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code_1b_helper_functions.R
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code_1b_helper_functions.R
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##=============================================================================##
## Define Helper Functions
##=============================================================================##
## Trim function removes leading and trailing whitespace
trim <- function (x) gsub("^\\s+|\\s+$", "", x)
## Add alpha for maps
add.alpha <- function(col, alpha=1){
if(missing(col))
stop("Please provide a vector of colours.")
apply(sapply(col, col2rgb)/255, 2,
function(x)
rgb(x[1], x[2], x[3], alpha=alpha))
}
## Process cv.glmnet output for covariate selection procedure
grabvars <- function(x,s="lambda.1se") {
coef.out <- coef(x, s=s, exact=TRUE)
inds <- which(coef.out != 0)
vars <- as.data.frame(cbind(rownames(coef.out)[inds], coef.out[inds,], abs(coef.out[inds,])))
vars <- vars[order(vars[,3], decreasing=TRUE),]
colnames(vars) <- c("variable","coef","abs.coef")
rownames(vars) <- NULL
return(list(vars=vars, nvars=nrow(vars)-1))
}
## Bootstrap estimator for covariate adjustment
## Estimate the empirical sandwich variance for each draw, since the
## variance estimate is needed to obtain the Studentized bootstrap CIs
bs = function(data, sims=5000, zvar, Yvar, z0, z1, X0, X1, ipwvar,ptvar){
z1 <- as.numeric(z1); z0 <- as.numeric(z0)
# subset data
data <- data[data[[zvar]] %in% c(z1,z0),]
# listwise deletion if obs includes missing data
data <- data[apply(data[,names(data) %in% c(Yvar,X0,X1)],1,function(x) sum(is.na(x))==0),]
# index rows so resampling can be done correctly
data$i <- 1:nrow(data)
# ipw variable
data$ipw2g <- data[[ipwvar]]
sapply(1:sims, function(j) {
cat(j," ")
# estimate betas for X from resample of control data
i0 = sample(data$i[data[[zvar]]==z0], sum(data[[zvar]]==z0), replace = TRUE)
b0 = lm(paste(Yvar, " ~ ", paste(X0, collapse="+")), data = data[i0,], weights=ipw2g)
# estimate betas for X from resample of treatment data
i1 = sample(data$i[data[[zvar]]==z1], sum(data[[zvar]]==z1), replace = TRUE)
b1 = lm(paste(Yvar," ~ ", paste(X1, collapse="+")), data = data[i1,], weights=ipw2g)
# estimated treatment effect from resampled data
data2 <- rbind(data[i1,], data[i0,])
#mean(predict(b1, newdata=data2, se.fit=TRUE, type="response")$fit) - mean(predict(b0, newdata=data2, se.fit=TRUE, type="response")$fit)
esv2g(data=data2,zvar=zvar,Yvar=Yvar,z0=z0,z1=z1,covs0=X0,covs1=X1,ipwvar=ipwvar,ptvar=ptvar)
})
}
## Empirical sandwich variance estimator
## from Yuan, S., Zhang, H.H., and Davidian, M. (2012). Variable selection for
## covariate-adjusted semiparametric inference in randomized clinical trials. Statistics in Medicine 31, 3789-3804
esv2g <- function(data,zvar,Yvar,covs0,covs1,z1,z0,ipwvar,ptvar) {
z1 <- as.numeric(z1); z0 <- as.numeric(z0)
# subset data
sub <- data[data[[zvar]] %in% c(z1,z0),]
# listwise deletion if obs includes missing data
sub <- sub[apply(sub[,names(sub) %in% c(Yvar,covs0,covs1)],1,function(x) sum(is.na(x))==0),]
# define regression models by arm
model0 <- paste(Yvar, "~", paste(covs0, collapse=" + "))
model1 <- paste(Yvar, "~", paste(covs1, collapse=" + "))
# fit models by arm (this will undo shrinkage from lasso)
sub$ipw.2g <- sub[[ipwvar]]
fit0 <- lm(formula=model0, data=sub[sub[[zvar]]==z0,], weights=ipw.2g)
