This vignette documents the use of the MANOVA.RM package for the analysis of semi-parametric repeated measures designs and multivariate data.
The package consists of two parts - one for repeated measurements and one for multivariate data - which will be explained in detail below. Both functions calculate the Wald-type statistic
(WTS) as well as the ANOVA-type statistic (ATS) for repeated measures and a modification thereof (MATS) for multivariate data based on means. These test statistics can be used for arbitrary semi-parametric designs, even with unequal covariance matrices among groups
and small sample sizes. For a short overview of the test statistics and corresponding references see the next section.
Furthermore, different resampling approaches are provided in order to improve the
small sample behavior of the test statistics.
The WTS requires non-singular covariance matrices. If the covariance matrix is singular, a warning is returned.
For detailed explanations and examples, see also the preprint Friedrich, Konietschke and Pauly (2018) on arXiv.
We consider the following model \[ X_{ik} = \mu_i + \varepsilon_{ik} \] for observation vectors from group \(i\) and individual \(k\). Here, \(\mu_i\) denotes the group mean which we wish to infer and \(\varepsilon_{ik}\) are the common error terms with expectation 0 and existing (co-)variances. We do not need to assume normally distributed errors for these methods and the covariances may be unequal between groups. Null hypotheses are formulated via contrast matrices, i.e., as \(H \mu = 0\), where the rows of \(H\) sum to zero. Then the Wald-type statistic (WTS) is a quadratic form in the estimated mean vector involving the Moore-Penrose inverse of the (transformed) empirical covariance matrix. Under the null hypothesis the WTS is asymptotically \(\chi^2\) distributed with rank(H) degrees of freedom. However, this approximation is only valid for large sample sizes, see e.g. Brunner (2001). We therefore recommend to use a resampling approach as proposed by Konietschke et al.(2015) or Friedrich et al.(2017).
Since the WTS requires non-singular covariance matrices, two other test statistics have been proposed: the ATS for repeated measures designs (Brunner, 2001) and the MATS for multivariate data (Friedrich and Pauly, 2018). The ATS is a scaled quadratic form in the mean vector, which is usually approximated by an F-distribution with estimated degrees of freedom. This approach is also implemented in the SAS PROC Mixed procedure. However, it is rather conservative for small sample sizes and does not provide an aysmptotic level \(\alpha\) test.
The MATS for multivariate data has the advantage of being invariant under scale transformations of the data, an important feature for multivariate data. Since its asymptotic distribution involves unknown parameters, we again propose to use bootstrap approaches instead (Friedrich and Pauly, 2018).
MANOVA and MANOVA.wide is the format of the data: For MANOVA data need to be in long format (one row per measurement), whereas MANOVA.wide is for data in wide format (one row per individual).Note that a combination of both types of data, i.e., multivariate longitudinal data, can not yet be analyzed with MANOVA.RM.
RM functionThe RM function calculates the WTS and ATS in a repeated measures design with an arbitrary number of crossed whole-plot (between subjects) and
sub-plot (within subjects) factors.
The resampling methods provided are a permutation procedure, a parametric bootstrap approach and a
wild bootstrap using Rademacher weights. The permutation procedure provides no valid approach for the ATS and is thus not implemented.
For illustration purposes, we consider the data set o2cons, which is included in MANOVA.RM.
library(MANOVA.RM)
data(o2cons)
The data set contains measurements on the oxygen consumption of leukocytes in the presence and absence of inactivated staphylococci at three consecutive time points. More details on the study and the statistical model can be found in Friedrich et al. (2017). Due to the study design, both time and staphylococci are sub-plot factors while the treatment (Verum vs. Placebo) is a whole-plot factor.
head(o2cons)
## O2 Staphylococci Time Group Subject
## 1 1.48 1 6 P 1
## 2 2.81 1 12 P 1
## 3 3.56 1 18 P 1
## 4 1.04 0 6 P 2
## 5 2.07 0 12 P 2
## 6 2.81 0 18 P 2
We will now analyze this data using the RM function.
