invariance.alignment {sirt}R Documentation

Alignment Procedure for Linking under Approximate Invariance

Description

The function invariance.alignment performs alignment under approximate invariance for G groups and I items (Asparouhov & Muthen, 2014; Byrne & van de Vijver, 2017; DeMars, 2020; Finch, 2016; Fischer & Karl, 2019; Flake & McCoach, 2018; Kim et al., 2017; Marsh et al., 2018; Muthen & Asparouhov, 2014, 2018; Pokropek, Davidov & Schmidt, 2019). It is assumed that item loadings and intercepts are previously estimated as a unidimensional factor model under the assumption of a factor with zero mean and a variance of one.

The function invariance_alignment_constraints postprocesses the output of the invariance.alignment function and estimates item parameters under equality constraints for prespecified absolute values of parameter tolerance.

The function invariance_alignment_simulate simulates a one-factor model for multiple groups for given matrices of \nu and \lambda parameters of item intercepts and item slopes (see Example 6).

The function invariance_alignment_cfa_config estimates one-factor models separately for each group as a preliminary step for invariance alignment (see Example 6). Sampling weights are accommodated by the argument weights. The computed variance matrix vcov by this function can be used to obtain standard errors in the invariance.alignment function if it is supplied as the argument vcov.

Usage

invariance.alignment(lambda, nu, wgt=NULL, align.scale=c(1, 1),
    align.pow=c(.5, .5), eps=1e-3, psi0.init=NULL, alpha0.init=NULL, center=FALSE,
    optimizer="optim", fixed=NULL, meth=1, vcov=NULL, eps_grid=seq(0,-10, by=-.5),
    num_deriv=FALSE, ...)

## S3 method for class 'invariance.alignment'
summary(object, digits=3, file=NULL, ...)

invariance_alignment_constraints(model, lambda_parm_tol, nu_parm_tol )

## S3 method for class 'invariance_alignment_constraints'
summary(object, digits=3, file=NULL, ...)

invariance_alignment_simulate(nu, lambda, err_var, mu, sigma, N, output="data",
     groupwise=FALSE, exact=FALSE)

invariance_alignment_cfa_config(dat, group, weights=NULL, model="2PM", verbose=FALSE, ...)

Arguments

lambda

A G \times I matrix with item loadings

nu

A G \times I matrix with item intercepts

wgt

A G \times I matrix for weighing groups for each item

align.scale

A vector of length two containing scale parameter a_\lambda and a_\nu (see Details)

align.pow

A vector of length two containing power p_\lambda and p_\nu (see Details)

eps

A parameter in the optimization function

psi0.init

An optional vector of initial \psi_0 parameters

alpha0.init

An optional vector of initial \alpha_0 parameters

center

Logical indicating whether estimated means and standard deviations should be centered.

optimizer

Name of the optimizer chosen for alignment. Options are "optim" (using stats::optim) or "nlminb" (using stats::nlminb).

fixed

Logical indicating whether SD of first group should be fixed to one. If fixed=FALSE, the product of all SDs is set to one. If NULL, then fixed is automatically chosen by default. For many groups, fixed=FALSE is chosen.

meth

Type of method used for optimization function. meth=1 is the default and the optimization function used in Mplus. meth=2 uses logarithmized item loadings in alignment. The choice meth=4 uses the constraint \prod_g \psi_g=1 and adds the penalty \lambda \sum_g \alpha_g^2 for a fixed value \lambda that depends on the weights wgt (similar to Mplus' free method). The choice meth=3 only uses the constraint \prod_g \psi_g=1 (similar to Mplus' FIXED method).

vcov

Variance matrix produced by invariance_alignment_cfa_config for standard error computation. If a matrix is provided, standard errors are computed.

eps_grid

Grid of logarithmized epsilon values in optimization

num_deriv

Logical indicating whether numerical derivatives should be used

object

Object of class invariance.alignment

digits

Number of digits used for rounding

file

Optional file name in which summary should be sunk

...