fit1 <- lm(formula=model1, data=sub[sub[[zvar]]==z1,], weights=ipw.2g)
# predict values using actual data, use data across both treatment arms
predY0 <- predict(fit0, newdata=sub, se.fit=TRUE, type="response")
predY1 <- predict(fit1, newdata=sub, se.fit=TRUE, type="response")
# grab vector of predicted values
predY0.i <- predY0$fit
predY1.i <- predY1$fit
# calculate mean predicted response (regression adjusted) by arm
mean.predY0 <- mean(predY0.i)
mean.predY1 <- mean(predY1.i)
# calculate covariate adjusted estimate of the ATE
b.hat <- mean.predY1 - mean.predY0
# calculate terms needed to construct the empirical sandwich variance estimate
n0 <- nrow(sub[sub[[zvar]]==z0,]) # number of obs in control
n1 <- nrow(sub[sub[[zvar]]==z1,]) # number of obs in treatment
n.tot <- n1 + n0 # total number of observations
z.i <- ifelse(sub[[zvar]]==z1, 1, 0) # vector of treatment assignments, recoded 0 and 1
pi.i <- sub[[ptvar]] # vector of treatment assignment probabilities, by unit
y.i <- sub[[Yvar]] # vector of observed outcomes
meanY0 <- mean(sub[[Yvar]][sub[[zvar]]==z0], na.rm=TRUE) # mean observed Y0
meanY1 <- mean(sub[[Yvar]][sub[[zvar]]==z1], na.rm=TRUE) # mean observed Y1
# take the first derivative of q*_{k,xi}(X, xi*_k) with respect to the vector xi*_k
# which is just the sum of the X_i's (for variables w/ nonzero coefs from the lasso) by unit
q0xi.star <- apply(as.matrix(sub[,names(sub)%in%covs0]),MARGIN=1,function(x) sum(x,na.rm=TRUE))
q1xi.star <- apply(as.matrix(sub[,names(sub)%in%covs1]),MARGIN=1,function(x) sum(x,na.rm=TRUE))
# code up D.hats, W.hats, phi.hats
D0.hat <- (1/n.tot) * sum( (z.i - pi.i) * t(q0xi.star) )
D1.hat <- (1/n.tot) * sum( (z.i - pi.i) * t(q1xi.star) )
W0.hat <- (1/n.tot) * sum( (1-z.i) * q0xi.star * t(q0xi.star) )
W1.hat <- (1/n.tot) * sum( (1-z.i) * q1xi.star * t(q1xi.star) )
phi0.hat.i <- z.i * (y.i - predY0.i) * q0xi.star
phi1.hat.i <- z.i * (y.i - predY1.i) * q1xi.star
# code up empirical sandwich variance estimator (eq 13)
var.es <- sum((((1/n1)*z.i - (1/n0)*(1-z.i))*y.i - (1/n.tot)*b.hat -
(z.i - pi.i)*((1/n0)*predY0.i + (1/n1)*predY1.i) -
(z.i - pi.i)*((1/n0)*(meanY1-mean.predY1) + (1/n1)*(meanY0-mean.predY0)) +
( (1/n1)*D1.hat*(1/W1.hat)*phi1.hat.i + (1/n0)*D0.hat*(1/W0.hat)*phi0.hat.i ))^2)
# return covariate adjusted ATE and empirical sandwich variance estimates and SE estimate
out <- list(est=b.hat, esv=var.es, se=sqrt(var.es))
return(out)
}
# extract p value from F test for lm
lmp <- function (modelobject) {
if (class(modelobject) != "lm") stop("Not an object of class 'lm' ")
f <- summary(modelobject)$fstatistic
p <- pf(f[1],f[2],f[3],lower.tail=F)
attributes(p) <- NULL
return(p)
}
# function to create balance tables
balanceTables <- function(d, z, xcon, xcat, weight=NULL){
require(Hmisc) # needed for weighted variance calculation
if(is.null(weight)){ # IF UNWEIGHTED MEANS AND PROPORTIONS
# for all continuous predictors, output means and sds
xcon_out <- list()
for(i in 1:length(xcon)){
out_means = round(unlist(as.list(by(d, d[,z], function(x) mean(x[,xcon[i]], na.rm=TRUE)))), 3)
out_sds = paste0("(",round(unlist(as.list(by(d, d[,z], function(x) sd(x[,xcon[i]], na.rm=TRUE)))), 3),")")
out_sub = cbind(c(xcon[i], NA), rbind(out_means, out_sds))
rownames(out_sub) = NULL
xcon_out[[i]] = rbind(out_sub, rep(NA, ncol(out_sub)))
}
xcon_out = do.call(rbind, xcon_out)
