracts between Apple and AT&T. Kim (2012) focuses on variations in consumers’
2There is a multi-equilibria issue when solving for equilibria. I will discuss the issue whenever it is aconcern in the following sections.
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adoption of mobile apps across different OSs. Boudreau (2012) discusses app developers’
innovation patterns. Bjorkegren (2014) estimates consumers’ dynamic demand for mobile
phones. Bresnahan, Orsini, and Yin (2014) model and estimate mobile app developers’
OS platform choice. In this paper, I study the impact of the carriers’ two-year contract
discounts.
The paper proceeds as follows. In Section 2, I study a two-period, two-OS model to
compare prices in two different supply settings. Section 3 sets up the consumer demand
and the carriers’ supply model for smartphones with two-year contracts. The industry
background and data used in this paper is described in Section 4. Section 5 discusses
identification and estimation details. The estimated results are presented in Section 6.
Section 7 shows the two counterfactual analysis results. Section 8 concludes the paper.
2 A Two-Period, Two-OS Model
In this section, I study a multi-network seller’s pricing strategy in a two-period, two-OS
model and compare it with single-network sellers’ strategies. This two-period model helps
to understand the telecom carriers’ pricing problem of smartphones in Section 3 and the
observed pricing strategy in data in Section 4.
2.1 Demand Model
There are two smartphone models, A and B, in a two-period economy. The two models have
different OSs, which are also denoted by A,B to simplify notation. Let the total mass of
consumers be 1 and the market shares of the two OSs be nt = (nAt, nBt) at the beginning
of period t. Assume that nA1 + nB1 < 1, which implies that not all consumers have
smartphones in the beginning of the first period. In each period, only consumers who do
not own smartphones enter the market. So the market size in period t is Mt = 1−nAt−nBt.Consumer i’s utility of buying smartphone j ∈ A,B in period t is:
uijt = δj + γnjt − αpjt + εijt,
in which δj , j ∈ A,B, is the consumer utility from the characteristics of model j; pjt is
the carrier’s smartphone price in period t; εijt is the idiosyncratic utility shock of option
j ∈ A,B in period t; and γ and α are parameters for OS network size and price.
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Assumption 1. A positive network effect exists, γ > 0. Without loss of generality, assume
that network A has a higher market share than B in period 1: nA1 > nB1.3
Assumption 2. The two models have the same characteristics, δA = δB, and the same
unit cost, c = 0.4
Assumption 2 means that the only difference between A and B lies in their network
sizes. This assumption allow me to focus on the network size effect in this model.
An outside option, not to buy any smartphone, exists in each period. Normalize the
mean utility of the outside option to be zero. Consumer i’s utility of the outside option is
ui0t = εi0t. Assume that the utility shock εijt follows a Type-I extreme value distribution
and is i.i.d. across consumers, models, and periods. The sales market share of model j in
period t is
sjt(pcAt, p
cBt, nt) =
e(δj+γnjt−αpjt)
1 +∑
k=A,B e(δk+γnkt−αpkt),∀j ∈ 0, A,B. (1)
An OS network grows due to the new sales of smartphones. At the beginning of the second
period, the market share of OS j ∈ A,B is
nj2 = nj1 +M1sj1(pcA1, pcB1, n1). (2)
Therefore, the market size in the second period is M2 = 1−nA2−nB2 = M1s01, where s01
is the market share of the outside option in the first period.
2.2 Two Single-Network Sellers’ Pricing Game
Consider two single-network sellers who play a dynamic pricing game in the two periods.
Denote the two sellers by A,B too for notation simplification. Seller j ∈ A,B only
sells smartphone j. In this subsection, I use superscript m to denote the single-network
sellers (manufacturers who sell directly to consumers) in this subsection. For seller j, the
3There are many reasons that the networks are asymmetric in a particular point of time. Different OSsmay enter the market in different years. Their companies may have different demand and supply shocks.Different operating systems may have different openness towards smartphone manufacturers.
4By normalizing costs to be zero, the prices in this section can be interpreted as markups that the carrierearns. When the costs are not zero, choosing prices is equivalent to choosing markups.
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profit in each period t is
πmjt (pmAt, p
mBt) = pmjtsjt(p
mAt, p
mBt)Mt.
The dynamic problem of seller j ∈ A,B is
maxpmj1πmj1(pmA1, p
mB1) + βdmax
pmj2πmj2(pmA2, p
mB2, n2|pmA1, p
mB1).
subject to the OS share transition rule in equation (2). Let (p∗mA1 , p∗mB1 , p
∗mA2 , p
∗mB2) be the
equilibrium prices.
Proposition 1. (1) The optimal price of A is higher than that of B in both periods:
p∗mAt > p∗mBt , for t = 1, 2.
(2) Network A keeps its network advantage in the second period.
Proof. See Section A.1 of the Supplemental Material.
The first statement of Proposition 2 says that, seller A chooses higher prices than B
does in both periods because seller A has initial OS network size advantage. Suppose that
both models have the same price in the first period, then A’s marginal profit is greater
than B’s, which is zero. So seller A would increase price. In equilibrium, A’s price is higher
than B’s price in the first period. The second statement says that A can keep its network
advantage in the second period.
2.3 A Monopoly Multi-Network Seller’s Pricing Problem
I now consider one seller who sells both models and chooses prices in the two periods to
maximize the total discounted profits. The OS market shares at the beginning of period t
are nt = (nAt, nBt). The seller’s profit in period t is:
πt(pcAt, p
cBt|nt) = [pcAtsAt(p
cAt, p
cBt, nt) + pcBtsBt(p
cAt, p
cBt, nt)]Mt.
where the superscript c means a multi-network seller (carrier). In the first period, the
seller’s profit maximization problem is:
maxpcA1,p
cB1
π1(pcA1, pcB1|n1) + βd max
pcA2,pcB2
π2(pcA2, pcB2, n2|pcA1, p
cB1) (3)
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subject to the OS share transition rule in equation (2). βd is the discount factor. The first
period prices affect the seller’s profits in both periods because of the network effect and
market size transition. The multi-network seller can internalize the competition between
A and B since it chooses the prices of both products. Optimal prices require that the
marginal profits from pcAt and pcBt are zero. The dynamic optimization problem can be
solved backwards. Let the optimal prices of the multi-network seller be (p∗cA1, p∗cB1, p
∗cA2, p
∗cB2).
Proposition 2. (1) The price of A is lower than that of B in the first period: p∗cA1 < p∗cB1.
(2) The price difference between the two models |pc∗A1 − pc∗B1| increases as the OS network
effect, γ, increases.
(3) The OS market share difference at the beginning of the second period (nA2 − nB2)
increases with the OS network effect, γ.
Proof. See Section A.2 of the Supplemental Material.
The first statement in Proposition 1 says that, when the OS network effect exists,
the multi-network seller chooses a lower price for the larger network A than for B in the
first period. It can be shown that the multi-OS seller’s second-period profit is convex in
(nA2, nB2). The seller prefers OS concentration because the strong network effect of A can
attract more future consumers, and it can get more profits in the second period.5 The sec-
ond statement means that the seller chooses more differentiated prices as the network effect
become stronger. The third statement says that the market becomes more concentrated in
the large operating system as the network effect increases.
The discount factor also makes an impact on the first period prices. Without the
dynamic effect (βd = 0), the optimization problem is static. In a static pricing problem
with Logit demand model, the multi-OS seller will choose the same price for the two
products, because the cross-derivatives of prices (αsAtsBt) are the same, and so are the
carrier’s two first-order conditions, as shown in Supplemental Material A.1. However, when
βd > 0, the large network has a lower price in the first period, pcA1 < pcB1, though the prices
of A and B in the second period are the same, pcA2 = pcB2.
The OS network effect affects optimal prices similarly as the discount factor. If there is
no network effect (γ = 0), A and B will have the same price in both periods since they are
symmetric products. However, if the network effect exists (γ > 0), the larger network A
5The reason for selling products with different OSs by the carriers is because that consumers are het-erogeneous. Some consumers might prefer B no matter how large network A is. So the carrier still sells B,which can increase its profits.
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will have a lower price than B in the first period because the seller’s second-period profit
increases with the OS concentration. Thus, both βd and γ need to be positive for the seller
to choose different prices for A and B.
The Logit demand model is an ideal choice to analyze the impact of network effect
on the multi-network seller’s prices. With the Logit demand model, the seller chooses the
same price for both OSs in each period when γ = 0 and βd > 0. This provides a clear
benchmark for studying the seller’s prices when γ > 0. Any price differentiation across the
two OSs will reflect only the impact of the network effect.
Though I consider a monopoly multi-network seller, its dynamic pricing strategy carries
over to the case with multiple multi-network sellers.6 Because the competition among the
sellers doesn’t change their incentive to take advantage of the initially larger network, and
using prices to grow different OSs can not be an equilibrium.
2.4 Comparing the Two Models
Single-OS sellers and the multi-OS seller choose the opposite pricing strategies in the first
period. This is because of the difference in their ability to internalize competition effect
across OS and the network effect. The multi-network seller prefers network concentration
and uses price differentiation to achieve that. Single-network sellers set prices based on
their network sizes.
In Section 4, I show that the carriers’ pricing strategy in data is consistent with the
multi-network seller’s dynamic pricing strategy. Next, I set up an empirical model of the
consumers’ demand and the carriers’ pricing of smartphones in the US, which is more
general than the two-period, two-OS model.
3 An Empirical Model of Demand and Supply of Smart-
phones
In this section, I design a structural model of consumer demand and carriers’ dynamic
pricing game for two-year contract smartphones. There are four leading wireless carriers,
four operating systems, and hundreds of smartphone models. I assume consumers make
static purchase decisions of smartphones and use the random coefficient demand model
as in Berry, Levinsohn, and Pakes (1995). I discuss more about the assumption of static
6I discuss more about multiple-carrier competition in Section A.3 in the Supplemental Material.