The RM function takes as arguments:
formula: A formula consisting of the outcome variable on the left hand side of a ~ operator and the factor
variables of interest on the right hand side. An interaction term must be specified. The time variable must be the last factor in the formula.data: A data.frame containing the variables in formula.subject: The column name of the subjects variable in the data frame.no.subf: The number of sub-plot factors, default is 1.iter: The number of iterations for the resampling approach. Default value is 10,000.alpha: The significance level, default is 0.05.resampling: The resampling method, one of 'Perm', 'paramBS' or 'WildBS'. Default is
set to 'Perm'.CPU: The number of cores used for parallel computing. If omitted, cores are detected automatically.seed: A random seed for the resampling procedure. If omitted, no reproducible seed is set.CI.method: The method for calculating the quantiles used for the confidence intervals,
either 't-quantile' (the default) or 'resampling' (based on quantile of the resampled WTS).dec: The number of decimals the results should be rounded to. Default is 3.model1 <- RM(O2 ~ Group * Staphylococci * Time, data = o2cons,
subject = "Subject", no.subf = 2, iter = 1000,
resampling = "Perm", CPU = 1, seed = 1234)
summary(model1)
## Call:
## O2 ~ Group * Staphylococci * Time
## A repeated measures analysis with 2 within-subject and 1 between-subject factors.
##
## Descriptive:
## Group Staphylococci Time n Means Lower 95 % CI Upper 95 % CI
## 1 P 0 6 12 1.322 1.150 1.493
## 5 P 0 12 12 2.430 2.196 2.664
## 9 P 0 18 12 3.425 3.123 3.727
## 3 P 1 6 12 1.618 1.479 1.758
## 7 P 1 12 12 2.434 2.164 2.704
## 11 P 1 18 12 3.527 3.273 3.781
## 2 V 0 6 12 1.394 1.201 1.588
## 6 V 0 12 12 2.570 2.355 2.785
## 10 V 0 18 12 3.677 3.374 3.979
## 4 V 1 6 12 1.656 1.471 1.840
## 8 V 1 12 12 2.799 2.500 3.098
## 12 V 1 18 12 4.029 3.802 4.257
##
## Wald-Type Statistic (WTS):
## Test statistic df p-value
## Group "11.167" "1" "0.001"
## Staphylococci "20.401" "1" "<0.001"
## Group:Staphylococci "2.554" "1" "0.11"
## Time "4113.057" "2" "<0.001"
## Group:Time "24.105" "2" "<0.001"
## Staphylococci:Time "4.334" "2" "0.115"
## Group:Staphylococci:Time "4.303" "2" "0.116"
##
## ANOVA-Type Statistic (ATS):
## Test statistic df1 df2 p-value
## Group "11.167" "1" "57.959" "0.001"
## Staphylococci "20.401" "1" "Inf" "<0.001"
## Group:Staphylococci "2.554" "1" "Inf" "0.11"
## Time "960.208" "1.524" "Inf" "<0.001"
## Group:Time "5.393" "1.524" "Inf" "0.009"
## Staphylococci:Time "2.366" "1.983" "Inf" "0.094"
## Group:Staphylococci:Time "2.147" "1.983" "Inf" "0.117"
##
## p-values resampling:
## Perm (WTS)
## Group "0.005"
## Staphylococci "<0.001"
## Group:Staphylococci "0.129"
## Time "<0.001"
## Group:Time "0.001"
## Staphylococci:Time "0.17"
## Group:Staphylococci:Time "0.153"
The output consists of four parts: model1$Descriptive gives an overview of the descriptive statistics: The number of observations,
mean and confidence intervals (based on either quantiles of the t-distribution or the resampling-based quantiles) are displayed for each factor level combination.
model1$WTS contains the results for the Wald-type test: The test statistic, degree of freedom and p-values based on the asymptotic \(\chi^2\) distribution
are displayed. Note that the \(\chi^2\) approximation is very liberal for small sample sizes.
model1$ATS contains the corresponding results based on the ATS.