Further optional arguments to be passed

model

Model of class invariance.alignment. For invariance_alignment_cfa_config: Model type: "2PM" for two-parameter model with unequal loadings and "1PM" with equal loadings and equal residual variances

lambda_parm_tol

Parameter tolerance for \lambda parameters

nu_parm_tol

Parameter tolerance for \nu parameters

err_var

Error variance

mu

Vector of means

sigma

Vector of standard deviations

N

Vector of sample sizes per group

output

Specifies output type: "data" for dataset and "suffstat" for sufficient statistics (i.e., means and covariance matrices)

groupwise

Logical indicating whether group-wise output is requested

exact

Logical indicating whether distributions should be exactly preserved in simulated data

dat

Dataset with items or a list containing sufficient statistics

group

Vector containing group indicators

weights

Optional vector of sampling weights

verbose

Logical indicating whether progress should be printed

Details

For G groups and I items, item loadings \lambda_{ig0} and intercepts \nu_{ig0} are available and have been estimated in a 1-dimensional factor analysis assuming a standardized factor.

The alignment procedure searches means \alpha_{g0} and standard deviations \psi_{g0} using an alignment optimization function F. This function is defined as

F=\sum_i \sum_{ g_1 < g_2} w_{i,g1} w_{i,g2} f_\lambda( \lambda_{i g_1,1} - \lambda_{i g_2,1} ) + \sum_i \sum_{ g_1 < g_2} w_{i,g1} w_{i,g2} f_\nu( \nu_{i g_1,1} - \nu_{i g_2,1} )

where the aligned item parameters \lambda_{i g,1} and \nu_{i g,1} are defined such that

\lambda_{i g,1}=\lambda_{i g 0} / \psi_{g0} \qquad \mbox{and} \qquad \nu_{i g,1}=\nu_{i g 0} - \alpha_{g0} \lambda_{ig0} / \psi_{g0}

and the optimization functions are defined as

f_\lambda (x)=| x/ a_\lambda | ^{p_\lambda} \approx [ ( x/ a_\lambda )^2 + \varepsilon ]^{p_\lambda / 2} \qquad \mbox{and} \qquad f_\nu (x)=| x/ a_\nu ]^{p_\nu} \approx [ ( x/ a_\nu )^2 + \varepsilon ]^{p_\nu / 2}

using a small \varepsilon > 0 (e.g. .001) to obtain a differentiable optimization function. For p_\nu=0 or p_\lambda=0, the optimization function essentially counts the number of different parameter and mimicks a L_0 penalty which is zero iff the argument is zero and one otherwise. It is approximated by

f(x)=x^2 (x^2 + \varepsilon )^{-1}

(O'Neill & Burke, 2023).

For identification reasons, the product \Pi_g \psi_{g0} (meth=0,0.5) of all group standard deviations or \psi_1 (meth=1,2) is set to one. The mean \alpha_{g0} of the first group is set to zero (meth=0.5,1,2) or a penalty function is added to the linking function (meth=0).

Note that Asparouhov and Muthen (2014) use a_\lambda=a_\nu=1 (which can be modified in align.scale) and p_\lambda=p_\nu=0.5 (which can be modified in align.pow). In case of p_\lambda=2, the penalty is approximately f_\lambda(x)=x^2 , in case of p_\lambda=0.5 it is approximately f_\lambda(x)=\sqrt{|x|} . Note that sirt used a different parametrization in versions up to 3.5. The p parameters have to be halved for consistency with previous versions (e.g., the Asparouhov & Muthen parametrization corresponds to p=.25; see also Fischer & Karl, 2019, for an application of the previous parametrization).

Effect sizes of approximate invariance based on R^2 have been proposed by Asparouhov and Muthen (2014). These are calculated separately for item loading and intercepts, resulting in R^2_\lambda and R^2_\nu measures which are included in the output es.invariance. In addition, the average correlation of aligned item parameters among groups (rbar) is reported.

Metric invariance means that all aligned item loadings \lambda_{ig,1} are equal across groups and therefore R^2_\lambda=1. Scalar invariance means that all aligned item loadings \lambda_{ig,1} and aligned item intercepts \nu_{ig,1} are equal across groups and therefore R^2_\lambda=1 and R^2_\nu=1 (see Vandenberg & Lance, 2000).