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decisions at the end of Section 3.1. The carriers play an infinite horizon dynamic pricing
game.7 Each carrier sold phones with all the four OSs, but the sets of phone models vary
by carrier and over time.
One challenge in modeling consumers’ demand for smartphones is that the sales market
shares are only available at the carrier-OS level, not the smartphone model level. Mean-
while, characteristics and prices data are at the model level in my dataset. To use as much
information on prices and characteristics as possible, I introduce a carrier-OS specific un-
observed demand shock. I explain this in detail next.
3.1 Consumer Demand
Each period, consumers who don’t own any smartphone or have ended previous two-year
contracts enter the market. Each consumer chooses one option from the choice set to
maximize utility. The choice set in period t is Ωt = (j, s, c, t)jsc ∪ (0, t), where j ∈1, 2, ..., Jt is a smartphone model, s ∈ 1, 2, ..., S is the operating system of model, and
c ∈ 1, 2, ..., C is a carrier. An outside option (0, t) exists, and it means not buying any
smartphone. Jt is the total number of models in Ωt.
When a consumer purchases model (j, s, c, t), s/he signs a two-year wireless service
contract with carrier c. Assume that consumer i’s utility of buying the model is:
uijsct = x′jscβi − αi(pcjsct + fct) + γNst + ηsvst + ψsc + ξsct + εijsct. (4)
xjsc is a K × 1 vector of observed smartphone characteristics. pcjsct is the price of the
two-year contract price of the smartphone. fct is carrier c’s price for wireless service for
two years.8 Nst is the number of users of OS s at the beginning of period t. It captures
both the indirect network effect and the direct network effect of an OS, as described in the
introduction.9 vst is the number of new versions of operating system s since the beginning
of data. ηs measures the improvement of a new version of OS s. ψsc is a dummy for the
carrier-OS pair (s, c). It captures the carrier-OS quality that is constant across periods.
Hence, (ηsvst +ψsc) represents the time-varying quality of the carrier-OS group. ξsct is the
7In this paper, I don’t model the manufacturers’ choices of prices in a Stackelberg leader-and-followerframework. I focus on the price decisions of the carriers after the manufacturers set their wholesale prices.
8I assume that the consumer takes the two years’ wireless service costs into account when signing thecontract.
9I can not separate the two kinds of network effect in this paper, and each type of network effect can bethe main force in the network effect in this paper.
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carrier-OS level unobserved demand shock in period t. εijsct is a consumer idiosyncratic
utility shock.
The unobserved quality shocks ξsct is assumed to be carrier-OS specific because the
market share data are at the carrier-OS level. The implication of the assumption is that the
market share variation across different models in the same carrier-OS group is determined
by their observed characteristics and prices, not by their individual unobserved quality
shocks.
Consumers have different income levels and tastes for the smartphone characteristics.
The parameters θi = (βi, αi) are consumer specific. Consumer i is described by vi =
(yi, vi1, ..., viK), where yi is income and viks are independent standard normal taste shocks.
Assume that vi is independent of the unobserved quality shock ξsct. Thus,(βi
αi
)=
(β
α
)+ Φvi,
in which β is the mean of βi over all consumers; α is the part of αi that is the same for all
consumers; and Φ is a diagonal matrix that measures the impact of vi on (βi;αi). Rewrite
the utility function (4) as:
uijsct = δjsct + µijsct + εijsct,
whereδjsct = x′jscβ − α(pcjsct + fct) + γNst + ψsc + ξsct,
µijsct = [x′jsc; (pcjsct + fct)]′ ∗ Φvi.
The mean utility of the outside option is normalized to zero. Consumer i’s utility of
the outside option is:
ui0t = εi0t.
Assume that the εijsct follows a Type-I extreme value distribution and is i.i.d. across
(i, j, s, c, t). Then consumer i’s probability of choosing product (j, s, c) in period t is:
sijsct(vi) =e(δjsct+µijsct)
1 +∑
j′s′c′∈Ωte(δj′s′c′t+µij′s′c′t)
.
Let Ajsct be the set of consumer characteristics such that j has the highest utility for
consumers in this set. That is, Ajsct = vi|uijsct(vi) ≥ uij′s′c′t(vi), for all (j′s′c′t) ∈ Ωt.
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Then the market share of product (j, s, c) in period t is:
sjsct =
∫Ajsct
sijsct(vi)dF (vi). (5)
I aggregate the smartphone model shares to carrier-OS levels, which are observed in
the data. Let Ωsct be the set of models with OS s by carrier c in period t. The market
share of the carrier-OS group (s, c) in period t is:
ssct =∑j∈Ωsct
sjsct. (6)
Consumers are assumed to make static decisions because it is very challenging to esti-
mate a model with dynamic demand and dynamic continuous game of firms for two reasons.
First, it’s rare to have explicit forms of the market share derivatives in a dynamic demand
model because consumers’ value functions are unknown. But the derivatives would be
required to analyze the FOCs in the firms’ dynamic problems. Second, with a dynamic de-
mand model, the carriers’ state variables would have to include the smartphone ownership
distribution, which would be a high dimension vector (shares of different models and the
contract status distribution) in this paper.
The main concern with using a static demand model is that it ignores the consumers’
expectation of future prices and OS network sizes. However, the static demand model
still gives the carriers the incentive to make dynamic price decisions, because as long as
consumers value the OS network sizes, current prices will always affect the future OS
network sizes.
The static model may lead to biases in the network effect estimate. The directions
of the biases depend on which of the following two dynamic factors dominates the other.
On one hand, forward-looking consumers may postpone purchasing a large OS model if
anticipating a decrease in price. A static model treats this low current demand for a
large OS as if that consumers do not value the OS network effect enough, which results
in underestimation. On the other hand, consumers may adopt a small OS because they
believe this OS would eventually dominate, which could lead to overestimation.
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3.2 The Carriers’ Dynamic Pricing Game
The carriers play a dynamic pricing game of smartphones due to the evolving OS network
sizes and market size. In this subsection, I model the carriers’ costs, the market size, and
the carriers’ dynamic pricing game over smartphones. Each period, the carriers observe
the OS market shares and choose the two-year contracts prices of smartphones.10
3.2.1 The Carriers’ Unit Costs
A carrier pays a wholesale cost, a service cost, and an unobserved cost shock on each smart-
phone model. Carrier c’s wholesale cost of model (j, s, c, t) is the product of a manufacturer
wholesale-retail price ratio ωj and the manufacturer retail price pmjsct. ωj is assumed to
be manufacturer specific.11 It captures the manufacturer’s bargaining power against the
carriers.
In addition to the wholesale cost, carrier c also pays a carrier-OS specific monthly
service cost κsc. It includes the costs of selling a phone, maintaining wireless coverage, and
providing customer service. There is also an unobserved cost shock at model level, λjsct.
Hence, carrier c’s unit cost of selling model (j, s, c) in period t is:
kjsct = ωjpmjsct + 24κsc + λjsct. (7)
3.2.2 The Market Size and the Transition of OS Market Shares
Let the cumulative OS market shares be nt = (n1t, ..., nSt) at the beginning of period
t. Let M be the population of potential smartphone users. The OS cumulative share of
OS s is nst = Nst/M . The sum∑S
s=1 nst is less than 1 because not all consumers have
smartphones at the beginning of period t.
In each period, two types of consumers enter the market, those who do not own any
smartphone yet and those who have finished their previous contracts. The share of the first
type consumers is 1−∑S
s=1 nst. To get the share of the second type consumers, I assume
that each user has the same probability to end his/her current contract every period. This
10The manufacturers may also affect the two-year contract prices of smartphones by negotiating withcarriers. I assume that a carrier would only reach an agreement with a manufacturer if the negotiatedprices can maximize its long run profit. Then the carriers indirectly choose the two-year contract priceseven if the agreements between manufacturers and carriers specify the two-year contract prices.
11 The manufacturers’ wholesale prices could change with the OS network sizes. However, this effectcould be already reflected in the manufacturer retail prices.
14
probability is fixed to be one eigth because a contract is 24 months long and one period is
three months in this paper. Hence, the market size in period t is:
Mt = 1−∑s
nstM +1
8
∑s
nstM = 1− 7
8
∑s
nstM. (8)
There are two limitations of assuming the same probability of ending contracts. First,
in reality, the consumers who end their contracts in a period should be the customers who
bought new smartphones two years ago. Tracking the distribution of the smartphone users’
contract status (shares of customers on each OS with different numbers of periods left) is
feasible. However, this would make the distribution vector a state variable for the carriers.
This would increase the dimension of the state space by at least four, which would be very
challenging to estimate. Second, some consumers may use a smartphone for more than two
years, in which case the carriers would face smaller markets in the data than in the model.
This implies that the carriers’ observed differentiated prices are for smaller markets than
in the model. Thus, I may underestimate the network effect parameter using the larger
markets in the model to match the same degree of price differentiation.
The market size decreases with the sum of OS shares. By assumption, the market
size cannot be zero, because 1/8 of the previous users end their contracts and re-enter the
market each period. At the beginning of period t+1, an OS has two types of users, previous
users from period t− 1 and new users in period t. Let Ωst be the set of smartphones with
OS s in period t. The transition of the cumulative market share of OS s is:
nst+1(nt, pct) =
7
8nst + (1− 7
8
S∑s′=1
ns′t)∑
(j,c)∈Ωst
sjsct(pct , ξt). (9)
3.2.3 Timing of the Pricing Game and the Carriers’ Bellman Equations
At the beginning of period t, the carriers observe the OS market shares, nt. Then the
demand and cost shocks (ξt, λt) are realized. Each carrier is assumed to have perfect infor-
mation of all carriers’ demand and cost shocks. The carriers choose prices simultaneously,
then consumers make purchase decisions. At the end of period t, the state variables update
to nt+1.