This test statistic tends to rather
conservative decisions in case of small sample sizes and is even asymptotically only an approximation, thus not providing an asymptotic level \(\alpha\) test.
Finally, model1$resampling contains the p-values based on
the chosen resampling approach. For the ATS, the permutation procedure cannot be applied.
Due to the above mentioned issues for small sample sizes, the resampling procedure is recommended for such situations.
We consider the data set EEG from the MANOVA.RM package: At the Department of Neurology, University Clinic of Salzburg, 160 patients were diagnosed
with either Alzheimer's Disease (AD), mild cognitive impairments (MCI), or subjective cognitive complaints without clinically significant deficits (SCC), based on neuropsychological diagnostics (Bathke et al.(2018)). This data set contains z-scores for
brain rate and Hjorth complexity, each measured at frontal, temporal and central electrode positions and averaged across hemispheres. In addition to standardization, complexity values were multiplied by -1 in order to make them more easily comparable to brain rate
values: For brain rate we know that the values decrease with age and pathology, while Hjorth complexity values are known to increase with age and pathology. The three between-subjects factors considered were sex (men vs. women), diagnosis (AD vs. MCI vs. SCC), and age (\(< 70\) vs. \(>= 70\) years). Additionally, the within-subjects factors region (frontal, temporal, central) and feature (brain rate, complexity) structure the response vector.
data(EEG)
EEG_model <- RM(resp ~ sex * diagnosis * feature * region,
data = EEG, subject = "id", no.subf = 2, resampling = "WildBS",
iter = 1000, alpha = 0.01, CPU = 1, seed = 987)
summary(EEG_model)
## Call:
## resp ~ sex * diagnosis * feature * region
## A repeated measures analysis with 2 within-subject and 2 between-subject factors.
##
## Descriptive:
## sex diagnosis feature region n Means Lower 99 % CI Upper 99 % CI
## 1 M AD brainrate central 12 -1.010 -4.881 2.861
## 13 M AD brainrate frontal 12 -1.007 -4.991 2.977
## 25 M AD brainrate temporal 12 -0.987 -4.493 2.519
## 7 M AD complexity central 12 -1.488 -10.053 7.077
## 19 M AD complexity frontal 12 -1.086 -6.906 4.735
## 31 M AD complexity temporal 12 -1.320 -7.203 4.562
## 3 M MCI brainrate central 27 -0.447 -1.591 0.696
## 15 M MCI brainrate frontal 27 -0.464 -1.646 0.719
## 27 M MCI brainrate temporal 27 -0.506 -1.584 0.572
## 9 M MCI complexity central 27 -0.257 -1.139 0.625
## 21 M MCI complexity frontal 27 -0.459 -1.997 1.079
## 33 M MCI complexity temporal 27 -0.490 -1.796 0.816
## 5 M SCC brainrate central 20 0.459 -0.414 1.332
## 17 M SCC brainrate frontal 20 0.243 -0.670 1.156
## 29 M SCC brainrate temporal 20 0.409 -1.210 2.028
## 11 M SCC complexity central 20 0.349 -0.070 0.767
## 23 M SCC complexity frontal 20 0.095 -1.037 1.227
## 35 M SCC complexity temporal 20 0.314 -0.598 1.226
## 2 W AD brainrate central 24 -0.294 -1.978 1.391
## 14 W AD brainrate frontal 24 -0.159 -1.813 1.495
## 26 W AD brainrate temporal 24 -0.285 -1.776 1.206
## 8 W