mixture modelling of continuous variables. mixture modelling so far we have dealt with mixture...

Mixture modelling of continuous variables

Mixture modelling

• So far we have dealt with mixture modelling for a selection of binary or ordinal variables collected at a single time point (c/s) or longitudinally across time

• The simplest example of a mixture model consists of a single continuous manifest variable

• The multivariate extension to this simple model is known as Latent Profile Analysis

Single continuous variable

• An underlying latent grouping might present itself as a multi-modal distribution for the continuous variable

Height



Height

Females



Height

Males


• But the distance between modes may be small or even non-existent

• Depends on the variation in the item being measured and also the sample in which the measurement is taken (e.g. clinical or general population)


Figure taken from: Muthén, B. (2001). Latent variable mixture modeling. In G. A. Marcoulides & R. E. Schumacker (eds.), New Developments and Techniques in Structural Equation Modeling (pp. 1-33). Lawrence Erlbaum Associates.


• We assume that the manifest variable is normally distributed within each latent class

GHQ Example

Data: File is "ego_ghq12_id.dta.dat" ;

Define: sumodd = ghq01 +ghq03 +ghq05 +ghq07 +ghq09 +ghq11; sumeven = ghq02 +ghq04 +ghq06 +ghq08 +ghq10 +ghq12; ghq_sum = sumodd + sumeven;

Variable: Names are ghq01 ghq02 ghq03 ghq04 ghq05 ghq06 ghq07 ghq08 ghq09 ghq10 ghq11 ghq12 f1 id; Missing are all (-9999) ; usevariables = ghq_sum;

Analysis: Type = basic ;

plot: type is plot3;

Here we derive a single sum-score from the 12 ordinal GHQ items

The syntax shows that variables can be created in the define statement which are not then used in the final model

Examine the distribution of the scale

Scale appears unimodal, although there is a long upper-tail

Examine the distribution of the scale

By changing from the default number of bins we see secondary modes appearing

Fit a 2-class mixture

Variable: <snip> classes = c(2);

Analysis: type = mixture ; proc = 2 (starts); starts = 100 20; stiterations = 20; stscale = 15;

model: %overall%

%c#1% [ghq_sum]; ghq_sum (equal_var);


Fit a 2-class mixture



model: %overall%



This funny set of symbols refers to the first class

Means are referred to using square brackets.

Variances are bracket-less.

Here we have constrained the variances to be equal between classes by having the same bit of text in brackets at the end of the two variance lines

Means will be freely estimated.

Model results

TESTS OF MODEL FIT

Loglikelihood

H0 Value -3624.960 H0 Scaling Correction Factor 1.078 for MLR

Information Criteria

Number of Free Parameters 4 Akaike (AIC) 7257.921 Bayesian (BIC) 7278.002 Sample-Size Adjusted BIC 7265.297 (n* = (n + 2) / 24)

Model results

FINAL CLASS COUNTS AND PROPORTIONS FOR THE LATENT CLASSESBASED ON THE ESTIMATED MODEL

Latent classes 1 200.36980 0.17906 2 918.63020 0.82094

CLASSIFICATION QUALITY Entropy 0.829

CLASSIFICATION OF INDIVIDUALS BASED ON THEIR MOST LIKELY LATENT CLASS MEMBERSHIP

Latent classes 1 189 0.16890 2 930 0.83110

Average Latent Class Probabilities for Most Likely Latent Class Membership (Row)by Latent Class (Column)

1 2 1 0.889 0.111 2 0.035 0.965

Entropy is high

A smaller class of 18% has emerged, consistent with the expected behaviour of the GHQ in this sample from primary care

Class-specific entropies are both good

Model results Two-Tailed Estimate S.E. Est./S.E. P-Value

Latent Class 1

Means GHQ_SUM 37.131 0.574 64.737 0.000

Variances GHQ_SUM 18.876 1.016 18.581 0.000

Latent Class 2

Means GHQ_SUM 23.618 0.202 117.046 0.000


Categorical Latent Variables

Means C#1 -1.523 0.118 -12.947 0.000

Huge separation in means since SD = 4.3 (i.e. sqrt(18.88))

Examine within-class distributions

What have we done?

• We have effectively done a t-test backwards.• Rather than obtaining a manifest binary variable,

assuming equality of variances and testing for equality of means

• we have derived a latent binary variable based on the assumption of a difference in means (still with equal variance)

What next?

• The bulk of the sample now falls into a class with a GHQ distribution which is more symmetric than the sample as a whole

• There appear to be additional modes within the smaller class

• The ‘optimal’ number of classes can be assessed in the usual way using aBIC, entropy and the bootstrap LRT.

• In the univariate case, residual correlations are not an issue, but when moving to a multivariate example, these too will need to be assessed.

What next?

• As before, posterior probabilities can be exported and modelled in a weighted regression analysis

• A logistic regression analysis using a latent binary variable derived from the data is likely to be far more informative than a linear-regression analysis using the manifest continuous variable

What if we had not constrained the variances?



model: %overall%

%c#1% [ghq_sum]; ghq_sum ; ! (equal_var);

%c#2% [ghq_sum]; ghq_sum ; ! (equal_var);

Commented out

TESTS OF MODEL FIT

Loglikelihood H0 Value -3610.586 H0 Scaling Correction Factor 0.932 for MLR

Information Criteria Number of Free Parameters 5 Akaike (AIC) 7231.172 Bayesian (BIC) 7256.273 Sample-Size Adjusted BIC 7240.392

FINAL CLASS COUNTS AND PROPORTIONS FOR THE LATENT CLASSESBASED ON THE ESTIMATED MODEL

Latent Classes

1 456.72641 0.40816 2 662.27359 0.59184

CLASSIFICATION QUALITY

Entropy 0.479

Entropy is poor

Classes are more equal

BIC is lower!

Means are closer, variances differ greatly

MODEL RESULTS

Two-Tailed Estimate S.E. Est./S.E. P-Value

Latent Class 1

Means GHQ_SUM 31.493 0.816 38.616 0.000


Latent Class 2

Means GHQ_SUM 22.275 0.328 67.823 0.000


Distribution far from symmetric

mixture modelling of continuous variables. mixture modelling so far we have dealt with mixture...

Documents

sum ghq

class mixture variable

var slide

latent class slide

sum equal

sum analysis

single sumscore

sumodd sumeven variable