Denote the set of carrier c’s smartphones in period t by Ωct. Let λt be the vector of all
cost shocks in period t and pct be the vector of all carriers’ prices in period t. Carrier c’s
15
profit in period t at price pct is:
πct(pct , ξt, λt) =
∑(j,s)∈Ωct
(pcjsct + fct − kjsct)sjsct(pct , ξt)Mt, (10)
where the demand shocks affect the market shares, and the cost shocks affect the unit costs
as in equation (7).
The carriers play dynamic pricing game because the prices in period t affect the OS
market shares in the next period. The demand shocks and cost shocks affect their prices,
so the price of each product is a function of these shocks, pjsct(ξt, λt). Carrier c’s Bellman
equation is:
Vc(nt) = Eξ,λ
[max
pcjsct(ξt,λt),(j,s)∈Ωct
πct(p
ct , ξt, λt) + βdVc(nt+1(nt, p
ct(ξt, λt)))
], (11)
subject to equation (9). βd is the discount factor across periods. The expectation is over
the unobserved shocks (ξ, λ), and the carriers choose prices after they observe the shocks.
The value functions are carrier specific because the carriers have different smartphone sets,
wireless service costs, and wireless plan prices.
I assume that the OS market shares are the only state variables in the carrier’s dynamic
game. Ideally, the evolving sets of smartphone models and their characteristics should also
be state variables. The number of smartphone models by each carrier is not a concern,
since it is relatively stable over time as shown in Section D.1 in the Supplemental Materials.
But the characteristics of the smartphones have been improving over time, so there should
be an increasing trend in the carriers’ period profits since the outside option always has
zero mean utility in any period. However, to keep the problem tractable, I don’t add these
variables to the state space. The value functions in this paper can be interpreted as the
averages of the discounted profits across all periods in the data.12
Assumption 3. (1) ξsct and λjsct follow the normal distributions N(0, σ2ξ ) and N(0, σ2
λ),
respectively.
12I also considered whether time, t, should be a state variable to count for the evolving set of smartphones.However, it’s not reasonable to assume that the carriers make decisions based on the time periods assigned inthis paper. An alternative is to add an inclusive value that represent the overall utility of all smartphonesin each period. See Gowrisankaran, Park, and Rysman (2014) for more details about inclusive value indiscrete choice demand models. However, I don’t use this method either because the inclusive value is anunobserved variable and must be calculated for each set of structural parameters, and it also increases thedimension of the state space.
16
(2) The cost shocks are independent across models and periods, and they are independent
with demand shocks.
The assumption of normal distribution and independence will be used in the estimation.
The cost shocks are assumed to be independent across periods so that they wouldn’t be state
variables. The independence of cost shocks across models and that between demand shocks
and cost shocks are not essential to identification and would not add much computation
burden if relaxed. The unobserved demand shocks are allowed to be correlated over time,
even though I control the time-invariant carrier-OS quality and the OS quality improvement
over time in the utility function. In case that they are correlated, I use instrumental
variables to deal with the possible endogeneity problem, which will be explained in Section
5.1, but the demand shocks are not added as state variables for tractability.
For any (ξt, λt), carrier c’s first-order conditions (FOC) with respect to price pjsct is
Mtsjsct(pct , ξt) +Mt
∑(j′,s′)∈Ωct
mj′s′ct∂sj′s′ct∂pcjsct
+ βd∂Vc(nt+1(nt, p
ct))
∂pcjsct= 0, (12)
where mjsct denotes the carrier markup:
mjsct = pcjsct + fct − kjsct. (13)
The price pcjsct affects not only the carrier’s current profit, but also its future profit through
the OS network size. The FOC implies that the marginal profit should be zero at the
equilibrium prices.
The carriers’ choices of service prices, fcts, are taken as exogenous for several reasons.
First, the wireless service plan price of each carrier rarely changed in the data. Second,
since each carrier sets the same service price for all models and OSs, the choice of optimal
service price is not key to the price differentiation across OSs. Lastly, the few service price
adjustments by the carriers in the data don’t appear periodically, which makes it hard to
define a period. Thus, I take the carriers’ service prices as given.
3.3 Equilibrium
The equilibrium concept used in the carriers’ dynamic pricing game is Markov Perfect Nash
equilibrium (MPNE). In this paper, an MPNE is a subgame perfect equilibrium where the
strategies depend on the past only through the state variables. An equilibrium consists of
17
a vector price function, pc(n, ξ, λ), and value functions, Vc(n)s, such that (1) Vc(n)s are
the expected discounted long run profits given pc(n, ξ, λ); and (2) pc(n, ξ, λ) maximizes the
long run profit for each carrier, given the rival’s prices in pc(n, ξ, λ) and Vc(n)s.
The dynamic game may have multiple equilibria for a given set of model parameters.
De Paula (2013) reviews the methods to deal with issues in identification, estimation, and
post-estimation analyses raised by the existence of multiple equilibria. I assume that the
data are from the same equilibrium and there is a unique vector of parameters that can
generate this equilibrium. Then the existence of multiple equilibria will not be an issue
for identifying the parameters. Since I use panel data from one single market (the US) as
opposed to multiple markets, assuming that the data are from the same equilibrium is not
as strong as when the data are from multiple markets. In this paper, multiple equilibria
issue will not cause discontinuity in the objective function in the estimation. I will explain
this at the end of Section 5.2.2. But it may affect the evaluation of the Bellman equation
and counterfactual computation, which will be discussed in Section 5.3 and Section 7.1.
4 Industry Background and Data
4.1 Background of the U.S. Smartphone Industry
A consumer has to choose both the smartphone model and the service provider when buying
a smartphone. The top service providers (carriers) in the U.S. are Verizon Wireless, AT&T
Mobility, Sprint Corporation, and T-Mobile US. According to Kantar World Panel data,
the average combined share of smartphone sales for the four carriers is 88.72% from October
2011 to November 2013. The top four OSs in the U.S. smartphone industry are Android,
iOS, Blackberry, and Windows Phone. Their combined market share increased from 94%
in 2011 to 99% 2011 in 2014.13 Therefore, I consider the top four OSs and top four carriers
in this paper.
Verizon, AT&T, Sprint, and T-Mobile all have been selling smartphone models with
Android, Blackberry, and Windows Phone since these OSs were first launched. AT&T
had been selling iOS exclusively until January 2011 when iPhones became available from
Verizon. Sprint started selling iPhones in October 2011, and T-Mobile started in April
2013. Since then, all carriers have been selling models with all the four OSs.
The two-year contract policy has been used by all carriers from the beginning of the
13Cromar (2010) has a thorough description of the US smartphone industry.
18
smartphone industry. Consumers get discounts on smartphones off the manufacturer retail
prices if they sign two-year service contracts. For example, Apple’s retail price of the
iPhone 5 was $649 in Oct 2012. Consumers could pay $199 to get an iPhone 5 if they sign
contracts with AT&T. If consumers need to end the contract early, they have to pay early
termination fees. Depending on the number of months left in an contract, the termination
fee could be between $150 and $350. According to the Statista.com, the average monthly
churn rate for the four carriers is 2% on average.14 Since 2013, the carriers gradually went
away from the two-year contract model, which has lead to a lot of discussions about its
impacts on the carriers and consumers.
I focus on the consumers’ demand for smartphones with two-year contracts in this
paper. According to the US Wireless Industry Overview 2011, more than 78% of mobile
phone users were on two-year contracts. The percentage is expected to be even higher for
smartphones alone because they are much more expensive without contracts.
4.2 Data
The data used in this paper come from several sources, and the sample period is from
Aug 2011 to Oct 2013. comScore.com reports the U.S. cumulative smartphone subscriber
market shares every month. Kantar World Panel has been publishing the sales market
shares by carrier. Carriers’ two-year contract prices and manufacturers’ retail prices for
smartphones are collected via the web archive website. The smartphone characteristics
data are from phonearena.com. I get household income distribution data from the yearly
Current Population Survey (CPS).
I exclude the population younger than twelve years old and older than 70 years old as
smartphone consumers. This assumption makes the potential market size of smartphones
to be 75% of the population, according to the 2010 US population distribution by age. I
calculate the market size Mt and state variables nt using market size and the cumulative OS
shares. The average household income increased from $69,677 to $72,641 and the standard
deviation increased from $368 to $499.
Each month, the sales market shares by carrier by OS are for the past three months.
For example, the sales market shares in Jan 2012 are for the three months ending in Jan
2012. comScore.com also reports the OS sales shares conditional on the sales shares of
14Churn rate is the proportion of contractual customers or subscribers who leave a supplier during agiven time period. Data source is from this link: http://www.statista.com/statistics/ .
19
AT&T and Verizon. Combining the carriers’ sales shares and the OS shares within each
carrier, I get the sales market share for each carrier-OS group. One missing piece of the
sales data is the conditional OS shares for Sprint or T-Mobile. Since only the joint OS
shares for the two carriers are observed, I assume that their OS share ratio is equal to their
number of models ratio. In the end, there are sales market shares for 16 carrier-OS groups
for 8 non-overlapping 3-months periods (out of 26 consecutive months).
The web archive website has been keeping records of the carriers’ webpages every month
sicne 2008.15 The carriers’ two-year contract prices and the listed manufacturer retail price
of each model can be collected by month. In the sample period, the data has 2283 model-
month observations. The highest two-year contract price is $399 for the 64 GB iPhones
from multiple carriers.