AD complexity central 24 -0.128 -1.372 1.116
## 20 W AD complexity frontal 24 0.026 -1.212 1.264
## 32 W AD complexity temporal 24 -0.194 -1.670 1.283
## 4 W MCI brainrate central 30 -0.106 -1.076 0.863
## 16 W MCI brainrate frontal 30 -0.074 -1.032 0.885
## 28 W MCI brainrate temporal 30 -0.069 -1.064 0.925
## 10 W MCI complexity central 30 0.094 -0.464 0.652
## 22 W MCI complexity frontal 30 0.131 -0.768 1.031
## 34 W MCI complexity temporal 30 0.121 -0.652 0.895
## 6 W SCC brainrate central 47 0.537 -0.049 1.124
## 18 W SCC brainrate frontal 47 0.548 -0.062 1.159
## 30 W SCC brainrate temporal 47 0.559 -0.015 1.133
## 12 W SCC complexity central 47 0.384 0.110 0.659
## 24 W SCC complexity frontal 47 0.403 -0.038 0.845
## 36 W SCC complexity temporal 47 0.506 0.132 0.880
##
## Wald-Type Statistic (WTS):
## Test statistic df p-value
## sex "9.973" "1" "0.002"
## diagnosis "42.383" "2" "<0.001"
## sex:diagnosis "3.777" "2" "0.151"
## feature "0.086" "1" "0.769"
## sex:feature "2.167" "1" "0.141"
## diagnosis:feature "5.317" "2" "0.07"
## sex:diagnosis:feature "1.735" "2" "0.42"
## region "0.07" "2" "0.966"
## sex:region "0.876" "2" "0.645"
## diagnosis:region "6.121" "4" "0.19"
## sex:diagnosis:region "1.532" "4" "0.821"
## feature:region "0.652" "2" "0.722"
## sex:feature:region "0.423" "2" "0.81"
## diagnosis:feature:region "7.142" "4" "0.129"
## sex:diagnosis:feature:region "2.274" "4" "0.686"
##
## ANOVA-Type Statistic (ATS):
## Test statistic df1 df2 p-value
## sex "9.973" "1" "36.497" "0.003"
## diagnosis "13.124" "1.343" "36.497" "<0.001"
## sex:diagnosis "1.904" "1.343" "36.497" "0.174"
## feature "0.086" "1" "Inf" "0.769"
## sex:feature "2.167" "1" "Inf" "0.141"
## diagnosis:feature "1.437" "1.562" "Inf" "0.238"
## sex:diagnosis:feature "1.031" "1.562" "Inf" "0.342"
## region "0.018" "1.611" "Inf" "0.965"
## sex:region "0.371" "1.611" "Inf" "0.644"
## diagnosis:region "1.091" "2.046" "Inf" "0.337"
## sex:diagnosis:region "0.376" "2.046" "Inf" "0.691"
## feature:region "0.126" "1.421" "Inf" "0.81"
## sex:feature:region "0.077" "1.421" "Inf" "0.864"
## diagnosis:feature:region "0.829" "1.624" "Inf" "0.415"
## sex:diagnosis:feature:region "0.611" "1.624" "Inf" "0.51"
##
## p-values resampling:
## WildBS (WTS) WildBS (ATS)
## sex "0.001" "0.001"
## diagnosis "<0.001" "<0.001"
## sex:diagnosis "0.127" "0.129"
## feature "0.797" "0.797"
## sex:feature "0.157" "0.157"
## diagnosis:feature "0.054" "0.257"
## sex:diagnosis:feature "0.464" "0.363"
## region "0.969" "0.981"
## sex:region "0.688" "0.7"
## diagnosis:region "0.168" "0.332"
## sex:diagnosis:region "0.865" "0.82"
## feature:region "0.817" "0.933"
## sex:feature:region "0.871" "0.944"
## diagnosis:feature:region "0.104" "0.502"
## sex:diagnosis:feature:region "0.738" "0.682"
We find significant effects at level \(\alpha = 0.01\) of the whole-plot factors sex and diagnosis, while none of the sub-plot factors or interactions become significant.
The RM() function is equipped with a plotting option, displaying the calculated means along with \((1-\alpha)\) confidence intervals based on a \(t\)-approximation.
