environmental regulation through trade: the case of shrimp
TRANSCRIPT
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Environmental regulation through trade: the case of shrimp
Darren Hudsona,*, Diane Hiteb, Abdul Jaffara, Fatimah Karia
aDepartment of Agricultural Economics, Mississippi State University, Mississippi State, MS 39762, USAbDepartment of Agricultural Economics, Auburn University, USA
Received 30 October 2002; revised 2 January 2003; accepted 19 February 2003
Abstract
The implications of a potential ban on shrimp imports by the US from countries that do not utilize the Turtle Excluder Device on
commercial shrimp nets is explored in this paper. A Linear Expenditure System (LES) was used to determine the own-price elasticities of
demand for shrimp imports. The system of estimated equations was then solved for quantity levels under assumptions made about the trade
restrictions, resulting in a set of prices for those import levels. These estimated prices were then used to estimate the compensating variation
impact of the trade restrictions. Findings suggest that the environmental regulation would have a negative impact on US consumers, but the
magnitude of that effect depends on assumptions made regarding the distribution of US imports after the trade restriction is imposed.
q 2003 Elsevier Science Ltd. All rights reserved.
Keywords: Shrimp; Linear expenditure system; Compensating variation; Import restrictions; Environmental regulation
1. Introduction
Trade and the environment are inexorably linked. Recent
discussion on a broad range of issues has clearly shown that
trade has both environmental benefits and costs (Copeland
and Taylor, 1995, 765–771). These developments in the
literature have improved our understanding of the linkages
between trade and the environment and allowed the design
of better models that incorporate these linkages. Despite
these advances in the literature, there has been only minor
treatment of the consequences of environmental regulation
implemented through trade. Most available literature
focuses on the trade impacts of environmental regulations
(Valluru and Peterson, 1997, 261–272; Bohman and
Lindsay, 1997, 17–38; Marchant and Ballenger, 1994,
108–128; Seale and Fairchild, 1994, 97–107).1 One
example of potential environmental regulation implemented
through a trade restriction lies in the shrimp industry.
Commercial shrimp trawling often creates by-catch
problems, especially with sea turtles in warm waters. A
recent development called the Turtle Excluder Device
(TED) has shown some promise in reducing turtle by-catch
when attached to shrimp nets. The US has sought wide-
spread adoption of the TED system on commercial
shrimping fleets worldwide. However, some countries
dispute the efficacy of the TED system and have refused
its adoption (Holloway, 1998, 3; Stewart, 1998, 197–219).
To promote adoption, the US placed an import ban on
shrimp originating in countries that do not have the TED
system on their commercial fleets.2 However, the World
Trade Organization (WTO) found that this action was in
violation of the General Agreement on Tariffs and Trade
(GATT).3 Undaunted, the US placed a de facto ban on
shrimp imports from non-complying countries through
Food and Drug Administration (FDA) safety and inspection
regulations on December 18, 1998.4 While there are other
0301-4797/03/$ - see front matter q 2003 Elsevier Science Ltd. All rights reserved.
doi:10.1016/S0301-4797(03)00061-6
Journal of Environmental Management 68 (2003) 231–238
www.elsevier.com/locate/jenvman
* Corresponding author. Tel.: þ1-662-325-7998; fax: þ1-662-325-6614.
E-mail address: [email protected] (D. Hudson).1 The reader is referred to The Greening of World Trade Issues edited by
Anderson and Blackhurst, which lays out in detail the linkages between
trade and the environment.
2 This, of course is a simplification of the issue. For a good discussion on
the history and issues underlying the TED debate and the shrimp import
ban, see Stewart (1998, 197–219).3 The precedent for this ruling had already been set. The US placed a ban
on imports of tuna not caught in a ‘dolphin safe’ manner. The WTO ruled
against the US in this case. This ultimately led to a labeling of tuna as
‘dolphin safe’ for those supplies caught with different, larger sized nets.
Other countries adopted these nets in order to insure their tuna could be
labeled ‘dolphin safe’.4 The original import ban was aimed only at wild caught shrimp.
However, the Earth Island Institute sued the US government, and now the
ban is applied to all shrimp imports from countries not in compliance with
the TEDs. Thus, all imports, whether aquaculture or wild caught, are
affected by the ban.