The monthly wireless plan prices are also from the web archive website. Each carrier
offers multiple wireless plans each month. I use the single line price for medium amount of
data and minutes.16 Verizon’s wireless plan price was the highest at $70 and T-Mobile’s
was the lowest at $50. The average across carriers is $60 per month during 2011 to 2013.17
To match the sales shares data, a period is three months in the structural model.
But the smartphone prices are observed every month. Thus, to use as much information
as possible, I construct consumers’ choice set every period in the following way. If a
smartphone model is observed in multiple months in a three-months period, I treat them
as different choice options in that period. The data are seasonally adjusted when used in
estimation.18
The smartphone characteristics include camera pixels, built-in storage, 4G dummy,
weight, screen size, resolution, processor speed, memory, and battery capacity. All the
characteristics are scaled so that their values are in similar range to compare their coeffi-
cients in the utility function.
Table 1 shows the summary statistics of the number of models, characteristics, average
smartphone two-year contract price, and manufacturer retail price by carrier-OS group
by month. All four carriers have more than 10 Android models each month on average.
Windows Phone has the fewest number of models, with an average lower than two. iOS
15 The web archive website link is: http://archive.org/web/16I use the prices for the following minutes and data bundles for the 4 carriers: Verizon (unlimited minutes,
2GB), AT&T (450 minutes, 300MB), Sprint (unlimited minutes, 1GB), T-Mobile (unlimited minutes anddata).
17This matches the $61 average reported by New Street Research company for 2013.18See Supplemental Material Section D.2 for details on removing seasonality from the data.
20
Tab
le1:
Des
crip
tive
Sta
tist
ics
by
Car
rier
-OS
grou
p(A
ver
age
over
Mon
ths)
Car
rier
-OS
Gro
up
No.
ofC
arri
erP
rice
Manu
f.P
rice
Batt
ery
Cam
era
Scr
een
Pix
elP
roce
ssor
Sale
sM
od
els
100$
100$
1000mAh
megapixels
inches
100/inch
2Ghz
Sh
are
%
Ver
izon
-iO
S4.
692.
266.7
41.4
37.1
43.6
53.2
61.7
217.8
0V
eriz
on-A
nd
16.1
51.
225.0
41.9
26.8
64.2
42.6
82.6
018.9
4V
eriz
on-B
la3.
001.
454.6
61.3
15.0
33.0
12.6
01.3
40.4
7V
eriz
on-W
in1.
811.
034.3
21.4
95.6
83.9
42.4
51.6
10.0
8A
T&
T-i
OS
5.07
1.98
6.4
71.4
16.7
53.6
63.1
11.6
620.7
5A
T&
T-A
nd
13.8
80.
984.6
91.9
07.0
44.3
12.6
62.9
89.5
8A
T&
T-B
la3.
810.
864.4
81.2
55.3
03.0
72.5
91.2
51.4
AT
&T
-Win
4.81
0.75
4.3
61.6
77.8
24.2
62.4
71.8
11.3
6S
pri
nt-
iOS
4.91
2.04
6.7
11.4
37.3
63.6
63.2
81.7
93.0
7S
pri
nt-
An
d11
.38
0.90
4.4
11.8
05.7
73.9
72.4
52.0
311.9
8S
pri
nt-
Bla
1.65
1.30
4.5
31.1
85.0
62.6
82.7
61.1
10.3
8S
pri
nt-
Win
1.13
0.79
4.4
21.5
75.6
03.7
72.5
71.3
60.4
5T
-Mob
ile-
iOS
4.00
—6.9
61.4
47.9
43.9
83.2
62.5
50.3
6T
-Mob
ile-
An
d10
.62
1.58
4.0
51.7
76.1
05.1
92.4
32.6
211.4
4T
-Mob
ile-
Bla
3.69
2.01
4.4
61.3
95.1
92.9
42.6
11.1
90.8
3T
-Mob
ile-
Win
1.31
1.15
3.4
91.4
65.8
03.9
12.4
81.8
90.8
0
Not
es:
Th
efi
rst
thre
ele
tter
sof
the
OS
sar
eu
sed
inth
eta
ble
.F
or
exam
ple
,“A
nd
”is
for
An
dro
id.
T-M
ob
ile
elim
inate
dth
etw
o-y
ear
contr
act
pol
icy
sin
ceit
star
ted
tose
lliO
Sm
od
els.
Th
esa
les
share
sare
con
dit
ion
al
share
sam
on
gth
eli
sted
gro
up
san
dare
reco
rded
for
the
sale
sin
the
pas
tth
ree
mon
ths
ever
ym
onth
.
21
models have the highest two-year contract prices and manufacturer retail prices on average.
Windows Phone models have the lowest carrier prices and manufacturer prices.
The pattern of hardware characteristics across OSs is mixed. iOS models outperform
other models in camera pixels and screen pixels per square inch. Android models have
the best battery capacities, screen sizes, and processor speeds. From the last column, I
find that Android has the highest sales market shares, and most new iPhone users signed
contracts with Verizon and AT&T.
Figure 1 shows the cumulative monthly market shares of the four operating systems
from August 2011 to October 2013. The market shares of iOS and Android both increased
from below 6% to above 25%. Blackberry’s market share dropped from 10% to less than
5%. The Windows Phone market share was stable and small, at around 3%.
Figure 1: The Cumulative OS Market Shares Over Time (2011.08-2013.10)
Table 2 shows the results from regressing the carriers’ contract prices of smartphones
on past month OS shares, manufacturer retail prices, model characteristics, OS dummies,
manufacture dummies, and month dummies. The results show that the carriers choose dif-
ferentiated prices across OS, lower prices for smartphones with larger OSs. The coefficient
−1.0362 implies that for every 10% increase in an OS share, the carriers drop the two-year
contract price of a model with that OS by $10.36.
22
Table 2: OLS Regression of Carriers’ Contract Prices of Smartphone ($100)
Variables Estimates Std
OS Share (Lag 1 month) -1.0362*** (0.3708)
Manufacturer price 0.6425*** (0.0162)
(Monthly data from Aug 2011 to Oct 2013. Control for
phone characteristics and fixed effects of OSs, carriers,
manufacturers, and months.)
The regression results are consistent with Proposition 1 and 2 in Section 2. The car-
riers are multi-network sellers, so they use a differentiated pricing strategy to achieve OS
concentration and attract more future consumers.
5 Identification and Estimation
The structural model parameters are θd = (α;β; γ;ψ; η; Φ;σξ) in the carrier-OS share
equation (6) and θs = (ω;κ;σλ) in the carriers’ FOCs in equation (12). I use GMM to
estimate (θd, θs). The moment conditions are based on the carrier-OS level unobserved
quality shock ξsct in equation (6) and the model level cost shock λjsct in equation (12). In
the rest of this section, I discuss the identification of the parameters, describe the moment
conditions and objective function in the GMM, and explain how I calculate the demand
and cost shocks for a given set of parameters.
5.1 Identification
The identification of the network effect parameter, γ, and the price coefficient, α, is subject
to endogeneity issues. First, if the demand shock in the past period ξsct−1 affects the current
shock ξsct, then ξsct is correlated with the cumulative network size Nst, which leads to an
endogeneity problem when estimating γ. Second, due to the carriers’ endogenous pricing
decisions on the supply side, the prices are correlated with the demand shocks. To deal
with these issues, I use moment conditions that are based on the orthogonality between
ξscts and a set of instrumental variables (IV).
Identification of network effect is a challenge in the literature, and previous empirical
studies have used different instrumental variables for different industries.19 In this paper,
19 Rysman (2004) uses the population coverage by a yellow page directory as an instrument to identifythe indirect network effect of advertising on the number of uses of the directory. Lee (2013) uses the lagged
23
I use the total number of smartphone models for each OS since the beginning of the data
until period t as the IV for the network size Nst. That is, the instrumental variable for Nst
is∑t
t′=1
∑js′c I(OSjs′ct′ = s), where I(OSjs′ct′ = s) is equal to one if s′ = s and is equal
to zero otherwise. Their simple correlation is 0.67. The underlying assumption is that
the number of smartphone models for each OS in the US in each period is not correlated
with the unobserved demand shocks (which do not include the carrier-OS fixed effects
and the OS quality improvement). This assumption is reasonable for several reasons.
First, all the manufacturers sell smartphones to many countries, and their decisions of
releasing new smartphone models mainly depend on demand from the global market and
competition among manufacturers. Second, most manufacturers (e.g. Apple, Samsung,
and LG) release new models of their flagship smartphones every year. This pattern didn’t
change with demand shocks. Third, the number of smartphone models for each OS is
largely determined by how many manufacturers adopt the OS, which is further determined
by the OS openness that is exogenous to the model. Therefore, the unobserved demand
shocks in the US market should have little impact on the number of smartphone models
in the US market.
To identify the price coefficient, I follow Berry, Levinsohn, and Pakes (1995) and use IVs
including the average characteristics of models in the same carrier-OS group, Ωs,c,t, that of
other OSs by the same carrier, Ω−s,c,t, and that of the same OS by other carriers, Ωs,−c,t,
in which the Ωs are sets of smartphone models and the subscripts denote the OS/carrier
information of the models. The average characteristics in the same carrier-OS group are
cost shifters, which are assumed to be exogenous. The average characteristics of other OSs
or by other carriers are correlated with prices due to the competition among the carriers,
but are also uncorrelated with demand shocks, ξscts. Hence, the average characteristics are
valid IVs.
After dealing with the endogeneity issues, γ is identified by the variation of the sales
shares and the past OS network sizes, and α is identified by the variation of sales shares
and prices across carrier-OS groups.
The diagonal matrix Φ has the non-linear coefficients in the consumer specific coeffi-
cients. It is identified by the variation of market shares and consumer income distribution
across periods.20 In particular, if after controlling for everything else, the average con-
values of software utility as instruments to identify the indirect network effect of video game software titleson hardware adoption. Ackerberg and Gowrisankaran (2006) avoid the endogeneity issue by fully specifyan equilibrium model of the adoption decisions of the two sides of the ACH network.