The plot function takes an RM object as an argument. In addition, the factor of interest may be specified. If this argument is
omitted in a two- or higher-way layout, the user is asked to specify the factor for plotting. Furthermore, additional graphical parameters
can be used to customize the plots. The optional argument legendpos specifies the position of the legend in higher-way layouts, while the argument gap (default 0.1) specifies the distance between the error bars.
plot(EEG_model, factor = "sex", main = "Effect of sex on EEG values")
plot(EEG_model, factor = "sex:diagnosis", legendpos = "topleft", col = c(4, 2))
plot(EEG_model, factor = "sex:diagnosis:feature", legendpos = "center", gap = 0.05)
MANOVA functionThe MANOVA function calculates the WTS for multivariate data in a design with crossed or nested factors.
Additionally, a modified ANOVA-type statistic (MATS) is calculated which has the additional advantage of being applicable to designs
involving singular covariance matrices and is invariant under scale transformations of the data, see Friedrich and Pauly (2018) for details.
The resampling methods provided are a parametric bootstrap approach and a
wild bootstrap using Rademacher weights.
Note that only balanced nested designs (i.e., the same number of factor levels \(b\) for each level of the factor \(A\)) with up to three factors are
implemented. Designs involving both crossed and nested factors are not implemented. Data must be provided in long format (for wide format, see MANOVA.wide below).
We again consider the data set EEG from the MANOVA.RM package, but now we ignore the sub-plot factor structure. Therefore, we are
now in a multivariate setting with 6 measurements per patient and three crossed factors sex, age and diagnosis. Due to the small number of subjects in
some groups (e.g., only 2 male patients aged \(<\) 70 were diagnosed with AD) we restrict our analyses to two factors at a time.
The analysis of this example is shown below.
The MANOVA function takes as arguments:
formula: A formula consisting of the outcome variable on the left hand side of a ~ operator and the factor
variables of interest on the right hand side.data: A data.frame containing the variables in formula.subject: The column name of the subjects variable in the data frame.iter: The number of iterations for the resampling procedure. Default value is 10,000.alpha: The significance level, default is 0.05.resampling: The resampling method, one of 'paramBS' and 'WildBS'. Default is
set to 'paramBS'.CPU: The number of cores used for parallel computing. If omitted, cores are detected automatically.seed: A random seed for the resampling procedure. If omitted, no reproducible seed is set.nested.levels.unique: For nested designs only: A logical specifying whether the levels of the nested factor(s)
are labeled uniquely or not. Default is FALSE, i.e., the levels of the nested
factor are the same for each level of the main factor. For an example and more explanations
see the GFD package and the corresponding vignette.dec: The number of decimals the results should be rounded to. Default is 3.data(EEG)
EEG_MANOVA <- MANOVA(resp ~ sex * diagnosis,
data = EEG, subject = "id", resampling = "paramBS",
iter = 1000, alpha = 0.01, CPU = 1, seed = 987)
summary(EEG_MANOVA)
## Call:
## resp ~ sex * diagnosis
##
## Descriptive:
## sex diagnosis n Mean 1 Mean 2 Mean 3 Mean 4 Mean 5 Mean 6
## 1 M AD 12 -0.987 -1.007 -1.010 -1.320 -1.086 -1.488
## 3 M MCI 27 -0.506 -0.464 -0.447 -0.490 -0.459 -0.257
## 5 M SCC 20 0.409 0.243 0.459 0.314 0.095 0.349
## 2 W AD 24 -0.285 -0.159 -0.294 -0.194 0.026 -0.128
## 4 W MCI 30 -0.069 -0.074 -0.106 0.121 0.131 0.094
## 6 W SCC 47 0.559 0.548 0.537 0.506 0.403 0.384
##
## Wald-Type Statistic (WTS):
## Test statistic df p-value
## sex "12.604" "6" "0.05"
## diagnosis "55.158" "12" "<0.001"
## sex:diagnosis "9.79" "12" "0.634"
##
## modified ANOVA-Type Statistic (MATS):
## Test statistic
## sex 45.263
## diagnosis 194.165
## sex:diagnosis 18.401
##
## p-values resampling:
## paramBS (WTS) paramBS (MATS)
## sex "0.124" "0.003"
## diagnosis "<0.001" "<0.001"
## sex:diagnosis "0.748" "0.223"
The output consists of several parts: First, some descriptive statistics of the data set are displayed, namely the sample size and mean for each factor level combination and each dimension. (Dimensions occur in the same order as in the original data set. For a labeled output, use MANOVA.wide().) In this example, Mean 1 to Mean 3 correspond to the brainrate (temporal, frontal, central) while Mean 4–6 correspond to complexity. Second, the results based on the WTS are displayed. For each factor, the test statistic, degree of freedom and p-value is given. For the MATS, only the value of the test statistic is given, since inference is here based on the resampling procedure only. The resampling-based p-values are finally displayed for both test statistics.