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motivations for safety restrictions such as disease outbreaks
in shrimp supplies, it has facilitated the implementation of
an environmental policy through a trade restriction.
There are many economic and social issues surrounding
such a ban. For example, is it equitable for the US to utilize
unilateral trade restrictions in an attempt to force other
countries to follow what the US deems an appropriate
environmental policy? Is this consistent with the free trade
principles of the WTO? What are the costs of such a policy?
Are there alternative methods of achieving the environ-
mental goal of reducing sea turtle by-catch?
The legal ramifications and equity issues associated with
the trade ban are beyond the scope of this study. However,
some knowledge of the potential welfare impacts of the ban
would be useful in the debate. No previous study has
addressed the impacts of the shrimp import ban. Artificial
trade distortions lead to expectations of decreased welfare
for US consumers. However, in a system of multiple price
changes, analytical expectations become complex and can
be misleading. Thus, it becomes necessary to expand the
analytical framework in order to quantify the effects of these
policies. The objective of this paper is to analyze the import
demand for shrimp in the US and assess the implications of
a ban on specific shrimp imports. This should provide an
estimate of the opportunity cost to US consumers of
achieving the environmental goal.
2. Shrimp imports
Shrimp imports into the US have become increasingly
prevalent, growing from 40% of domestic consumption in
1980 to 67% by 1996. Table 1 shows that the distribution of
imports has changed substantially as well.
In general, imports have shifted away from Central and
South American countries to Association of Southeast Asian
Nations (ASEAN) or Asian countries. The exception to this
has been Equador, which has exhibited an increasing market
share. The increase in ASEAN market share has come in the
face of increasing ASEAN prices (Table 2).
ASEAN prices increased by 188% during the study
period while the rate of increase for other countries ranges
from just 13–76%. Furthermore, in 1996, the ASEAN price
is 33% higher than the next highest price. This phenomenon
may indicate a relative preference for Asian shrimp or that
Asian shrimp is of superior quality. However, no data are
available to directly support this hypothesis.
A second element not captured in the data is the
increasing prevalence of aquaculture or farm-raised shrimp.
Some countries such as Thailand have increased aqua-
culture production and now harvest virtually no wild caught
shrimp. However, the data on aquaculture shrimp are
inconsistent. Data on imports are not differentiated by
aquaculture or wild caught. However, because the ban is
currently applied to all shrimp imports from specific
countries, this distinction is not germane.4
3. Related literature
Previous economic studies on shrimp have typically
focused on price determination and domestic marketing
issues. One of the earliest studies by Doll (1972, 431–440)
examined the ex-vessel shrimp price movements between
1950 and 1968. Adams et al. (1987, 103–112) analyzed the
price relationships between market levels for different sizes
of shrimp incorporating the dynamic nature of price
transmission between market levels. Hopkins (1980) also
Table 1
Market share for shrimp imported into the US, 1980–1996
Year Total imports ($000) NAFTA (%) Brazil and Argentina (%) ASEAN (%) EU (%) Equador (%) India (%) China (%) ROW (%)
1980 719,263 44.81 2.83 4.19 0.76 9.47 2.91 1.36 33.69
1981 723,875 40.71 3.30 2.35 0.75 11.09 4.52 2.44 34.83
1982 980,233 38.92 4.37 2.32 0.18 13.93 5.05 1.17 34.06
1983 1,233,522 32.58 4.55 5.16 0.61 17.88 4.35 0.49 34.38
1984 1,216,350 31.34 6.69 6.50 0.74 15.25 3.38 1.02 35.07
1985 1,152,912 26.75 7.10 8.76 1.59 14.41 3.70 1.85 35.84
1986 1,434,337 23.89 4.76 7.90 1.16 19.37 3.26 4.36 35.29
1987 1,710,224 24.33 3.03 7.88 0.85 22.13 6.95 3.33 31.49
1988 1,754,690 18.51 3.45 10.28 0.46 21.78 17.10 3.14 25.28
1989 1,705,192 17.26 2.93 20.19 0.28 18.10 3.03 16.23 21.98
1990 1,658,691 11.31 1.31 25.07 0.16 17.55 3.41 21.41 19.78
1991 1,856,667 10.53 1.27 34.69 0.07 19.51 3.63 11.83 18.46
1992 2,017,433 7.84 1.97 35.86 0.16 18.77 3.00 15.75 16.66
1993 2,169,581 10.28 1.76 40.06 0.04 17.09 3.80 8.47 18.50
1994 2,667,755 10.25 1.31 42.86 0.15 17.06 5.33 3.94 19.11
1995 2,580,891 14.30 0.62 42.05 0.22 17.18 4.26 3.08 18.29
1996 2,457,500 14.42 0.27 42.78 0.15 15.05 4.83 1.44 21.07
Average share 22.24 3.03 19.94 0.49 16.80 3.82 6.99 26.69
Source: Current Fisheries Statistics, various issues (US Department of Commerce).