20See Supplemental Material Section C.1 for the details of simulation and normalization of individual
24
sumer income increases over time and so do the sales shares, then this implies that the
price coefficient decreases as income goes up.
The unit costs then provide identification for service cost κsc and the wholesale pa-
rameters in ω as in equation (7). The differences between observed prices and predicted
markups are the unit costs kjsct. The structural model predicts product level markups for
any given (θd, θs). I don’t directly estimate the standard variances of the demand and cost
shocks, σξ and σλ. Instead, I calculate them using the demand and cost shocks backed out
from the market share equation and the FOCs. Following Goettler and Gordon (2011), I
fix βd to be 0.975 as the three-month discount rate for carriers’ profits.
5.2 Estimation
5.2.1 Moment Conditions and Objective Functions
The moment conditions are based on the orthogonality between the instrumental variables
and the random shocks, (νsct, λjsct). Let (θd0, θs0) be the vector of true parameters. The
moment conditions are:
E[ξsct(θd0)|Z1sct] = 0, (14)
E[λjsct(θd0, θs0)|Z2jsct] = 0. (15)
Z1sct is the vector of IVs as explained above. Z2jsct is a vector of the variables including
manufacturer dummies and carrier-OS dummies in the unit cost equation, the model char-
acteristics, xjsct, the numbers of models in (Ωsct,Ωst,Ωct), the average characteristics over
models in (Ωct,Ωst,Ωt). There are 44 moment conditions in (14) and 67 moment conditions
in (15). The number of structural parameters to be estimated is 62.
To get efficient estimates, I use the two-stage GMM. In the first stage, the weight matrix
for the demand side moment conditions is Wd1 = (Z ′1Z1)−1 and that for the supply side
moment conditions is Ws1 = (Z ′2Z2)−1. The second stage uses the optimal weight matrix
estimate W2, estimated using the first stage results. The second stage objective function
is:
Q2(θd, θs) = (1
Nλ
Nλ∑jsct
[Z1sctξsct(θd);Z2jsctλjsct(θs; θd)])′W2(
1
Nλ
Nλ∑jsct
[Z1sctξsct(θd);Z2jsctλjsct(θs; θd)]).
(16)
income levels.
25
where (Z1sctξsct(θd);Z2jsctλjsct(θs; θd)) is a vector of moment conditions from both the
demand shocks and cost shocks.
5.2.2 Solve for the Demand and Cost Shocks
To evaluate the GMM objective function for a (θd, θs), I first calculate the model level
shares in equation (5) using observed model level characteristics, prices, and the number of
OS users. The model level shares and their derivatives are then used to solve for demand
shocks and cost shocks for any given vector of (θd, θs).
To calculate demand shocks, ξsct(θd), I aggregate the model level shares to the carrier-
OS level, so that they match the observed carrier-OS shares. I show that there exists a
unique vector of demand shocks that make the model prediction match the data for any
θd. See Appendix A for the proof of the invertibility from the carrier-OS sales shares to
ξsct(θd).
The model market share in equation (5) is an integration of individual probabilities
over the distribution of consumer characteristics vi. Since vi is a nine-by-one vector, I
use numerical approximation to calculate the integration. I simulate Ns = 200 consumers
with different characteristics each period and use the averages of their individual choice
probabilities to approximate the sales market share of each model.21
sjsct(θd) =1
Ns
Ns∑i=1
sijsct(θd). (17)
The predicted carrier-OS sales share is the sum over all models in the group.
ssct(θd) =∑j∈Ωsct
sjsct(θd).
Following Berry, Levinsohn, and Pakes (1995) and Nevo (2001), I apply an iterative
procedure to solve for the unobserved shocks ξ(θd). Let the observed carrier-OS shares
be sosct. Given an initial guess of the vector of unobserved demand shocks, ξ0 = ξ0sct,
calculate the predicted market shares ssct(θd, ξ0). Then compare the predicted shares with
the observed shares. The updating rule is to increase ξsct if the predicted share is less than
21To check the accuracy of the numerical integration with 200 simulated individuals, I compare the inte-gration results for some known joint normal distributions by simulating 1,000, 5,000, and 10,000 individuals.I find that simulating 5,000 individuals only changes the integration by a magnitude of less than 10−4.
26
the observed market share for the group (s, c, t) and decrease it otherwise. Repeat this
updating process until the vector ξk converges. The iteration is summarized by:
ξk+1sct (θd) = ξksct(θd) + χ(sosct − ssct(θd, ξk(θd))),
where χ is a constant, set to be 0.9. The proof of unique fixed point in Appendix A
guarantees the convergence of this iteration.
Next, I describe the algorithm for calculating the cost shock λjsct for a given (θd, θs).
I first solve for the smartphone model level markup mjsct using data and FOCs. Then it’s
straightforward to calculate λjsct, using the definition of markup. As in equation (12), the
FOC w.r.t. price pcjsct is:
Mtsjsct(pct , ξt; θd) +Mt
∑(j′,s′)∈Ωct
mj′s′ct∂sj′s′ct∂pcjsct
+ βd∂Vc(nt+1(nt, p
ct(ξt)))
∂pcjsct= 0. (18)
An important feature of the FOCs is that they are linear in the markups mjscts, given
the observed prices. I take advantage of this linearity when solving for equilibrium prices.
The first two terms in equation (18) can be calculated using the demand side market
share functions. To calculate the last term in equation (18), I approximate each carrier’s
value function with a linear combination of basis functions, so that that there is explicit
functional form for ∂Vc(nt+1)∂pcjsct
.
Each carrier’s value function is a multivariate function of the four operating systems’
market shares nt. I use the second-order complete polynomials as basis functions. I also
use higher order polynomial approximation to check the robustness of the estimates and
find the results don’t change much.22 Hence, there are 15 basis functions for the four state
variables. Denote the basis functions by Bf(n) = (1, bf1(n), ..., bf14(n)). Let θvc be the
coefficient vector for carrier c ∈ 1, 2, 3, 4.
Vc(nt) = Bf(nt) ∗ θvc .
Let θv = (θv1 ; ...; θv4) be the vector of approximation coefficients. With the approximated
value functions, I solve for the model level markups using the FOCs. In Supplemental
Materials Section B, I derive the function forms for the derivatives in equation (18). Let
22Barwick and Pathak (2015) use the Multivariate Adaptive Regression Spline (MARS) method to ap-proximate multivariate functions.
27
mjsct(θd, θs) be the solution for the given (θd, θs). Then the unobserved cost shock is:
λjsct(θd, θs) = pcjsct + fct −mjsct(θd, θs)− ωjpmjsct − 24κsc. (19)
Therefore, given an alternative of the parameters (θd, θs), the shocks ξsct(θd) and
λjsct(θd, θs) can be solved using observed data and approximation of the value functions.23
The next subsection describes the restrictions on the approximation of value functions,
which will be the constraints in the MPEC estimation method.
The possibility of having multiple equilibria of the dynamic pricing game will not lead
to discontinuity in the λjsct(θd, θs) or the GMM objective function in this paper. The
discontinuity problem rises when the equilibrium found by solving (18) for an updated
(θd, θs) is far from the equilibrium found for the previous (θd, θs). This may cause jumps
in the solved cost shocks, thus the GMM objective function. However, in this paper, the
solution of mjsct(θd, θs|data) is unique and continuous in (θd, θs). There is a unique solution
of the markup vector because the coefficient matrix for the markup vector has full rank
due to diagonal dominance of∂sj′s′ct∂pcjsct
. This markup vector is continuous in (θd, θs) because
all other terms in the FOCs are continuous in (θd, θs). The uniqueness of mjsct(θd, θs|data)
doesn’t imply that there is a unique equilibrium for a (θd, θs), but that the prices observed
in data imply a unique vector of markups for the given (θd, θs).
5.3 Equilibrium Constraints
The approximation parameters are identified by the Bellman equations at the true struc-
tural parameters. Instead of using a nested loop to solve for θv(θd, θs), I impose the carriers’
Bellman equations as constraints in the MPEC algorithm to reduce computation time. In
the estimation, both sides of the carriers’ Bellman equations need to be evaluated for any
given (θd, θs). The right hand sides of the Bellman equations are integrations of the car-
riers’ discounted profits over (ξ, λ), which requires solving for the equilibrium prices for
any possible (ξ, λ). Since direct integration over the distributions of (ξ, λ) is not feasible, I
23When calculating the GMM objective function, I exclude observations with $0 carrier price and T-Mobile models in May 2013-July 2013. Since $0 is the lower bound of the carrier prices, they wouldbe conner solutions in the equilibrium prices. The corresponding cost shocks could be far from the actualshocks if included in the GMM objective function. T-Mobile completely dropped the two-year contract sinceMay 2013. There are no carrier discounts for those models. So the cost shocks calculated in equation(19)for these observations would have a different meaning if I include them in the GMM objective function.Therefore, I exclude the cost shocks of these observations in the GMM objective function.