MANOVA.wide functionThe MANOVA.wide function is used for data provided in wide format, i.e., with one row per unit. Input and output are almost identical to the MANOVA function, except that no subject variable needs to be specified. The formula now consists of the matrix of outcome variables (bound together via cbind()) on the left hand side of the ~ operator and the factors of interest on the right.
For an example we use the data provided as an example for the summary.manova() function:
tear <- c(6.5, 6.2, 5.8, 6.5, 6.5, 6.9, 7.2, 6.9, 6.1, 6.3,
6.7, 6.6, 7.2, 7.1, 6.8, 7.1, 7.0, 7.2, 7.5, 7.6)
gloss <- c(9.5, 9.9, 9.6, 9.6, 9.2, 9.1, 10.0, 9.9, 9.5, 9.4,
9.1, 9.3, 8.3, 8.4, 8.5, 9.2, 8.8, 9.7, 10.1, 9.2)
opacity <- c(4.4, 6.4, 3.0, 4.1, 0.8, 5.7, 2.0, 3.9, 1.9, 5.7,
2.8, 4.1, 3.8, 1.6, 3.4, 8.4, 5.2, 6.9, 2.7, 1.9)
rate <- gl(2,10, labels = c("Low", "High"))
additive <- gl(2, 5, length = 20, labels = c("Low", "High"))
example <- data.frame(tear, gloss, opacity, rate, additive)
fit <- MANOVA.wide(cbind(tear, gloss, opacity) ~ rate * additive, data = example, iter = 1000, CPU = 1)
summary(fit)
## Call:
## cbind(tear, gloss, opacity) ~ rate * additive
##
## Descriptive:
## rate additive n tear gloss opacity
## 1 Low Low 5 6.30 9.56 3.74
## 2 High Low 5 6.68 9.58 3.84
## 3 Low High 5 6.88 8.72 3.14
## 4 High High 5 7.28 9.40 5.02
##
## Wald-Type Statistic (WTS):
## Test statistic df p-value
## rate "25.9" "3" "<0.001"
## additive "14.591" "3" "0.002"
## rate:additive "4.589" "3" "0.204"
##
## modified ANOVA-Type Statistic (MATS):
## Test statistic
## rate 23.808
## additive 11.835
## rate:additive 4.296
##
## p-values resampling:
## paramBS (WTS) paramBS (MATS)
## rate "0.006" "0.004"
## additive "0.027" "0.028"
## rate:additive "0.317" "0.285"
A function for calculating and plotting of confidence regions is available for MANOVA objects. Details on the methods can be found in Friedrich and Pauly (2018).
Confidence regions can be calculated using the conf.reg function. Note that confidence regions can only be plotted in designs with 2 dimensions.