Value

A list with following entries

pars

Aligned distribution parameters

itempars.aligned

Aligned item parameters for all groups

es.invariance

Effect sizes of approximate invariance

lambda.aligned

Aligned \lambda_{i g,1} parameters

lambda.resid

Residuals of \lambda_{i g,1} parameters

nu.aligned

Aligned \nu_{i g,1} parameters

nu.resid

Residuals of \nu_{i g,1} parameters

Niter

Number of iterations for f_\lambda and f_\nu optimization functions

fopt

Minimum optimization value

align.scale

Used alignment scale parameters

align.pow

Used alignment power parameters

vcov

Estimated variance matrix of aligned means and standard deviations

References

Asparouhov, T., & Muthen, B. (2014). Multiple-group factor analysis alignment. Structural Equation Modeling, 21(4), 1-14. doi:10.1080/10705511.2014.919210

Byrne, B. M., & van de Vijver, F. J. R. (2017). The maximum likelihood alignment approach to testing for approximate measurement invariance: A paradigmatic cross-cultural application. Psicothema, 29(4), 539-551. doi:10.7334/psicothema2017.178

DeMars, C. E. (2020). Alignment as an alternative to anchor purification in DIF analyses. Structural Equation Modeling, 27(1), 56-72. doi:10.1080/10705511.2019.1617151

Finch, W. H. (2016). Detection of differential item functioning for more than two groups: A Monte Carlo comparison of methods. Applied Measurement in Education, 29,(1), 30-45, doi:10.1080/08957347.2015.1102916

Fischer, R., & Karl, J. A. (2019). A primer to (cross-cultural) multi-group invariance testing possibilities in R. Frontiers in Psychology | Cultural Psychology, 10:1507. doi:10.3389/fpsyg.2019.01507

Flake, J. K., & McCoach, D. B. (2018). An investigation of the alignment method with polytomous indicators under conditions of partial measurement invariance. Structural Equation Modeling, 25(1), 56-70. doi:10.1080/10705511.2017.1374187

Kim, E. S., Cao, C., Wang, Y., & Nguyen, D. T. (2017). Measurement invariance testing with many groups: A comparison of five approaches. Structural Equation Modeling, 24(4), 524-544. doi:10.1080/10705511.2017.1304822

Marsh, H. W., Guo, J., Parker, P. D., Nagengast, B., Asparouhov, T., Muthen, B., & Dicke, T. (2018). What to do when scalar invariance fails: The extended alignment method for multi-group factor analysis comparison of latent means across many groups. Psychological Methods, 23(3), 524-545. doi: 10.1037/met0000113

Muthen, B., & Asparouhov, T. (2014). IRT studies of many groups: The alignment method. Frontiers in Psychology | Quantitative Psychology and Measurement, 5:978. doi:10.3389/fpsyg.2014.00978

Muthen, B., & Asparouhov, T. (2018). Recent methods for the study of measurement invariance with many groups: Alignment and random effects. Sociological Methods & Research, 47(4), 637-664. doi:10.1177/0049124117701488

O'Neill, M., & Burke, K. (2023). Variable selection using a smooth information criterion for distributional regression models. Statistics and Computing, 33(3), 71. doi:10.1007/s11222-023-10204-8

Pokropek, A., Davidov, E., & Schmidt, P. (2019). A Monte Carlo simulation study to assess the appropriateness of traditional and newer approaches to test for measurement invariance. Structural Equation Modeling, 26(5), 724-744. doi:10.1080/10705511.2018.1561293

Vandenberg, R. J., & Lance, C. E. (2000). A review and synthesis of the measurement invariance literature: Suggestions, practices, and recommendations for organizational research. Organizational Research Methods, 3, 4-70. doi:10.1177/109442810031002s

See Also

For IRT linking see also linking.haberman or TAM::tam.linking.

For modeling random item effects for loadings and intercepts see mcmc.2pno.ml.