28
simulate R vectors of the demand and costs shocks.24 For each simulated (ξr, λr), I solve
for the equilibrium prices pc,rjsct(ξr, λr). I design a Newton-Raphson iteration algorithm that
takes the advantage of linearity of markups in the FOCs to get the equilibrium prices.25
There is potential multi-equilibria issue when solving for the equilibrium prices for the
simulated shocks. I take the markups implied by the observed prices and a (θd, θs, θv) as
the starting point when solving for an equilibrium for each vector of shocks. In the cases
where multiple equilibria exist, my algorithm always selects the equilibrium that is closest
to the observed one.26 Let pc,rjsct be the equilibrium price of (j, s, c, t) for (ξr, λr). Then I
use the average long run profit across simulations to approximate the integration on right
hand side of the Bellman equations:
∼RHSct(θd, θs, θ
v) =1
R
R∑r=1
[∑(j,s)
(pc,rjsct − ωjpmjsct − 24κsc − λrjsct)Mtsjsct(p
c,rt , ξrt ; θd)
+ βdVc(nt+1(nt, pc,rt ), θv)]
In the estimation, I allow an approximation error between the two sides of the Bellman
equations, a percentage difference smaller than τ between the two sides of the Bellman
equation at each observed state and for each carrier. This flexibility is added due to the
finite basis functions used in the approximation. Imposing strict equality of the Bellman
equations may lead to algorithm to fail to find an approximation vector or taking too long a
time to find the approximation coefficients. Barwick and Pathak (2015) also approximate
the value functions and impose the FOCs of the distance between the two sides of the
Bellman equations with respect to approximation parameters as equilibrium constraints.
Their method also allows errors in the value function approximation.
|Vc(nt; θd, θs, θv)−∼
RHSct(θd, θs, θv)|/ |Vc(nt; θv)| < τ, ∀c, t. (20)
The constraint (20) implies that the relative difference between the two sides of each
carrier’s Bellman equation at any state nt should be smaller than the tolerance τ . The
24Due to computation time issue, I use R = 50 in the estimation. After I get the parameter estimates, Icheck the impact of the number of Monte Carlo simulation on the value functions and find that increasingR doesn’t affect the integration much. See Supplemental Materials Section C.2 for details.
25See Section C.3 of the Supplemental Materials for details on the iteration algorithm.26See Supplemental Materials Section C.3 for details on using iterations to solve for prices.
29
smaller is τ , the better the value functions are approximated. In the estimation, I set the
value of τ be 5% and impose the constraints at the observed states. At the converged
parameter estimates, the average error in Bellman equations is 3%.
6 Estimation Results
Table 3 shows the estimates of demand parameters. Model (1) shows the estimates using
only the demand model. The potential endogeneity issues are dealt with. Model (2) is the
full model, and the demand model and supply model are estimated jointly. The coefficient
estimate of the OS network effect, γ, is 0.0814 and significant in the full model. This means
that a consumer’s utility of buying a smartphone increases with the number of existing users
of the smartphone OS. The network effect is more important in the full model because the
carriers’ differentiating pricing strategies in Table 2 imply strong OS network effect. The
price coefficient estimate α is −1.5793. Comparing the parameters for OS network size and
price, I find that adding 19.41 million users for an OS increases a consumer’s utility by the
same amount as cutting the price by $100. To see the scale of the OS network effect, iOS
and Android had 55.47 and 86.69 million users at the beginning of 2013, respectively. The
interaction between price and income has a positive coefficient, meaning that high income
consumers are less price sensitive. The income effect implies that the price of smartphones
will not affect the utility of an individual who has an annual income of $201,000.
In model (1), the estimates of β imply that consumer utility increases with camera
pixels and CPU speed. But the coefficients for storage, battery, screen size, and pixels
are negative. This is probably because that the best selling models do not have the most
advanced characteristics. For example, iPhone 5’s battery is 1540mAh, while most other
top models have capacities more than 2000mAh. Similarly, the average screen size for
carrier-iOS groups is 3.66 inches, while that for carrier-Android and carrier-Windows Phone
groups are 4.24 and 3.94 inches, respectively. The estimates become insignificant in the
full model, where the important factors in determining consumers’ purchase decisions are
only price, OS network size, and OS quality.
30
Table 3: Demand Model Parameter Estimates
(1) (2) (1) (2)
Variable RDC-IV Full Fixed Effects RDC-IV Full
OS Subscribers (Million), γ 0.0107*** 0.0814*** Verizon-iOS, ψiv 1.3285 1.7664(0.0038) (0.0171) (0.9082) (5.4545)
Carrier Price ($100), −α -1.5516*** -1.5793* Verizon-Android, ψav -0.2821 -0.4445(0.6481) (0.9097) (0.8698) (5.8247)
Price*Income, −φ1 1.2705*** 1.2537 Verizon-Blackberry, ψbv -3.3741*** -2.3277(0.5117) (0.8270) (0.7780) (4.7689)
Storage (GB), β1 -0.0863*** -0.3082 Verizon-Windows, ψwv -0.1147 -0.0770(0.0161) (0.2248) (0.8756) (5.3396)
Battery (1000mAh), β2 -0.6356*** -1.2989 AT&T-iOS, ψia 1.5404 1.2312(0.4659) (3.7447) (0.9245) (5.4172)
Camera(100MP ), β3 0.2930*** -0.3792 AT&T-Android, ψaa -0.9411 -1.7506(0.0327) (0.4563) (0.8182) (5.3095)
Screen Size (inch), β4 -2.000*** -2.8462 AT&T-Blackberry, ψba -2.8566*** -2.3800(0.1921) (2.9428) (0.8211) (4.9948)
Dummy 4G, β5 0.3127 -0.1253 AT&T-Windows, ψwa -0.7067 0.5833(0.4799) (1.8099) (0.9702) (5.3578)
Pixels (100/inch2), β6 0.2885 0.4169 Sprint-iOS, ψis -0.2821 -0.8214(0.1715) (1.5726) (0.9270) (5.4625)
RAM (GB), β7 -0.0261 0.2039 Sprint-Android, ψas -0.2071 -0.7632(0.2131) (1.3457) (0.8482) (5.8705)
CPU (Ghz), β8 0.7518*** -0.5389 Sprint-Blackberry, ψbs -4.0000*** -3.1028(0.1138) (0.9647) (0.8039) (4.9485)
ηios 0.1468 3.8196*** Sprint-Windows, ψws 0.4296 0.3924(0.0951) 0.6049 (0.8663) (5.3910)
ηand 0.0000 1.4887*** T-Mobile-iOS, ψit -0.4043 0.6467(0.0581) 0.3524 (0.8421) (4.9588)
ηbla 0.0000 4.4243*** T-Mobile-Android, ψat -0.7020 -1.3600(0.0830) 0.6845 (0.8666) (5.3040)
ηwin 0.2537*** 4.5885*** T-Mobile-Blackberry, ψbt -4.000*** -3.1594(0.0676) 0.6541 (0.7988) (5.1802)
T-Mobile-Windows, ψwt -0.3009 0.0052(0.9221) (4.7559)
The number of OS version updates has positive impacts on consumer utility in model
(2). Android’s improvement in each new version is the smallest, increasing a consumer’s
utility by 1.4887, while Windows Phone’s improvement is the highest. The carrier-OS fixed
effects, ψs, measure the unobserved characteristics of these groups that are constant over
time. The results of model (1) show that Blackberry has the lowest time-invariant quality
among all OSs, and iOS has the highest quality. Though the estimates become insignificant
in the full model, the rank of the OS quality stays the same.
31
Table 4 shows the demand elasticities across eight smartphone models by Verizon and
AT&T in November 2012. The own elasticities are stronger than cross elasticities. The
own elasticities of Android models (Samsung Galaxy S3 and LG Lucid) are the highest.
Since there are a lot of Android models available, a price increase of an Android model will
make consumers to choose other Android models. Consumers have quite robust demand
for iPhone 4s(16GB), less elastic than for iPhone 5(16GB). This is due to lower price of
iPhone 4s than iPhone 5. There is high cross demand elasticities among iPhone models.
The eighth column shows that the price change of Blackberry 9900 has small impacts on
other models’ sales, similar for the Nokia 920 with Windows Phone. Overall, Android and
iOS models are closer substitutes for each other than for Blackberry and Windows Phone
models.
Table 4: Demand Elasticities w.r.t. Prices at Model Level
V-iPhone4s V-iPhone5 V-S3 V-Lucid A-iPhone4s A-iPhone5 A-B9900 A-Nokia
V-iPhone4s -1.6116 0.1866 0.0243 0.0247 0.7768 0.1842 0.0047 0.0186V-iPhone5 0.5874 -2.0203 0.0246 0.0395 0.5798 0.2029 0.0056 0.0161V-S3 0.2004 0.0645 -2.5905 0.0413 0.1978 0.0637 0.0007 0.0098V-Lucid 0.1701 0.0862 0.0345 -2.6651 0.1679 0.0851 0.0028 0.0060A-iPhone4s 0.7869 0.1866 0.0243 0.0247 -1.6118 0.1842 0.0047 0.0186A-iPhone5 0.5874 0.2055 0.0246 0.0395 0.5798 -2.0204 0.0056 0.0161A-B9900 0.3272 0.1230 0.0058 0.0283 0.3230 0.1214 -2.0048 0.0062A-Nokia 0.6854 0.1890 0.0439 0.0322 0.6766 0.1865 0.0033 -1.7542
Notes: V: Verizon. A: AT&T. The (g, g′)th element is the demand elasticity of product g when prices of productg′ increase by 1%. S3 is Samsung Galaxy S3 with Android OS. Lucid is an Android smartphone by LG. B9900 isa Blackberry model. Nokia is the Nokia 920 model with Windows Phone OS.
The estimates of the supply side parameters are in Table 5. The wholesale cost co-
efficients ω are significant. Apple’s wholesale-retail price ratio is the highest at 89.63%.
This implies that the carriers pay $581 to Apple for a $649 iPhone on average. This ex-
actly matches the $581 estimate from Apple’s balance sheet according to a report in 2013
by Digital Trends.27 Samsung’s wholesale-retail price ratio is 85.89%, implying that the
carriers pay $514 for a Samsung S3 whose manufacturer retail price is $599. Motorola’s
wholesale discount is the highest among all manufacturers, at 16.55%.