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focused attention on domestic issues of the shrimp industry
without much elaboration on shrimp imports. No previous
study, however, has derived system wide shrimp import
demand elasticities, which are necessary to assess the
impacts of trade restrictions.5 The systems approach is
advantageous in the context of the current study because it
allows differentiation of imports by source, which in turn
allows the analysis of trade restrictions on specific import
sources. Furthermore, the system can capture complex
price/quantity interactions in the shrimp import market that
are lost in a single equation framework.
A wide variety of demand system models have been
applied in the literature. A number of studies have utilized
the Linear Expenditure System (LES) or versions of LES
(Richards et al., 1997, 825–837; Green et al., 1979, 41–52;
McIntosh, 1974, 45–51; Goddard, 1983, 291–318; Deaton
and Muellbauer, 1980). The LES model is parsimonious in
its estimation requirements and is ideal for situations where
data is limited. It is, however, a relatively restrictive model
structure. Weatherspoon and Seale (1995, 536– 543)
estimated a system-wide beef import demand model for
Japan. In their analysis, they suggested the use of a nested
test of the Rotterdam and Central Bureau of Statistics (CBS)
model to test for proper functional form. They concluded
that the CBS model best fit the data for their analysis.
Despite being more flexible, however, these models require
more data for accurate estimation.
Huang (1993, 217–227) analyzed meat trade effects on
US consumers through a demand systems approach. In
particular, he estimated an inverse demand system to predict
price changes as a result of quantity changes coming from
trade. Huang (1993, 217–227) also estimated an ordinary
demand system to derive own- and cross-price elasticities of
demand. Combining the results of both models, he was able
to derive estimates of Hicksian compensating variation
(CV) for different scenarios of quantity effects as a result of
meat trade.
The appealing feature of the Huang (1993, 217–227)
approach is that it explicitly accounts for price changes as a
result of trade changes. However, it does so in an indirect
fashion. That is, Huang’s (1993, 217–223) method requires
the estimation of two separate models, which requires two
sets of assumptions and are subject to two sets of random
error. A more direct approach requiring estimation of one
system of equations would be desirable to estimate the
welfare effects of quantity changes.
4. Methods
The traditional method of estimating trade models
centers on the assumption, attributed to Armington (1969,
159–178), that product importation is differentiated by
region of origin. Armington (1969, 159–178) developed an
empirical framework in which to estimate import/export
demand functions. However, some researchers have deemed
the Armington (1969, 159–178) framework too restrictive
and have opted for more flexible estimation methods (Yang
and Koo, 1994, 396–408). While achieving some degree of
flexibility, analyses that utilize more flexible estimation
methods maintain the underlying assumption that product
imports–exports are differentiated by region of origin. For
purposes of this analysis, the assumption that shrimp
imports are differentiated by region of origin is maintained.