Examples

#############################################################################
# EXAMPLE 1: Item parameters cultural activities
#############################################################################

data(data.activity.itempars, package="sirt")
lambda <- data.activity.itempars$lambda
nu <- data.activity.itempars$nu
Ng <-  data.activity.itempars$N
wgt <- matrix( sqrt(Ng), length(Ng), ncol(nu) )

#***
# Model 1: Alignment using a quadratic loss function
mod1 <- sirt::invariance.alignment( lambda, nu, wgt, align.pow=c(2,2) )
summary(mod1)

#****
# Model 2: Different powers for alignment
mod2 <- sirt::invariance.alignment( lambda, nu, wgt,  align.pow=c(.5,1),
              align.scale=c(.95,.95))
summary(mod2)

# compare means from Models 1 and 2
plot( mod1$pars$alpha0, mod2$pars$alpha0, pch=16,
    xlab="M (Model 1)", ylab="M (Model 2)", xlim=c(-.3,.3), ylim=c(-.3,.3) )
lines( c(-1,1), c(-1,1), col="gray")
round( cbind( mod1$pars$alpha0, mod2$pars$alpha0 ), 3 )
round( mod1$nu.resid, 3)
round( mod2$nu.resid,3 )

# L0 penalty
mod2b <- sirt::invariance.alignment( lambda, nu, wgt,  align.pow=c(0,0),
              align.scale=c(.3,.3))
summary(mod2b)

#****
# Model 3: Low powers for alignment of scale and power
# Note that setting increment.factor larger than 1 seems necessary
mod3 <- sirt::invariance.alignment( lambda, nu, wgt, align.pow=c(.5,.75),
            align.scale=c(.55,.55), psi0.init=mod1$psi0, alpha0.init=mod1$alpha0 )
summary(mod3)

# compare mean and SD estimates of Models 1 and 3
plot( mod1$pars$alpha0, mod3$pars$alpha0, pch=16)
plot( mod1$pars$psi0, mod3$pars$psi0, pch=16)

# compare residuals for Models 1 and 3
# plot lambda
plot( abs(as.vector(mod1$lambda.resid)), abs(as.vector(mod3$lambda.resid)),
      pch=16, xlab="Residuals lambda (Model 1)",
      ylab="Residuals lambda (Model 3)", xlim=c(0,.1), ylim=c(0,.1))
lines( c(-3,3),c(-3,3), col="gray")
# plot nu
plot( abs(as.vector(mod1$nu.resid)), abs(as.vector(mod3$nu.resid)),
      pch=16, xlab="Residuals nu (Model 1)", ylab="Residuals nu (Model 3)",
      xlim=c(0,.4),ylim=c(0,.4))
lines( c(-3,3),c(-3,3), col="gray")

## Not run: 
#############################################################################
# EXAMPLE 2: Comparison 4 groups | data.inv4gr
#############################################################################

data(data.inv4gr)
dat <- data.inv4gr
miceadds::library_install("semTools")

model1 <- "
    F=~ I01 + I02 + I03 + I04 + I05 + I06 + I07 + I08 + I09 + I10 + I11
    F ~~ 1*F
    "

res <- semTools::measurementInvariance(model1, std.lv=TRUE, data=dat, group="group")
  ##   Measurement invariance tests:
  ##
  ##   Model 1: configural invariance:
  ##       chisq        df    pvalue       cfi     rmsea       bic
  ##     162.084   176.000     0.766     1.000     0.000 95428.025
  ##
  ##   Model 2: weak invariance (equal loadings):
  ##       chisq        df    pvalue       cfi     rmsea       bic
  ##     519.598   209.000     0.000     0.973     0.039 95511.835
  ##
  ##   [Model 1 versus model 2]
  ##     delta.chisq      delta.df delta.p.value     delta.cfi
  ##         357.514        33.000         0.000         0.027
  ##
  ##   Model 3: strong invariance (equal loadings + intercepts):
  ##       chisq        df    pvalue       cfi     rmsea       bic
  ##    2197.260   239.000     0.000     0.828     0.091 96940.676
  ##
  ##   [Model 1 versus model 3]
  ##     delta.chisq      delta.df delta.p.value     delta.cfi
  ##        2035.176        63.000         0.000         0.172
  ##
  ##   [Model 2 versus model 3]
  ##     delta.chisq      delta.df delta.p.value     delta.cfi
  ##        1677.662        30.000         0.000         0.144
  ##

# extract item parameters separate group analyses
ipars <- lavaan::parameterEstimates(res$fit.configural)
# extract lambda's: groups are in rows, items in columns
lambda <- matrix( ipars[ ipars$op=="=~", "est"], nrow=4,  byrow=TRUE)
colnames(lambda) <- colnames(dat)[-1]
# extract nu's
nu <- matrix( ipars[ ipars$op=="~1"  & ipars$se !=0, "est" ], nrow=4,  byrow=TRUE)
colnames(nu) <- colnames(dat)[-1]

