Description Usage Arguments Details Value Author(s) References See Also Examples
For a dataset containing a time variable, a scalar response variable,
and an optional subject identification variable, obtains least squares
estimates of the coefficients of a restricted cubic spline function or
a linear regression in time after adjusting for subject effects
through the use of subject dummy variables. Then the fit is
bootstrapped B
times, either by treating time and subject ID as
fixed (i.e., conditioning the analysis on them) or as random
variables. For the former, the residuals from the original model fit
are used as the basis of the bootstrap distribution. For the latter,
samples are taken jointly from the time, subject ID, and response
vectors to obtain unconditional distributions.
If a subject id
variable is given, the bootstrap sampling will
be based on samples with replacement from subjects rather than from
individual data points. In other words, either none or all of a given
subject's data will appear in a bootstrap sample. This cluster
sampling takes into account any correlation structure that might exist
within subjects, so that confidence limits are corrected for
withinsubject correlation. Assuming that ordinary least squares
estimates, which ignore the correlation structure, are consistent
(which is almost always true) and efficient (which would not be true
for certain correlation structures or for datasets in which the number
of observation times vary greatly from subject to subject), the
resulting analysis will be a robust, efficient repeated measures
analysis for the onesample problem.
Predicted values of the fitted models are evaluated by default at a grid of 100 equally spaced time points ranging from the minimum to maximum observed time points. Predictions are for the average subject effect. Pointwise confidence intervals are optionally computed separately for each of the points on the time grid. However, simultaneous confidence regions that control the level of confidence for the entire regression curve lying within a band are often more appropriate, as they allow the analyst to draw conclusions about nuances in the mean time response profile that were not stated apriori. The method of Tibshirani (1997) is used to easily obtain simultaneous confidence sets for the set of coefficients of the spline or linear regression function as well as the average intercept parameter (over subjects). Here one computes the objective criterion (here both the 2 log likelihood evaluated at the bootstrap estimate of beta but with respect to the original design matrix and response vector, and the sum of squared errors in predicting the original response vector) for the original fit as well as for all of the bootstrap fits. The confidence set of the regression coefficients is the set of all coefficients that are associated with objective function values that are less than or equal to say the 0.95 quantile of the vector of \code{B} + 1 objective function values. For the coefficients satisfying this condition, predicted curves are computed at the time grid, and minima and maxima of these curves are computed separately at each time point toderive the final simultaneous confidence band.
By default, the log likelihoods that are computed for obtaining the
simultaneous confidence band assume independence within subject. This
will cause problems unless such log likelihoods have very high rank
correlation with the log likelihood allowing for dependence. To allow
for correlation or to estimate the correlation function, see the
cor.pattern
argument below.
1 2 3 4 5 6 7 8 9 10 11 12 13 14 15 16 17 18 19 20 21 22 23 24 25  rm.boot(time, y, id=seq(along=time), subset,
plot.individual=FALSE,
bootstrap.type=c('x fixed','x random'),
nk=6, knots, B=500, smoother=supsmu,
xlab, xlim, ylim=range(y),
times=seq(min(time), max(time), length=100),
absorb.subject.effects=FALSE,
rho=0, cor.pattern=c('independent','estimate'), ncor=10000,
...)
## S3 method for class 'rm.boot'
plot(x, obj2, conf.int=.95,
xlab=x$xlab, ylab=x$ylab,
xlim, ylim=x$ylim,
individual.boot=FALSE,
pointwise.band=FALSE,
curves.in.simultaneous.band=FALSE,
col.pointwise.band=2,
objective=c('2 log L','sse','dep 2 log L'), add=FALSE, ncurves,
multi=FALSE, multi.method=c('color','density'),
multi.conf =c(.05,.1,.2,.3,.4,.5,.6,.7,.8,.9,.95,.99),
multi.density=c( 1,90,80,70,60,50,40,30,20,10, 7, 4),
multi.col =c( 1, 8,20, 5, 2, 7,15,13,10,11, 9, 14),
subtitles=TRUE, ...)

time 
numeric time vector 
y 
continuous numeric response vector of length the same as 
x 
an object returned from 
id 
subject ID variable. If omitted, it is assumed that each timeresponse pair is measured on a different subject. 
subset 
subset of observations to process if not all the data 
plot.individual 
set to 
bootstrap.type 
specifies whether to treat the time and subject ID variables as fixed or random 
nk 
number of knots in the restricted cubic spline function fit. The number of knots may be 0 (denoting linear regression) or an integer greater than 2 in which k knots results in \var{k}  1 regression coefficients excluding the intercept. The default is 6 knots. 
knots 
vector of knot locations. May be specified if 
B 
number of bootstrap repetitions. Default is 500. 
smoother 
a smoothing function that is used if 
xlab 
label for xaxis. Default is 
xlim 
specifies xaxis plotting limits. Default is to use range of times
specified to 
ylim 
for 
times 
a sequence of times at which to evaluated fitted values and
confidence limits. Default is 100 equally spaced points in the
observed range of 
absorb.subject.effects 
If 
rho 
The loglikelihood function that is used as the basis of
simultaneous confidence bands assumes normality with independence
within subject. To check the robustness of this assumption, if