Table 2
Trade weighted shrimp import prices from various regions, 1980–1996
Year NAFTAa Brazil and Argentinaa ASEANa EUa Equadora Indiaa Chinaa ROWa
1980 4.99 2.81 2.28 2.91 4.09 1.95 2.18 3.91
1981 4.88 2.62 2.67 3.53 3.94 2.09 4.30 3.82
1982 5.52 3.79 2.76 3.16 4.59 2.23 5.01 4.06
1983 5.43 3.74 3.22 3.34 5.17 2.15 3.92 4.10
1984 5.47 3.82 3.65 3.25 4.83 2.15 4.65 4.00
1985 5.21 3.36 3.32 4.22 4.59 2.16 3.73 3.55
1986 5.33 4.02 3.37 3.93 5.44 2.32 3.67 4.14
1987 5.43 3.72 3.65 4.33 4.54 3.40 2.44 4.43
1988 5.72 3.60 4.63 4.35 4.46 3.49 2.08 4.32
1989 5.54 3.22 4.53 3.92 4.62 2.19 3.26 4.02
1990 5.43 2.99 5.07 4.19 4.19 2.19 3.40 3.69
1991 5.38 3.47 5.02 3.84 4.08 2.12 3.44 3.87
1992 5.30 3.68 5.08 3.36 3.81 1.88 3.54 3.94
1993 5.17 3.85 5.47 3.65 4.15 2.37 3.27 3.91
1994 5.45 4.04 6.40 3.75 5.21 3.47 2.53 4.68
1995 5.02 4.49 6.78 5.06 4.72 3.41 2.99 4.68
1996 4.91 3.97 6.57 3.28 4.62 3.45 2.52 4.45
Source: Current Fisheries Statistics, various issues. (US Department of Commerce, 1985–1998).a 1984 constant dollars per pound.
5 The systems approach refers to the use of a complete demand system for
shrimp imports. The complete demand system has the advantage of
accounting for all of the interactions between shrimp imports from different
regions. It does not, however, allow for explicit treatment of supply effects.
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Given the wide variance in observed regional prices, this is
probably a reasonable assumption, but the assumption is
tested empirically.
Differentiation of shrimp imports by region of origin
suggests that a system of equations estimation method
should be employed. There is a wide variety of demand
system models available for use in analysis, each with its
relative strengths and weaknesses. The preference in the
literature is for the use of flexible functional form models
such as the AIDS. Computational difficulties associated
with maximum likelihood estimation of the non-linear
AIDS model has led to the widespread use of the Linear
Approximation to the AIDS model (or LA/AIDS). How-
ever, as Buse (1994, 781–793) points out, the potential bias
in the LA/AIDS model and the widespread availability of
solution algorithms has led researchers to prefer the AIDS
model over its linear counterpart.
Flexible functional form models are thought to be
superior because they do not impose restrictions on the
underlying utility function, and can be used to test the
assumptions of homotheticity and homogeneity. However,
they can be quite data intensive, requiring more degrees of
freedom than more restrictive models such as the LES. The
LES is the most parsimonious of commonly used demand
system models, requiring the least number of observations
to obtain an estimate. This can be advantageous when data
are scarce. However, the LES has limitations as well,
primarily stemming from the simplicity of the Stone–Geary
utility function from which it is derived. The primary
limitation is that the LES cross-price elasticities are
negative by construction, which allows consideration of
Marshallian gross complements only and limiting compari-
son to Hicksian substitutes. Thus, the LES is typically used
to describe broad product groupings. That is, the LES is
used to describe groupings that account for a large portion of
total expenditures so that each grouping is seen as
competing with the other groups for a portion of total
expenditure in Hicksian terms.
4.1. Empirical model
The LES model was chosen for this analysis. This choice
was made for three primary reasons. First, to reduce the
probability of crossing multiple unknown structural changes
in the market, the time period was restricted to that found in
Table 1 (1980–1996). The relatively small number of
observations resulting from this restriction necessitated a
model form that was parsimonious. Second, calculation of
elasticities from the LES model is straightforward limiting
ambiguity about their calculation and interpretation. Third,
the Stone–Geary utility function on which the LES is based
is easily solved to obtain a unique, closed-form measure of
CV for use in welfare analysis. The linear nature of the
model also lends itself more readily to analytical solutions
to the system of equations for simulation purposes. On
the downside, however, the LES is quite restrictive because
it is only relevant for Hicksian substitutes. The fact that only
Hicksian substitute products are considered was not deemed
to be a problem as all imports are competing for market
share.
To conserve degrees of freedom for estimation, the
regions were further aggregated from the data in Table 1.
The NAFTA countries, Brazil, Argentina, and Equador
were combined into a group called WEST. The countries of
the ASEAN group were kept in an individual region and
India was kept in an individual region because these two
areas are the primary focus of the US ban on shrimp imports.