# Model 1: least squares optimization
mod1 <- sirt::invariance.alignment( lambda=lambda, nu=nu )
summary(mod1)
  ##   Effect Sizes of Approximate Invariance
  ##          loadings intercepts
  ##   R2       0.9826     0.9972
  ##   sqrtU2   0.1319     0.0526
  ##   rbar     0.6237     0.7821
  ##   -----------------------------------------------------------------
  ##   Group Means and Standard Deviations
  ##     alpha0  psi0
  ##   1  0.000 0.965
  ##   2 -0.105 1.098
  ##   3 -0.081 1.011
  ##   4  0.171 0.935

# Model 2: sparse target function
mod2 <- sirt::invariance.alignment( lambda=lambda, nu=nu, align.pow=c(.5,.5) )
summary(mod2)
  ##   Effect Sizes of Approximate Invariance
  ##          loadings intercepts
  ##   R2       0.9824     0.9972
  ##   sqrtU2   0.1327     0.0529
  ##   rbar     0.6237     0.7856
  ##   -----------------------------------------------------------------
  ##   Group Means and Standard Deviations
  ##     alpha0  psi0
  ##   1 -0.002 0.965
  ##   2 -0.107 1.098
  ##   3 -0.083 1.011
  ##   4  0.170 0.935

#############################################################################
# EXAMPLE 3: European Social Survey data.ess2005
#############################################################################

data(data.ess2005)
lambda <- data.ess2005$lambda
nu <- data.ess2005$nu

# Model 1: least squares optimization
mod1 <- sirt::invariance.alignment( lambda=lambda, nu=nu, align.pow=c(2,2) )
summary(mod1)

# Model 2: sparse target function and definition of scales
mod2 <- sirt::invariance.alignment( lambda=lambda, nu=nu, control=list(trace=2) )
summary(mod2)

#############################################################################
# EXAMPLE 4: Linking with item parameters containing outliers
#############################################################################

# see Help file in linking.robust

# simulate some item difficulties in the Rasch model
I <- 38
set.seed(18785)
itempars <- data.frame("item"=paste0("I",1:I) )
itempars$study1 <- stats::rnorm( I, mean=.3, sd=1.4 )
# simulate DIF effects plus some outliers
bdif <- stats::rnorm(I, mean=.4, sd=.09) +
             (stats::runif(I)>.9 )*rep( 1*c(-1,1)+.4, each=I/2 )
itempars$study2 <- itempars$study1 + bdif
# create input for function invariance.alignment
nu <- t( itempars[,2:3] )
colnames(nu) <- itempars$item
lambda <- 1+0*nu

# linking using least squares optimization
mod1 <- sirt::invariance.alignment( lambda=lambda, nu=nu )
summary(mod1)
  ##   Group Means and Standard Deviations
  ##          alpha0 psi0
  ##   study1 -0.286    1
  ##   study2  0.286    1

# linking using powers of .5
mod2 <- sirt::invariance.alignment( lambda=lambda, nu=nu, align.pow=c(1,1) )
summary(mod2)
  ##   Group Means and Standard Deviations
  ##          alpha0 psi0
  ##   study1 -0.213    1
  ##   study2  0.213    1

# linking using powers of .25
mod3 <- sirt::invariance.alignment( lambda=lambda, nu=nu, align.pow=c(.5,.5) )
summary(mod3)
  ##   Group Means and Standard Deviations
  ##          alpha0 psi0
  ##   study1 -0.207    1
  ##   study2  0.207    1

#############################################################################
# EXAMPLE 5: Linking gender groups with data.math
#############################################################################

data(data.math)
dat <- data.math$data
dat.male <- dat[ dat$female==0, substring( colnames(dat),1,1)=="M"  ]
dat.female <- dat[ dat$female==1, substring( colnames(dat),1,1)=="M"  ]

#*************************
# Model 1: Linking using the Rasch model
mod1m <- sirt::rasch.mml2( dat.male )
mod1f <- sirt::rasch.mml2( dat.female )

# create objects for invariance.alignment
nu <- rbind( mod1m$item$thresh, mod1f$item$thresh )
colnames(nu) <- mod1m$item$item
rownames(nu) <- c("male", "female")
lambda <- 1+0*nu