cor.pattern 
More generally than using an equalcorrelation structure, you can
specify a function of two time vectors that generates as many
correlations as the length of these vectors. For example,

ncor 
the maximum number of pairs of time values used in estimating the
correlation function if 
... 
other arguments to pass to 
obj2 
a second object created by 
conf.int 
the confidence level to use in constructing simultaneous, and optionally pointwise, bands. Default is 0.95. 
ylab 
label for yaxis. Default is the 
individual.boot 
set to 
pointwise.band 
set to 
curves.in.simultaneous.band 
set to 
col.pointwise.band 
color for the pointwise confidence band. Default is 2, which defaults to red for default Windows SPLUS setups. 
objective 
the default is to use the 2 times log of the Gaussian likelihood
for computing the simultaneous confidence region. If neither

add 
set to 
ncurves 
when using 
multi 
set to 
multi.method 
specifies the method of shading when 
multi.conf 
vector of confidence levels, in ascending order. Default is to use 12 confidence levels ranging from 0.05 to 0.99. 
multi.density 
vector of densities in lines per inch corresponding to

multi.col 
vector of colors corresponding to 
subtitles 
set to 
Observations having missing time
or y
are excluded from
the analysis.
As most repeated measurement studies consider the times as design
points, the fixed covariable case is the default. Bootstrapping the
residuals from the initial fit assumes that the model is correctly
specified. Even if the covariables are fixed, doing an unconditional
bootstrap is still appropriate, and for large sample sizes
unconditional confidence intervals are only slightly wider than
conditional ones. For moderate to small sample sizes, the
bootstrap.type="x random"
method can be fairly conservative.
If not all subjects have the same number of observations (after
deleting observations containing missing values) and if
bootstrap.type="x fixed"
, bootstrapped residual vectors may
have a length m that is different from the number of original
observations n. If \var{m} > \var{n} for a bootstrap
repetition, the first n elements of the randomly drawn residuals
are used. If \var{m} < \var{n}, the residual vector is appended
with a random sample with replacement of length \var{n} 
\var{m} from itself. A warning message is issued if this happens.
If the number of time points per subject varies, the bootstrap results
for bootstrap.type="x fixed"
can still be invalid, as this
method assumes that a vector (over subjects) of all residuals can be
added to the original yhats, and varying number of points will cause
misalignment.
For bootstrap.type="x random"
in the presence of significant
subject effects, the analysis is approximate as the subjects used in
any one bootstrap fit will not be the entire list of subjects. The
average (over subjects used in the bootstrap sample) intercept is used
from that bootstrap sample as a predictor of average subject effects
in the overall sample.
Once the bootstrap coefficient matrix is stored by rm.boot
,
plot.rm.boot
can be run multiple times with different options
(e.g, different confidence levels).
See bootcov
in the rms library for a general
approach to handling repeated measurement data for ordinary linear
models, binary and ordinal models, and survival models, using the
unconditional bootstrap. bootcov
does not handle bootstrapping
residuals.
an object of class rm.boot
is returned by rm.boot
. The
principal object stored in the returned object is a matrix of
regression coefficients for the original fit and all of the bootstrap
repetitions (object Coef
), along with vectors of the
corresponding 2 log likelihoods are sums of squared errors. The
original fit object from lm.fit.qr
is stored in
fit
. For this fit, a cell means model is used for the
id
effects.
plot.rm.boot
returns a list containing the vector of times used
for plotting along with the overall fitted values, lower and upper
simultaneous confidence limits, and optionally the pointwise
confidence limits.
Frank Harrell
Department of Biostatistics
Vanderbilt University School of Medicine
f.harrell@vanderbilt.edu
Feng Z, McLerran D, Grizzle J (1996): A comparison of statistical methods for clustered data analysis with Gaussian error. Stat in Med 15:1793–1806.
Tibshirani R, Knight K (1997):Model search and inference by bootstrap
"bumping". Technical Report, Department of Statistics, University of Toronto.
http://wwwstat.stanford.edu/~tibs. Presented at the Joint Statistical
Meetings, Chicago, August 1996.
Efron B, Tibshirani R (1993): An Introduction to the Bootstrap. New York: Chapman and Hall.
Diggle PJ, Verbyla AP (1998): Nonparametric estimation of covariance structure in logitudinal data. Biometrics 54:401–415.
Chapman IM, Hartman ML, et al (1997): Effect of aging on the sensitivity of growth hormone secretion to insulinlike growth factorI negative feedback. J Clin Endocrinol Metab 82:2996–3004.