All other countries were combined into the Rest of the
World (ROW). This led to four regions for estimation,
greatly reducing the number of parameters to be estimated.
The Stone–Geary Utility function is given as
U ¼X
i
bi logðqi 2 giÞ; ð1Þ
with 0 , bi , 1;P
bi ¼ 1; and qi . gi: The bi are
interpreted as the marginal budget shares, qi are the total
quantities of i; and gi are the subsistence or minimum
typical quantities. Maximizing utility subject to a budget
constraint yields the LES system of equations. To maintain
consistency with demand theory, the gis were restricted to
be the same across equations
piqi ¼ pigi þ bi x 2X
jpjgj
� �i ¼ j ¼ 1;…; 4; ð2Þ
where pi and pj are the prices of goods i and j; and x total
expenditure. The standard interpretation of pigi is that it
represents the minimum expenditure required to attain a
subsistence level of consumption. In the current context,
pigi can be viewed as the minimum typical expenditures for
shrimp imports from a particular region. Thus,P
pjgj is the
sum of all minimum expenditures on imports. The term
(x 2P
pjgj) is the portion of total expenditure available
after the minimum expenditure for each product has been
accounted for, which is allocated to group i by the marginal
expenditure share bi:
Eq. (2) can be rewritten in quantity dependent form as
qi ¼ gi þbix
pi
1 2
Xjgjpj
x
0@
1A i ¼ j ¼ 1;…; 4: ð3Þ
The demand system represented by Eq. (3) was estimated
using Full Information Maximum Likelihood (FIML)
estimation. A Monte Carlo analysis was then used to
examine parameter consistency given the small sample size.
Using the variance–covariance matrix of the parameter
estimates as well as the variance–covariance matrix of the
residuals, 100 random iterations at each observation were
performed, generating an additional 1800 observations.
These observations were then used to re-estimate Eq. (3)
using FIML. The resulting parameter estimates were
compared to the original parameter estimates to check for
consistency.
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The income elasticity of demand is given by the
following equation
eix ¼bi
wi
; ð4Þ
where wi is the expenditure share for region i: By definition,
eix is always positive in the Stone–Geary utility function,
which precludes the possibility of an inferior good. The
own-price elasticity of demand is given by
eii ¼ 21 þ ð1 2 biÞgi
piqi
; ð5Þ
and the cross-price elasticity of demand is given by
eij ¼ 2bi
pjgj
piqi
i – j: ð6Þ
One question is whether the imports from different
regions are truly perceived differently in the market. This
issue was examined by performing a likelihood ratio test for
the equality of the own-price elasticity of demand for
different regions. If the own-price elasticities were different,
it was concluded that each region was treated separately.
4.2. Policy simulation
The second step in the analysis was to estimate the
anticipated impacts of the trade ban on shrimp. This was
accomplished by utilizing the resulting parameter estimates
from above. First, assumptions had to be made about the
quantity impact of the trade restrictions. There are no a
priori expectations about the quantities that will be affected
by the trade ban. ASEAN countries and India are likely to be
the most affected because they are not currently in TED
compliance and have a larger individual market share in the
US import market.6 For simulation purposes, it was assumed
that a 30% reduction in imports for ASEAN countries and
India would result from the ban.
Two scenarios were analyzed. First, it was assumed that
the reduction in imports from ASEAN and India were
reallocated to the WEST and ROW regions on the basis of
the percentage of imports these countries contribute.
Underlying this allocation is the assumption that the natural
fisheries and aquacultural industries in these regions could
sustain the increase in demand from the US. The second
scenario assumed that there was no reallocation of imports
to other regions. That is, the US simply reduced the quantity
of shrimp imports by the amount decreased as a result of
the trade ban. All quantities and quantity changes were
taken from the historical mean levels.
Interestingly, these two scenarios provide an illustration
of the impacts of substitutes on the welfare impacts of
policy changes. That is, the first scenario is one in which the
US has the ability to substitute other imports for the lost
imports as a result of the ban. The second scenario has no
provision for substitutes. Thus, a comparison of both
simulations reveals the impact of the ability to substitute.
The expectation is that the ability to substitute will offset
welfare losses, resulting in a lower net welfare loss when
substitution is allowed.