xcon_out = as.data.frame(xcon_out, stringsAsFactors=FALSE)
names(xcon_out) = c("Variable", paste0("Z=", names(xcon_out)[2:ncol(xcon_out)]))
# for all categorical variables, output proportion in each level and sds
xcat_out <- list()
for(i in 1:length(xcat)){
temp_out = as.list(by(d, d[,z], function(x) {
counts = table(x[,xcat[i]])
props = table(x[,xcat[i]])/nrow(x)
cat_names = names(table(x[,xcat[i]]))
ses = round(sqrt(props * (1 - props) / nrow(x)), 3)
props = round(props, 3)
return(cbind(cat_names, props, ses, counts))
}))
for(j in 1:length(temp_out)){
colnames(temp_out[[j]]) = paste0(colnames(temp_out[[j]]), ".z", names(temp_out)[j])
}
xcat_out[[i]] = do.call(cbind, temp_out)
}
for(i in 1:length(xcat_out)){
xcat_out[[i]] <- rbind(c(xcat[i], rep(NA, ncol(xcat_out[[i]])-1)),
xcat_out[[i]])
}
dropif = paste0("cat_names.z", names(table(d[,z])) )
dropif = dropif[dropif != "cat_names.z0"]
xcat_out = do.call(rbind, xcat_out)
rownames(xcat_out) = NULL
xcat_out = as.data.frame(xcat_out, stringsAsFactors=FALSE)
xcat_out = xcat_out[,!(names(xcat_out) %in% dropif)]
names(xcat_out)[1] = "Variable"
names(xcat_out) = gsub("props", "Pct", names(xcat_out), fixed=TRUE)
names(xcat_out) = gsub("ses", "SE", names(xcat_out), fixed=TRUE)
names(xcat_out) = gsub("counts", "N", names(xcat_out), fixed=TRUE)
} else { # IF WEIGHTED MEANS AND PROPORTIONS
# for all continuous predictors, output means and sds
xcon_out <- list()
for(i in 1:length(xcon)){
out_means = round(unlist(as.list(by(d, d[,z], function(x) weighted.mean(x[,xcon[i]], x[,weight], na.rm=TRUE)))), 3)
out_sds = paste0("(",round(unlist(as.list(by(d, d[,z], function(x) sqrt(wtd.var(x[,xcon[i]], x[,weight], na.rm=TRUE)) ))), 3),")")
out_sub = cbind(c(xcon[i], NA), rbind(out_means, out_sds))
rownames(out_sub) = NULL
xcon_out[[i]] = rbind(out_sub, rep(NA, ncol(out_sub)))
}
xcon_out = do.call(rbind, xcon_out)
xcon_out = as.data.frame(xcon_out, stringsAsFactors=FALSE)
names(xcon_out) = c("Variable", paste0("Z=", names(xcon_out)[2:ncol(xcon_out)]))
# for all categorical variables, output proportion in each level and sds
xcat_out <- list()
for(i in 1:length(xcat)){ # for each variable
cat_vals = names(table(d[,xcat[i]]))
z_vals = names(table(d[,z]))
wt_p_numer_out = wt_p_denom_out = wt_p_out = wt_p_se_out = matrix(NA, nrow=length(cat_vals), ncol=length(z_vals))
for(j in 1:length(z_vals)){
for(k in 1:length(cat_vals)){
wt_p_numer = sum(d[d[,z] == z_vals[j] & d[,xcat[i]]==cat_vals[k], weight], na.rm=TRUE)
wt_p_denom = sum(d[d[,z] == z_vals[j] ,weight], na.rm=TRUE)
wt_p = wt_p_numer / wt_p_denom
wt_p_se = sqrt(wt_p * (1 - wt_p) / nrow( d[d[,z]==z_vals[j],] ))
wt_p_numer_out[k,j] = wt_p_numer
wt_p_denom_out[k,j] = wt_p_denom
wt_p_out[k,j] = wt_p
wt_p_se_out[k,j] = wt_p_se
}
}
tab_out = NULL
for(j in 1:ncol(wt_p_out)){
tab_out = cbind(tab_out, round( wt_p_out[,j], 3), round(wt_p_se_out[,j], 3), round(wt_p_numer_out[,j], 3))
}
tab_out = cbind(cat_vals, tab_out)
colnames(tab_out) = c("Variable", paste0(rep(c("Pct", "SE", "Wtd N"), length(z_vals)), ".z", rep(z_vals, each=3)))
tab_out = rbind(c(xcat[i], rep(NA, ncol(tab_out)-1)),
tab_out)
xcat_out[[i]] = tab_out
}
xcat_out = do.call(rbind, xcat_out)
rownames(xcat_out) = NULL
xcat_out = as.data.frame(xcat_out, stringsAsFactors=FALSE)
}
# Combine output balance labels in single list to return
out = list(bt_con = xcon_out,
bt_cat = xcat_out)
return(out)
}