The conf.reg function takes as arguments:
object: A MANOVA object calculated via MANOVA() or MANOVA.wide().nullhypo: In designs involving more than one factor, it is necessary to specify the null hypothesis, i.e., the contrast of interest.As an example, we consider the data set water from the package HSAUR. The data set contains measurements of mortality and drinking water hardness for 61 cities in England and Wales. Suppose we want to analyse whether these measurements differ between northern and southern towns. Since the data set is in wide format, we need to use the MANOVA.wide function.
if (requireNamespace("HSAUR", quietly = TRUE)) {
library(HSAUR)
data(water)
test <- MANOVA.wide(cbind(mortality, hardness) ~ location, data = water, iter = 1000, resampling = "paramBS", CPU = 1, seed = 123)
summary(test)
cr <- conf.reg(test)
cr
}
## Loading required package: tools
## Call:
## cbind(mortality, hardness) ~ location
##
## Descriptive:
## location n mortality hardness
## 1 North 35 1633.600 30.400
## 2 South 26 1376.808 69.769
##
## Wald-Type Statistic (WTS):
## Test statistic df p-value
## location "51.584" "2" "<0.001"
##
## modified ANOVA-Type Statistic (MATS):
## Test statistic
## location 69.882
##
## p-values resampling:
## paramBS (WTS) paramBS (MATS)
## location "<0.001" "<0.001"
## Center:
## [,1]
## [1,] 256.792
## [2,] -39.369
##
## Scale:
## [1] 90.70294 22.86942
##
## Eigenvectors:
## [,1] [,2]
## [1,] -1 0
## [2,] 0 -1
The output consists of the necessary parameters specifying the ellipsoid: the center, the eigenvectors which determine the axes of the ellipsoid as well as the scaling factors for the eigenvectors, which are calculated based on the eigenvalues, the bootstrap quantile and the total sample size. For more information on the construction of the confidence ellipses see Friedrich and Pauly (2018).
For observations with two dimensions, the confidence ellipse can be plotted using the generic plot function. The usual plotting parameters can be used to customize the plots.
plot(cr, col = 2, lty = 2, xlab = "Difference in mortality", ylab ="Difference in water hardness")
Calculation of simultaneous confidence intervals and multivariate p-values for contrasts of the mean vector is based on the sum statistic, see Friedrich and Pauly (2018) for details. Note that the confidence intervals and p-values returned are simultaneous, i.e., they maintain the given alpha-level.
Confidence intervals are calculated based on summary effects, i.e., averaging over all dimensions, whereas the returned p-values are multivariate.
The function simCI takes the following arguments:
object: A MANOVA object calculated via MANOVA() or MANOVA.wide().contrast: The contrast of interest, can either be “pairwise” or “user-defined”. contmat: For user-defined contrasts, the contrast matrix must be specified here. Note that
its rows must sum to zero.type: Pairwise contrasts are calculated based on the contrMat function in package multcomp, see also the corresponding help page. The type of the pairwise comparison must be specified here. base: an integer specifying which group is considered the baseline group for Dunnett contrasts, see also the documentation of contrMat() from the multcomp-package.As an example, we consider the EEG_MANOVA example from above:
# pairwise comparison using Tukey contrasts
simCI(EEG_MANOVA, contrast = "pairwise", type = "Tukey")