Using the assumed quantities, the system of equations
resulting from Eq. (3) was solved simultaneously using
Newton’s method.7 That is, prices were solved endogen-
ously given assumed quantities. This solution provided the
expected prices under the assumed quantities of imports.
Fig. 1 demonstrates the method graphically, assuming two
goods for simplicity: one good is the numeraire ðxÞ; and the
second good, Q; is quantity of shrimp imports from an
arbitrary region.
Under a non-quota scenario, the quantity of shrimp
imported is Q0; and the price of Q0 is P0; given by the slope
of the budget constraint. If quantity is reduced from Q0 to Q1
under the quota, the virtual price of Q1 (i.e. P1) is found to
be the slope of the expenditure function as it rotates inward.
The virtual prices of all import categories in this analysis are
simultaneously determined by perturbing a regional quan-
tity and then solving all the virtual prices in the system.
The CV was found by using the estimated prices under
the assumed quantities. In this case, the Stone–Geary
indirect utility function was solved using the formula
Vðp0; x0Þ2 Vðp1
; x0 2 CVÞ; ð7Þ
which gives a unique empirical measure of CV based on
parameter estimates from the demand equations. With a
constant income, the restrictions are hypothesized to result
in a negative impact on welfare. A negative impact on the
welfare of US consumers is expected because the utility at
the new prices (which should be higher because quantity is
restricted) is expected to be lower than when quantity
restrictions are not in effect.
5. Results
Table 3 shows the results of the estimated equations with
the original data and under the Monte Carlo simulation.8
The parameter estimates appear to be consistent given
that there are no substantial differences between those
generated from the simulation and those of the original
6 There are other, much smaller, import sources that may be affected by
the ban. However, these countries are scattered around the world and make
up a very small portion of total imports. Separating them out would reduce
degrees of freedom and not add much to the model. However, the reader
should be aware that the welfare estimates presented in this paper are likely
slightly underestimated.
7 This option is available in the ‘goal seeking’ capability of SAS’s PROC
Model package (SAS Institute, 1997).8 Note that it was not possible with these data to perform Monte Carlo
simulation to estimate more flexible functional forms. This is because there
are too few observations to estimate initial variance–covariance matrix on
which to base the simulation.
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model estimate. White’s test was performed and suggested
no signs of heteroskedasticity, and Godfrey’s test suggested
no signs of serial correlation.
No minimum import quantity from a region ðgjÞ is
significant, suggesting that total expenditure, x; is allocated
across regions on the basis of the marginal expenditure
shares, bi: Results show that approximately 40% of US
shrimp import expenditure is allocated to imports in the
WEST region, about 24% to the ASEAN region, 2% to
India, and the remainder to the ROW. The relatively low
share for India suggests that the shrimp import ban for that
country will have little impact on US consumer welfare by
itself. However, the ASEAN group makes up a large portion
of total US expenditure so that changes in the quantity
coming from that region will likely have a much larger
impact on US consumer welfare.
Table 4 shows the uncompensated own-price and cross-
price as well as the income elasticities of demand for each
region.
The WEST exhibited the most inelastic demand with an
own-price elasticity of 20.798. This result is expected
given the proximity of the WEST countries to the US The
ASEAN group exhibited the largest price elasticity of
import demand at 21.263, suggesting that US demand is
considerably more responsive to ASEAN shrimp price
changes.
Imports from ASEAN countries were most sensitive to
changes in US consumer expenditures. A 1% increase in US
expenditures for imported shrimp results in a 1.61% increase
in imports of shrimp from ASEAN countries. The magnitude
of this elasticity relative to the other regions suggests that US
consumers treat ASEAN shrimp as more of a luxury than
shrimp from other regions. That is, as income increases,
imports from ASEAN countries are expected to increase the
most. The ROW is also slightly elastic. The WEST region
and India are both inelastic, suggesting that these regions
benefit the least from income increases in the US.
The own-price elasticities were tested for equivalence
using the likelihood ratio test and these results are shown in
Table 5.
These results strongly suggest that the own-price
elasticities of demand for each region are different, implying
that each region is viewed differently by importers. The
exception was the WEST and ROW regions. These regions
did not appear to be statistically different. These results
generally support the maintained hypothesis that it is
consistent to model these regions separately.