The monthly service cost estimates, κs, are at the carrier-OS level. The four carriers’
average monthly service cost estimate is $22.14. Sprint has the highest estimated service
cost, $26.73 per month per user. T-Mobile has the lowest service cost with an average of
27See the report here: http://www.digitaltrends.com/mobile/iphone-cost-what-apple-is-paying/
32
$19.60 per month. The average monthly service costs for Verizon and AT&T are $20.31
and $21.91. The results don’t show that one OS costs more than others for the carriers
to provide services. Comparing the estimated unit costs with the service price data, the
monthly markups per customer on wireless services for Verizon, AT&T, Sprint, and T-
Mobile are $44.13, $36.44, $34.59, and $32.80, respectively.
Table 5: Supply Model Estimates
Variable Estimate Variable Estimate
Wholesale Apple, ωa 0.8963*** AT&T-iOS, κai 0.2360price (0.1971) (0.2932)ratio Samsung, ωs 0.8589*** AT&T-Android, κaa 0.2671ω : (0.2819) (0.2313)
Motorola, ωm 0.8345*** AT&T-Blackberry, κab 0.1842(0.2819) (2.7595)
LG, ωl 0.8675*** AT&T-Windows, κaw 0.1891(0.3052) (2.5295)
HTC, ωh 0.8744*** Sprint-iOS, κsi 0.3047(0.2481) (0.4797)
Blackberry, ωb 0.8399*** Sprint-Android, κsa 0.2324(0.2625) (0.2477)
Nokia, ωn 0.8354*** Sprint-Blackberry, κsb 0.2335(0.2627) (2.7546)
Monthly Verizon-iOS, κvi 0.2244 Sprint-Windows, κsw 0.2987service (0.0207) (5.2813)cost (100$) Verizon-Android, κvi 0.1885 T-Mobile-iOS, κti 0.2244κ : (0.0538) (0.0000)
Verizon-Blackberry, κvb 0.1936 T-Mobile-Android, κta 0.1680(0.2898) (0.4144)
Verizon-Windows, κvw 0.2058 T-Mobiel-Blackberry, κtb 0.1711(0.1253) (2.2132)
T-Mobiel-Windows, κtw 0.2206(0.5362)
Given the estimates, I calculate the carriers’ markups per two-year contract customer.
Take AT&T and iPhone 5 in December 2012 for example. AT&T sells the iPhone 5 at
$199 while paying $581 to the manufacturers, which implies a $382 net cost on the phone.
AT&T earns a net margin of $36.44 each month on wireless service, which makes a net
profit of $874.56 on the two-year service. So AT&T earns a net profit of $492.56 from an
iPhone 5 two-year contract customer. Table 6 shows the carriers’ average estimated profits
per two-year contract customer by carrier-OS groups.
33
Table 6: Carriers’ Markups per Two-Year Contract by Carrier-OS ($100)
Verizon AT&T Sprint T-Mobile
iOS 5.95 5.01 3.18 -Android 6.99 5.13 5.93 5.24Blackberry 7.95 7.38 6.59 5.30Windows Phone 7.31 7.33 4.78 4.26
The carriers get lower markups on iOS and Android models than on Blackberry and
Windows Phone models, which is consistent with the results in the two-period theoretical
model in Section 2. Their markups on iOS models are the lowest since they get the small
wholesale discounts from Apple and offer high discounts to consumers. This finding is
in line with the news about the carrier margin drops in 2011 because of iPhones.28 The
carriers’ markups on Blackberry and Windows Phone models are higher than on iOS and
Android models. This is because that the carriers give lower discounts on Blackberry and
Windows Phone models and that they pay lower wholesale prices to the manufacturers.
Among the carriers, Verizon has the highest overall markups due to its high margin on the
wireless service. AT&T has the second highest average markups. T-Mobile’s markups are
the lowest due to their low margins on wireless service.
The value function approximation results show that Verizon’s value function is the
highest among the carriers. AT&T has the second highest value function. T-Mobile’s
value function is the lowest. See the Supplemental Materials for plots of the carriers’ value
functions.29
7 Counterfactuals
In this section, I study two counterfactual cases to measure the impacts of the carriers’ abil-
ity to internalize across operating systems and the carriers’ two-year contract discounts on
smartphone penetration, OS market concentration, carriers’ profits, and consumer surplus.
7.1 Carriers Specialize in Operating Systems
As shown in Section 2, multi-OS carriers’ ability to internalize prices across OSs leads to
price differentiation across OSs. In this counterfactual analysis, I assume the four carriers
28Data source: http://money.cnn.com/2012/02/08/technology/iphone carrier subsidy/ .29The value functions are plotted in Supplemental Material D.2.
34
specialize in the four OSs to measure the impact of internalization of OS competition. I
assume that Verizon, AT&T, Sprint, and T-Mobile specialize in Android, iOS, Blackberry,
and Windows Phone, respectively.
To keep consumers’ choice sets the same as in data, I keep all the Android smartphones
that were sold by AT&T, Sprint, and T-Mobile and assume that they are now only available
at Verizon, same for the other OSs. In addition, I still use the estimated carrier-OS
fixed effects from original carriers and estimated demand shocks from data, so that only
price and OS network size in a consumer’s utility from a smartphone would change in the
counterfactual case. On the supply side, I also use the cost shocks backed out from data.
This scenario is designed in this way so that only the supply side OS ownership structure
changes from multi-OS carriers to single-OS carriers.
The four carriers still play a dynamic pricing game after they specialize. I first solve
for the value function approximation parameters if they specialize, by minimizing the
differences between the two sides of Bellman equations. I then calculate the counterfactual
equilibrium prices by iterating guesses of prices (markups) using new value functions. There
could be multiple equilibria when solving for prices. The counterfactual equilibrium shown
below is the one that is closest to the equilibrium in data, since I use the vector of observed
prices as the starting point in the iterative algorithm.
Table 7 shows the changes in smartphone prices and the carriers’ profits if they spe-
cialized in OSs. The average two-year contract prices of Android and iOS smartphones
would increase by $286 and $26, respectively, due to their OS network size advantage and
OS specialization. The average prices of Blackberry and Windows Phone models would
drop $131 and $72. This is consistent with the results in Section 2. If the carriers become
single-OS sellers, the carriers on larger networks will choose higher prices than carriers
on small networks. Comparing the second row and the last row, I find that the profits
of the carriers who specialize in Android (Verizon) and iOS (AT&T) would increase by
48.31% ($14.68 billion) and 74.45% ($15.28 billion), while Spring (Blackberry) would and
T-Mobile (Windows Phone) would lose profits by more than 60%. This is because that
most consumers would still buy either Android models or iPhones, and both would have
higher prices. The third row shows the profits by OS before specialization. Carriers get
most of their profits from Android and iOS models in the data.
35
Table 7: Price ($100) and Profit ($billion) Comparison
Verizon AT&T Sprint T-Mobile
(And) (iOS) (Bla) (Win)
∆Price by OS +2.86 +0.26 −1.31 −.72Profits by Carrier (Multi-OS) 30.40 20.52 10.99 7.91Profits by OS (Multi-OS) 26.46 38.54 2.11 2.07Profits by OS (Single-OS) 45.87 35.80 4.07 3.03
Figure 2: OS Growth if the Carriers Specialize in OSs
Figure 2 show the OS market shares over time. The dashed curves show the counter-
factual OS shares, and the solid curves are the OS shares in the data. The two curves in
the same color represent the same OS. The OS market would become less concentrated,
and the smartphone penetration rate would drop from 78.36% in the data to 62.53% if
the carriers specialized. The market share of Android would decrease from 41% to 26%,
while iOS would drop from 31% to 29%. Android’s market share would be below iOS
from January 2013 on, due to its increased prices and the growing number of iOS users.
However, Verizon still has the highest profits among all carriers, because of the large price
increases of Android models as in Table 7. The market share of Blackberry and Windows
Phone would increase slightly due to lower prices. Their joint share would increase from
36
7% to 9%.
If the carriers specialized in OS, consumers’ surplus would decrease by $137.40 million
during the sample period.30 Consumers would get higher utility from Blackberry and
Windows Phone models because of lower prices and larger OS networks, but their utility
from Android and iOS models would decrease. Since most consumers are Android and iOS
users in the data, the aggregate consumers surplus would drop.
7.2 The Impact of the Two-Year Contract Discounts
In this counterfactual case, I assume that the carriers sell smartphones at the manufacturer
retail prices and cut the service prices by $15 each month, in order to measure the impacts
of the two-year contract discounts. This is motivated by the fact that the carriers started to
sell smartphones at the manufacturer prices and cut monthly service prices by at least $15
for non two-year contract subscribers from late 2013. By January 2016, all the four leading
carriers stopped the two-year contract option for subscribers.31 To make this counterfactual
results comparable with data, I assume that each consumer uses a smartphone for two years.
By using the manufacturer retail prices, I eliminate the carriers’ discounts on smart-
phones and their price differentiation across OSs. Without the differentiated discounts,
iOS and Android models become relatively more expensive than Blackberry and Win-
dows Phone. Table 8 compares the carrier profits with and without the carrier discounts.
AT&T could get 18.25%($3.51 billion) more profits than in the data if it didn’t offer high
discounts on iPhones, because 63% of its new service subscribers during the sample period
bought iPhones on which AT&T had low markups, while the iPhone sales shares for Ver-
izon, Sprint, and T-Mobile were 47.33%, 19.56%, and 3.24%. Verizon’s would lose profits
by 8.69% ($2.97 billion), Sprint by 44.32%($4.91 billion), and T-Mobile by 40.18% ($2.92
billion).
30I calculate the consumer surplus following the definition in Chapter 3 of Train (2009) and use thepotential population of smartphone users as the market size in each period. If I use the market sizedefinition in Section 3.2.2, then the consumer surplus would increase if carrier specialized due to largermarket sizes from lower OS shares, though an individual consumer’s surplus would decrease.