Li Y, Wang YG (2008): Smooth bootstrap methods for analysis of longitudinal data. Stat in Med 27:937953. (potential improvements to cluster bootstrap; not implemented here)
rcspline.eval
, lm
, lowess
,
supsmu
, bootcov
,
units
, label
, polygon
,
reShape
1 2 3 4 5 6 7 8 9 10 11 12 13 14 15 16 17 18 19 20 21 22 23 24 25 26 27 28 29 30 31 32 33 34 35 36 37 38 39 40 41 42 43 44 45 46 47 48 49 50 51 52 53 54 55 56 57 58 59 60 61 62 63 64 65 66 67 68 69 70 71 72 73 74 75 76 77 78 79 80 81 82 83 84 85 86 87 88 89 90 91 92 93 94 95 96 97 98 99 100 101 102 103 104 105 106 107 108 109 110 111 112 113 114 115 116 117 118 119 120 121 122 123 124 125 126 127 128 129 130 131 132 133 134  # Generate multivariate normal responses with equal correlations (.7)
# within subjects and no correlation between subjects
# Simulate realizations from a piecewise linear population timeresponse
# profile with large subject effects, and fit using a 6knot spline
# Estimate the correlation structure from the residuals, as a function
# of the absolute time difference
# Function to generate n pvariate normal variates with mean vector u and
# covariance matrix S
# Slight modification of function written by Bill Venables
# See also the builtin function rmvnorm
mvrnorm < function(n, p = 1, u = rep(0, p), S = diag(p)) {
Z < matrix(rnorm(n * p), p, n)
t(u + t(chol(S)) %*% Z)
}
n < 20 # Number of subjects
sub < .5*(1:n) # Subject effects
# Specify functional form for time trend and compute nonstochastic component
times < seq(0, 1, by=.1)
g < function(times) 5*pmax(abs(times.5),.3)
ey < g(times)
# Generate multivariate normal errors for 20 subjects at 11 times
# Assume equal correlations of rho=.7, independent subjects
nt < length(times)
rho < .7
set.seed(19)
errors < mvrnorm(n, p=nt, S=diag(rep(1rho,nt))+rho)
# Note: first random number seed used gave rise to mean(errors)=0.24!
# Add E[Y], error components, and subject effects
y < matrix(rep(ey,n), ncol=nt, byrow=TRUE) + errors +
matrix(rep(sub,nt), ncol=nt)
# String out data into long vectors for times, responses, and subject ID
y < as.vector(t(y))
times < rep(times, n)
id < sort(rep(1:n, nt))
# Show lowess estimates of time profiles for individual subjects
f < rm.boot(times, y, id, plot.individual=TRUE, B=25, cor.pattern='estimate',
smoother=lowess, bootstrap.type='x fixed', nk=6)
# In practice use B=400 or 500
# This will compute a dependentstructure loglikelihood in addition
# to one assuming independence. By default, the dep. structure
# objective will be used by the plot method (could have specified rho=.7)
# NOTE: Estimating the correlation pattern from the residual does not
# work in cases such as this one where there are large subject effects
# Plot fits for a random sample of 10 of the 25 bootstrap fits
plot(f, individual.boot=TRUE, ncurves=10, ylim=c(6,8.5))
# Plot pointwise and simultaneous confidence regions
plot(f, pointwise.band=TRUE, col.pointwise=1, ylim=c(6,8.5))
# Plot population response curve at average subject effect
ts < seq(0, 1, length=100)
lines(ts, g(ts)+mean(sub), lwd=3)
## Not run:
#
# Handle a 2sample problem in which curves are fitted
# separately for males and females and we wish to estimate the
# difference in the timeresponse curves for the two sexes.
# The objective criterion will be taken by plot.rm.boot as the
# total of the two sums of squared errors for the two models
#
knots < rcspline.eval(c(time.f,time.m), nk=6, knots.only=TRUE)
# Use same knots for both sexes, and use a times vector that
# uses a range of times that is included in the measurement
# times for both sexes
#
tm < seq(max(min(time.f),min(time.m)),
min(max(time.f),max(time.m)),length=100)
f.female < rm.boot(time.f, bp.f, id.f, knots=knots, times=tm)
f.male < rm.boot(time.m, bp.m, id.m, knots=knots, times=tm)
plot(f.female)
plot(f.male)
# The following plots female minus male response, with
# a sequence of shaded confidence band for the difference
plot(f.female,f.male,multi=TRUE)
# Do 1000 simulated analyses to check simultaneous coverage
# probability. Use a null regression model with Gaussian errors
n.per.pt < 30
n.pt < 10
null.in.region < 0
for(i in 1:1000) {
y < rnorm(n.pt*n.per.pt)
time < rep(1:n.per.pt, n.pt)
# Add the following line and add ,id=id to rm.boot to use clustering
# id < sort(rep(1:n.pt, n.per.pt))
# Because we are ignoring patient id, this simulation is effectively
# using 1 point from each of 300 patients, with times 1,2,3,,,30
f < rm.boot(time, y, B=500, nk=5, bootstrap.type='x fixed')
g < plot(f, ylim=c(1,1), pointwise=FALSE)
null.in.region < null.in.region + all(g$lower<=0 & g$upper>=0)
prn(c(i=i,null.in.region=null.in.region))
}
# Simulation Results: 905/1000 simultaneous confidence bands
# fully contained the horizontal line at zero
## End(Not run)

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