The CV estimates for the two scenarios are presented in
Table 6.
In both cases (reallocation of imports to other regions and
no reallocation of imports), there is a welfare loss to US
consumers. However, when reallocation is possible, the
welfare loss is roughly 1/5 of that when reallocation is not
possible. Thus, if fisheries and aquacultural enterprises in
other regions have the ability to sustain the increase in
demand from US imports, then the cost of the shrimp import
ban is expected to be much lower than if a reallocation of
imports is not possible.
Fig. 1. Estimation of CV using virtual prices.
Table 3
Estimated parameters for LES model
Parameter Estimated model
using original data
Estimated model
using Monte Carlo
simulation
b1 0.398 (0.0975) 0.408 (0.0055)
b2 0.241 (0.0484) 0.237 (0.0022)
b3 0.023 (0.0070) 0.023 (0.0005)
b4 0.332 (0.0655) 0.326 (0.0040)
g1 6220.15 (67,799.7) 14,102.13 (2952.8)
g2 229,243.67 (12,741.9) 230,910.13 (1494.2)
g3 10,697.28 (9048.9) 12,121.45
g4 4329.2 (40,696.4) 6944.45 (3018.1)
Number of
observations
18 1818
Log likelihood
of system
2736.6 277,277
Numbers in parentheses are standard errors.
Table 4
Uncompensated own-price, cross-price, and income elasticities of demand
for shrimp imports
West ASEAN India ROW
West 20.798
ASEAN 0.052 21.263
India 20.000a 20.000a 21.00
ROW 20.011 20.021 20.008 20.978
Income 0.744 1.607 0.516 1.049
a Smaller than 0.000 in absolute value.
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6. Discussion
The results clearly indicate that the ban on shrimp
imports from certain countries will have (or is having) an
adverse impact on the welfare of US consumers, at least in
monetary terms. However, one could interpret this loss in
welfare as the opportunity cost of achieving the environ-
mental goal of reducing sea turtle by-catch. Interpreted in
this way, US consumers are willing to forgo the CV
estimated here to reduce the loss of sea turtles. The question
becomes, are trade restrictions the most equitable and
efficient way to reduce sea turtle by-catch? Are there
alternative ways to achieve this goal?
The issue of equity is beyond the scope of this paper.
Some authors such as Bhagwati and Srinivisan, 1996 have
taken the position that environmental and social goal-setting
is allowed under the WTO if the impacts are borne directly
by the domestic consumers/producers. In this case,
however, there would likely be some direct impacts
experienced by producers in the nations that are affected
by the ban (Stewart, 1998, 197–219). If the CV estimate is
viewed as the opportunity cost that US consumers are
willing to take to achieve the environmental goal, then it
seems plausible to devise some type of compensation
scheme that would be more efficient in achieving the goals.
For instance, if the cost of equipping the ASEAN countries’
fleets with TEDs is lower than the foregone CV from
reduced imports, then a welfare gain could be achieved via a
policy in which the US compensates and/or provides
ASEAN countries with TEDs.
We attempt here to provide a rough estimate of the
difference in costs and benefits of such a compensation
scheme.9 The price of a TED is $300/trawler (Stewart, 1998,
197–219), and there are approximately 2,79,261 trawlers in
ASEAN countries and India (this is an approximation from
Food and Agriculture Organization (1995) fisheries data).
Assuming that TEDs will require replacement approxi-
mately every 3 years, we can calculate the net present value
of the cost of the policy over the next 10 years as10
NPVðTEDÞ ¼X10
t¼1
TEDcost
ð1:10Þt: ð8Þ
Making the simplifying assumption that the CV measure
will remain static, we can estimate the lost welfare as
NPVðCVÞ ¼X10
t¼1
CV
ð1:10Þt: ð9Þ
In order to estimate the NPV of the policy, the ‘without’
policy scenario is interpreted as being the trade restriction
alone, and the ‘with’ policy scenario as the compensation
scheme instead of the trade restriction. Thus, if equipping
ASEAN and Indian shrimpers with TEDs results in an
increase in imports back to the pre-restriction level, the net
welfare gain (loss) would be W ¼ NPVðCVÞ2 NPVðTEDÞ:
There are two CV estimates, one with and one without the
ability to reallocate shrimp imports. Thus, there are two
estimates of W (Table 6).