31Sprint brought the two-year contract option back in March 2016.
37
Table 8: Profit Comparison by Carrier ($billion)
Verizon AT&T Sprint T-Mobile
Profits by Carrier (Estimated) 30.40 20.52 10.99 7.91Profits by Carrier (No Contract) 27.43 24.03 6.08 4.99
Figure 3 compares the OS growth paths in this counterfactual case with data. The
dashed curves show the counterfactual OS shares, and the solid curves are the OS shares
in the data. The two curves in the same color represent shares of the same OS. Without
the discounts, the overall smartphone penetration rate by the end of May 2013 would be
58.31% (102.33 million), compared with 78.36% (137.51 million) in data. Because less
consumers would be willing to buy iOS and Android models, which have a lot of users in
the data.
Figure 3: OS Growth without two-year Contract
The OS concentration would decrease without the carrier discounts because the larger
OSs no longer have high carrier discounts. Blackberry and Windows Phone would share
10.08% of the market, more than the 6.39% in the data. The lead of Android to Windows
Phone would decrease to 14.30%, compared with 28.57% in the data. iOS and Android
would still dominate the market for several reasons. First, they still have the initial OS
38
network advantages, which would result in higher demand in all periods. Second, iOS has
high fixed effects from the demand estimates and Android has many models in the market,
so consumers’ demand for the two OSs would still be stronger.
If the carriers didn’t offer the two-year contracts, consumers’ surplus would decrease
by $855.37 million during the sample period. Consumers would get higher utility from
Blackberry and Windows Phone models, because the service fee deduction would be more
than the carriers’ contract discounts on smartphones and OS network sizes would increase.
Their utility from Android and iOS models would decrease, because the service fee deduc-
tion would be less than the carriers’ discounts on smartphones and their OS network sizes
would be smaller. Again, since most consumers are Android and iOS users in the data,
consumers surplus would drop without the two-year contract discounts.
8 Conclusion
The literature on network effects focused on pricing decisions of single-network firms, but
not multi-network sellers. In this paper, I analyze the impact of a network effect on a
multi-network seller’s dynamic prices in a two-period, two-OS theoretical model. I find
that, multi-network sellers choose lower prices for the products with larger networks in
early periods, while single-network sellers choose higher prices for products with larger
networks, . This is due to the difference in the two types of sellers’ ability to internalize the
competition effect across networks. A multi-network seller’s profit increases with network
concentration, so they use differentiated prices across networks to achieve concentration.
The multi-network seller’s pricing strategy is present in the smartphone industry, where
the smartphone operating system network effect exists and telecom carriers act like multi-
network sellers. To measure the impact of the network effect and the carriers’ pricing
strategy, I set up a structural model of consumers’ demand and carriers’ dynamic pricing
game for smartphones. I use smartphone model level data from 2011 to 2013 to estimate
the structural model. The results show that the OS network sizes affect consumers’ utility,
and thus carriers should make dynamic pricing strategies.
The dynamic oligopolistic game in this paper features continuous choice variables, con-
tinuous state variables, multi-product firms, and asymmetric firms. The existing estima-
tion algorithms for dynamic discrete choice games and dynamic continuous choice games
among single-product firms can’t be used in this paper. I solve the dynamic pricing game
by approximating the firms’ value functions with linear combinations of basis functions. I
39
develop an iterative procedure to efficiently solve for the equilibrium prices. As a result,
the oligopolistic multiple-product firms’ asymmetric pricing game can be solved efficiently
in the estimation.
With the estimates, I study two counterfactual cases, eliminating carriers’ ability to in-
ternalize competition across OSs and the two-year contracts, respectively. I find that both
the carriers’ ability to internalize OS competition and the two-year contract discounts sig-
nificantly accelerated the smartphone industry’s growth and the concentration of operating
systems and increased consumer surplus.
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Appendix
A The Inversion of Carrier-OS Shares to Carrier-OS Unob-served Quality
In this section, I prove that the observed vector carrier-OS sales market shares sscts uniquelydetermine a vector of the carrier-OS unobserved quality ξsct when the utility function isat smartphone model level. The proof is based on that in Berry (1994). For notationsimplicity, I use a logit model version of the demand model with carrier-OS unobservedquality.
Consider the following consumer utility function:
uijsct = δjsct + ξsct + εijsct,
where δjsct is the mean observed utility and ξsct is carrier-OS specific unobserved quality.The utility of the outside option is assumed to be ui0t = εi0t. Given the assumption thatεijscts follow Type-I extreme value distribution and are i.i.d. across consumers, models,and periods, the market share of carrier-OS group (c, s) in period t is:
ssct = Ssct(ξt) =∑j∈Ωsct
e(δjsct+ξsct)
1 +∑
(j′,s′,c′)∈Ωte(δj′s′c′t+ξs′c′t)
. (A.1)
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I need to prove that there is a unique ξt = S −1(sdatat ) ∈ RG for any fixed finite δvector, where sdatat is the observed vector of carrier-OS market shares in period t givenother unobserved shocks ξ−sct. G is the number of carrier-OS groups. The equation (A.1)has the following properties. (1), ∂Ssct/∂ξsct > 0; (2) ∂Ssct/∂ξs′c′t < 0, if (s, c) 6= (s′, c′);and (3) Ssct approaches to zero as ξsct goes to −∞ and it approaches to 1 as ξsct goes to∞.
Define the element-by-element inverse, rsc(ξt, sdatasct ), as the unobserved quality value
for group (s, c, t) such that the model predicted carrier-OS share Ssct equals the observedshare sdatasct . That is:
sdatasct = Ssct(rsc((ξt, sdatasct )), ξ−sct; δt). (A.2)
Since the market share function S is continuously differentiable and satisfy the threeproperties above, the function rsc(ξt, s
datasct ) is well defined and differentiable. In particular,
rsc is strictly increasing in ξs′c′t for any (s′, c′) 6= (s, c) and doesn’t depend on ξsct. So avector ξt solves equations in (A.1) if and only if it is a fixed point of the element-by-elementinverse: ξt = r(ξt, d
data). Next, I first show the existence of a fixed point of r(ξt, ddata),
then show the uniqueness of the fixed point.First, r(ξt, d
data) has a lower bound ξ. The lower bound for the (s, c)th element is the
value of rsc(ξ′t, d
data), with ξ′s′c′t = −∞, for all (s′, c′) 6= (s, c). Define ξ as the smallestvalue across the products of these lower bounds. Note that there is no upper bound forrsc, but a slight variant of the element-by-element inverse has.
Lemma 1. There is a value ξ, with the property that if one element of ξt, say ξsct is greaterthan ξ, then there is another carrier-OS pair (s′, c′) such that rs′c′t(ξt, s
datat ) < ξs′c′t.
Proof. To construct ξ, set ξs′c′t = −∞, for all (s′, c′) 6= (s, c). Then define ξsct as thevalue of ξsct that set the outside option market share S0t(ξsct, ξ−sct) = sdata01 . Define ξas any value greater than the maximum of the ξsct. Then, if for the vector ξt, there isan element (s, c) such that ξsct > ξsct, then S0t(ξsct, ξ−sct) < sdata01 , which implies that∑
s′c′ Ss′c′t(ξt; δt) >∑
s′c′ sdatas′c′t, so there is at least one carrier-OS pair (s′, c′) such that
Ss′c′t(ξt; δt) > sdatas′c′t. Then for this pair (s′, c′), rs′c′t(ξt, sdatat ) < ξs′c′t.
Now define a new function which is a truncated version of rsc: rsc(ξt, sdatat ) =
minrsc(ξt, sdatat ), ξ. Then r is a continuous function which maps [ξ, ξ]G into itself. Thenby Brouwer’s fixed-point theorem, r is has a fixed point ξ∗. By the definition of ξ and ξ,
ξ∗ can’t have a value at the upper bound, so ξ∗ is in the interior of [ξ, ξ]G. This implies
that ξ∗ is also a fixed point of the function r(ξt, sdatat ). So there exists a fixed point for the
element-by-element inverse function.Next I show the uniqueness of the fixed point. One sufficient condition for unique-
ness is the diagonal dominance of the Jacobian matrix of the inverse functions. That is:∑(s′,c′)6=(s,c) |∂rsc/∂ξs′c′t| < |∂rsc/∂ξsct|. By the implicit function theorem on equation
(A.2), we have:∂rsc/∂ξs′c′t = −[∂Ssct/∂ξs′c′t]/[∂Ssct/∂ξsct],
44
which implies that ∂rsc/∂ξsct = 1. Then the sum is:∑(s′,c′)6=(s,c)
|∂rsc/∂ξs′c′t| =1
|∂Ssct/∂ξsct|∑
(s′,c′)6=(s,c)
|∂Ssct/∂ξs′c′t|. (A.3)
Note that increasing all the unobserved quality levels (including the outside option ξ0t)by the same amount wouldn’t change any market share. That is:
K∑s′c′=0
∂Ssct/∂ξs′c′t = 0
Then it implies that:
∂Ssct/∂ξsct = −[∂Ssct/∂ξ0t +K∑
s′c′ 6=(sc)
∂Ssct/∂ξs′c′t].
Since all terms on the right hand side are strictly negative, so
|∂Ssct/∂ξsct| > |K∑
s′c′ 6=(sc)
∂Ssct/∂ξs′c′t|.
Then the sum in equation (A.3) is:∑(s′,c′)6=(s,c)
|∂rsc/∂ξs′c′t| < 1 = |∂rsc/∂ξsct|.
Hence the sufficient condition for uniqueness is satisfied. Therefore, the element-by-element inverse function has unique fixed point ξ∗, which is the solution of the marketshare inversion function.
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