# mean of item difficulties
round( rowMeans(nu), 3 )

# Linking using least squares optimization
res1a <- sirt::invariance.alignment( lambda, nu, align.scale=c( .3, .5 ) )
summary(res1a)

# Linking using optimization with absolute value function (pow=.5)
res1b <- sirt::invariance.alignment( lambda, nu, align.scale=c( .3, .5 ),
                align.pow=c(1,1) )
summary(res1b)

#-- compare results with Haberman linking
I <- ncol(dat.male)
itempartable <- data.frame( "study"=rep( c("male", "female"), each=I ) )
itempartable$item <- c( paste0(mod1m$item$item),  paste0(mod1f$item$item) )
itempartable$a <- 1
itempartable$b <- c( mod1m$item$b, mod1f$item$b )
# estimate linking parameters
res1c <- sirt::linking.haberman( itempars=itempartable )

#-- results of sirt::equating.rasch
x <- itempartable[ 1:I, c("item", "b") ]
y <- itempartable[ I + 1:I, c("item", "b") ]
res1d <- sirt::equating.rasch( x, y )
round( res1d$B.est, 3 )
  ##     Mean.Mean Haebara Stocking.Lord
  ##   1     0.032   0.032         0.029

#*************************
# Model 2: Linking using the 2PL model
I <- ncol(dat.male)
mod2m <- sirt::rasch.mml2( dat.male, est.a=1:I)
mod2f <- sirt::rasch.mml2( dat.female, est.a=1:I)

# create objects for invariance.alignment
nu <- rbind( mod2m$item$thresh, mod2f$item$thresh )
colnames(nu) <- mod2m$item$item
rownames(nu) <- c("male", "female")
lambda <- rbind( mod2m$item$a, mod2f$item$a )
colnames(lambda) <- mod2m$item$item
rownames(lambda) <- c("male", "female")

res2a <- sirt::invariance.alignment( lambda, nu, align.scale=c( .3, .5 ) )
summary(res2a)

res2b <- sirt::invariance.alignment( lambda, nu, align.scale=c( .3, .5 ),
                align.pow=c(1,1) )
summary(res2b)

# compare results with Haberman linking
I <- ncol(dat.male)
itempartable <- data.frame( "study"=rep( c("male", "female"), each=I ) )
itempartable$item <- c( paste0(mod2m$item$item),  paste0(mod2f$item$item ) )
itempartable$a <- c( mod2m$item$a, mod2f$item$a )
itempartable$b <- c( mod2m$item$b, mod2f$item$b )
# estimate linking parameters
res2c <- sirt::linking.haberman( itempars=itempartable )

#############################################################################
# EXAMPLE 6: Data from Asparouhov & Muthen (2014) simulation study
#############################################################################

G <- 3  # number of groups
I <- 5  # number of items
# define lambda and nu parameters
lambda <- matrix(1, nrow=G, ncol=I)
nu <- matrix(0, nrow=G, ncol=I)

# define size of noninvariance
dif <- 1

#- 1st group: N(0,1)
lambda[1,3] <- 1+dif*.4; nu[1,5] <- dif*.5

#- 2nd group: N(0.3,1.5)
gg <- 2 ; mu <- .3; sigma <- sqrt(1.5)
lambda[gg,5] <- 1-.5*dif; nu[gg,1] <- -.5*dif
nu[gg,] <- nu[gg,] + mu*lambda[gg,]
lambda[gg,] <- lambda[gg,] * sigma

#- 3nd group: N(.8,1.2)
gg <- 3 ; mu <- .8; sigma <- sqrt(1.2)
lambda[gg,4] <- 1-.7*dif; nu[gg,2] <- -.5*dif
nu[gg,] <- nu[gg,] + mu*lambda[gg,]
lambda[gg,] <- lambda[gg,] * sigma

# define alignment scale
align.scale <- c(.2,.4)   # Asparouhov and Muthen use c(1,1)
# define alignment powers
align.pow <- c(.5,.5)   # as in Asparouhov and Muthen

#*** estimate alignment parameters
mod1 <- sirt::invariance.alignment( lambda, nu, eps=.01, optimizer="optim",
            align.scale=align.scale, align.pow=align.pow, center=FALSE )
summary(mod1)