When no reallocation of imports is possible, the resulting
NPV of equipping the trawlers with TEDs is $46,62,18,965,
suggesting a positive impact on US consumers if ASEAN
and Indian shrimpers are compensated for adopting the TED
system. In contrast, when reallocation of imports to other
regions is possible, the compensation for the TEDs results in
a negative welfare impact of 2$84,461,686. This indicates
that there is no real incentive for compensation when the US
has the ability to make up for import shortfalls by increasing
its own production and reallocating imports from other
regions. Again, there is no consideration here of the impacts
on other parties. Thus, this represents only a partial analysis
of the welfare effects and potential benefits of
the compensation scheme.
7. Conclusions
This analysis utilized an LES model of shrimp imports to
address the impacts of a shrimp import ban to achieve
Table 5
Likelihood ratio tests for equivalence of own-price elasticities of demand
Elasticitiesa Likelihood ratio
eWEST ¼ eASEAN 568.88b
eWEST ¼ eIndia 469.62b
eWEST ¼ eROW 0.04
eASEAN ¼ eIndia 1116.79b
eASEAN ¼ eROW 1008.18b
eIndia ¼ eROW 251.85b
a Own-price elasticities of demand in each region.b Statistically significant at the 0·001 level or better.
Table 6
Estimated CV for two alternative scenarios
Scenario CV estimate W estimate
No reallocation of imports $ 2 109,835,930 $466,218,965
Reallocation of imports between
West and ROW regions
on the basis of
previous import percentages
$ 2 20,215,190 $ 2 84,461,686
9 We do not directly consider the price impacts of the capital investment
in the TED device. That is, the TED may make the shrimpers more or less
efficient, which ultimately may impact prices. To the extent that it makes
shrimpers less efficient, the reported impacts would be underestimated.10 A 10-year planning horizon was chosen given the uncertainty about the
length of time for political agreements. A discount rate of 10% was
assumed for this analysis, but further analysis reveals that the results
presented in Table 6 are insensitive (that is, the signs on the results do not
change) to the assumed discount rate.
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the environmental goal of reduced sea turtle by-catch. The
CV estimates suggest a negative impact on US consumers
resulting from the ban, but the magnitude of the impact
depends on whether the lost imports from the banned
countries are reallocated to other countries.
The fact that the shrimp import ban reduces consumer
welfare is not surprising. However, the fact that the
magnitude of the impact is dependent on whether imports
are reallocated or not demonstrates the implications of
being in a multi-product versus single product world.
That is, when consumers have the ability to substitute
between regions for imports, this appears to greatly
dampen the effects of the trade restriction on US
consumers. Thus, it appears that it is important to
consider substitution possibilities in policy impact anal-
ysis because failure to do so may overstate the true
impact of the policy.
Finally, interpretation of the welfare loss as an
opportunity cost opens the door for designing compensation
schemes so that those countries that are affected by the ban
can be compensated. Results of this analysis suggest that the
efficacy of any compensation scheme will depend on
the ability to substitute shrimp from other regions. That is,
the greater the ability to substitute, the less incentive for
compensation. However, two factors should be considered.
First, the positive impact when substitution is not possible is
disproportionately larger than the negative impact when
substitution is possible. Coupled with the fact that most
global fisheries are already pressured and may not sustain
increased demand from shifting US imports suggests that
the effect of compensation is likely to be positive. However,
this question needs further research. Approaching the
problem from this perspective may result in a more efficient
method of achieving the environmental goal than through a
trade restriction.
Further research into the shrimp ban is warranted
because several questions have yet to be answered. What
is the impact of the ban on producers in both countries that
do and do not use the TED system? What are the impacts on
consumers around the world? If data were available on
aquaculture shrimp imports, this might improve the quality
of the estimates. The lack of data is likely to have only a
marginal effect on the magnitude of the estimates, but
distinction between aquaculture and wild caught imports
would improve the analytical richness of the model. As
trade rules become more complex and the demand for
environmental regulation increases, more problems such as
the shrimp ban debate will arise. This paper clearly
demonstrates an example of environmental regulation
through trade and that these regulations have impacts on
the distribution of income.
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