#--- find parameter constraints for prespecified tolerance
cmod1 <- sirt::invariance_alignment_constraints(model=mod1, nu_parm_tol=.4,
            lambda_parm_tol=.2 )
summary(cmod1)

#############################################################################
# EXAMPLE 7: Similar to Example 6, but with data simulation and CFA estimation
#############################################################################

#--- data simulation

set.seed(65)
G <- 3  # number of groups
I <- 5  # number of items
# define lambda and nu parameters
lambda <- matrix(1, nrow=G, ncol=I)
nu <- matrix(0, nrow=G, ncol=I)
err_var <- matrix(1, nrow=G, ncol=I)

# define size of noninvariance
dif <- 1
#- 1st group: N(0,1)
lambda[1,3] <- 1+dif*.4; nu[1,5] <- dif*.5
#- 2nd group: N(0.3,1.5)
gg <- 2 ;
lambda[gg,5] <- 1-.5*dif; nu[gg,1] <- -.5*dif
#- 3nd group: N(.8,1.2)
gg <- 3
lambda[gg,4] <- 1-.7*dif; nu[gg,2] <- -.5*dif
#- define distributions of groups
mu <- c(0,.3,.8)
sigma <- sqrt(c(1,1.5,1.2))
N <- rep(1000,3) # sample sizes per group

#* simulate data
dat <- sirt::invariance_alignment_simulate(nu, lambda, err_var, mu, sigma, N)
head(dat)

#--- estimate CFA models
pars <- sirt::invariance_alignment_cfa_config(dat[,-1], group=dat$group)
print(pars)

#--- invariance alignment
# define alignment scale
align.scale <- c(.2,.4)
# define alignment powers
align.pow <- c(.5,.5)
mod1 <- sirt::invariance.alignment( lambda=pars$lambda, nu=pars$nu, eps=.01,
            optimizer="optim", align.scale=align.scale, align.pow=align.pow, center=FALSE)
#* find parameter constraints for prespecified tolerance
cmod1 <- sirt::invariance_alignment_constraints(model=mod1, nu_parm_tol=.4,
            lambda_parm_tol=.2 )
summary(cmod1)

#--- estimate CFA models with sampling weights

#* simulate weights
weights <- stats::runif(sum(N), 0, 2)
#* estimate models
pars2 <- sirt::invariance_alignment_cfa_config(dat[,-1], group=dat$group, weights=weights)
print(pars2$nu)
print(pars$nu)

#--- estimate one-parameter model
pars <- sirt::invariance_alignment_cfa_config(dat[,-1], group=dat$group, model="1PM")
print(pars)

#############################################################################
# EXAMPLE 8: Computation of standard errors
#############################################################################

G <- 3  # number of groups
I <- 5  # number of items
# define lambda and nu parameters
lambda <- matrix(1, nrow=G, ncol=I)
nu <- matrix(0, nrow=G, ncol=I)

# define size of noninvariance
dif <- 1

mu1 <- c(0,.3,.8)
sigma1 <- c(1,1.25,1.1)

#- 1st group
lambda[1,3] <- 1+dif*.4; nu[1,5] <- dif*.5

#- 2nd group
gg <- 2
lambda[gg,5] <- 1-.5*dif; nu[gg,1] <- -.5*dif

#- 3nd group
gg <- 3
lambda[gg,4] <- 1-.7*dif; nu[gg,2] <- -.5*dif

dat <- sirt::invariance_alignment_simulate(nu=nu, lambda=lambda, err_var=1+0*lambda,
                mu=mu1, sigma=sigma1, N=500, output="data", exact=TRUE)

#* estimate CFA
res <- sirt::invariance_alignment_cfa_config(dat=dat[,-1], group=dat$group )

#- perform invariance alignment
eps <- .001
align.pow <- 0.5*rep(1,2)
lambda <- res$lambda
nu <- res$nu
mod1 <- sirt::invariance.alignment( lambda=lambda, nu=nu, eps=eps, optimizer="optim",
             align.pow=align.pow, meth=meth, vcov=res$vcov)
# variance matrix and standard errors
mod1$vcov
sqrt(diag(mod1$vcov))

## End(Not run)

[Package sirt version 4.1-15 Index]