##
## #------ Call -----#
##
## - Contrast: Tukey
## - Confidence level: 99 %
##
## #------Multivariate post-hoc comparisons: p-values -----#
##
## contrast p.value
## 1 M MCI - M AD 0.961
## 2 M SCC - M AD 0.548
## 3 W AD - M AD 0.899
## 4 W MCI - M AD 0.775
## 5 W SCC - M AD 0.417
## 6 M SCC - M MCI 0.368
## 7 W AD - M MCI 0.995
## 8 W MCI - M MCI 0.843
## 9 W SCC - M MCI 0.111
## 10 W AD - M SCC 0.845
## 11 W MCI - M SCC 0.938
## 12 W SCC - M SCC 0.989
## 13 W MCI - W AD 1.000
## 14 W SCC - W AD 0.526
## 15 W SCC - W MCI 0.563
##
## #-----------Confidence intervals for summary effects-------------#
##
## Estimate Lower Upper
## M MCI - M AD 4.275 -16.181707 24.731707
## M SCC - M AD 8.767 -11.126510 28.660510
## W AD - M AD 5.864 -14.947797 26.675797
## W MCI - M AD 6.995 -12.978374 26.968374
## W SCC - M AD 9.835 -9.799574 29.469574
## M SCC - M MCI 4.492 -4.040216 13.024216
## W AD - M MCI 1.589 -8.907565 12.085565
## W MCI - M MCI 2.720 -5.996803 11.436803
## W SCC - M MCI 5.560 -2.349709 13.469709
## W AD - M SCC -2.903 -12.254617 6.448617
## W MCI - M SCC -1.772 -9.069776 5.525776
## W SCC - M SCC 1.068 -5.243764 7.379764
## W MCI - W AD 1.131 -8.389330 10.651330
## W SCC - W AD 3.971 -4.816350 12.758350
## W SCC - W MCI 2.840 -3.719140 9.399140
# the same but with Dunnett contrasts using group 2 as baseline
simCI(EEG_MANOVA, contrast = "pairwise", type = "Dunnett", base = 2)
##
## #------ Call -----#
##
## - Contrast: Dunnett
## - Confidence level: 99 %
##
## #------Multivariate post-hoc comparisons: p-values -----#
##
## contrast p.value
## 1 M AD - M MCI 0.664
## 2 M SCC - M MCI 0.046
## 3 W AD - M MCI 0.863
## 4 W MCI - M MCI 0.303
## 5 W SCC - M MCI 0.007
##
## #-----------Confidence intervals for summary effects-------------#
##
## Estimate Lower Upper
## M AD - M MCI -4.275 -17.8559687 9.305969
## M SCC - M MCI 4.492 -1.1724388 10.156439
## W AD - M MCI 1.589 -5.3795468 8.557547
## W MCI - M MCI 2.720 -3.0669840 8.506984
## W SCC - M MCI 5.560 0.3088365 10.811164
# a one-way layout using MANOVA.wide():
oneway <- MANOVA.wide(cbind(brainrate_temporal, brainrate_central) ~ diagnosis, data = EEGwide,
iter = 1000, CPU = 1)
# and a user-defined contrast matrix
H <- as.matrix(cbind(rep(1, 5), -1*Matrix::Diagonal(5)))
# user-specified comparison
simCI(oneway, contrast = "user-defined", contmat = H)
##
## #------ Call -----#
##
## - Contrast: user-defined
## - Confidence level: 95 %
##
## #------Multivariate post-hoc comparisons: p-values -----#
##
## [1] 1.000 0.700 0.675 0.017 0.014
##
## #-----------Confidence intervals for summary effects-------------#
##
## Estimate Lower Upper
## 1 0.013 -1.018061 1.0440609
## 2 -0.243 -1.061669 0.5756690
## 3 -0.251 -1.069950 0.5679499
## 4 -1.033 -1.823753 -0.2422474
## 5 -1.033 -1.802626 -0.2633741
If the global null hypothesis is rejected, it may be of interest to infer the univariate outcomes that caused the rejection. To answer this question, one can simply calculate the univariate p-values and adjust them accordingly for multiple testing, e.g., using Bonferroni-correction. An example is given below. We consider a one-way layout of the EEG data with influencing factor sex and all 6 outcome variables:
model_sex <- MANOVA.wide(cbind(brainrate_temporal, brainrate_central, brainrate_frontal,
complexity_temporal, complexity_central, complexity_frontal) ~ sex,
data = EEGwide,
iter = 1000, seed = 987, CPU = 1)
summary(model_sex)
## Call:
## cbind(brainrate_temporal, brainrate_central, brainrate_frontal,
## complexity_temporal, complexity_central, complexity_frontal) ~
## sex
##
## Descriptive:
## sex n brainrate_temporal brainrate_central brainrate_frontal
## 1 M 59 -0.294 -0.254 -0.335
## 2 W 101 0.172 0.149 0.195
## complexity_temporal complexity_central complexity_frontal
## 1 -0.386 -0.302 -0.399
## 2 0.226 0.176 0.233
##
## Wald-Type Statistic (WTS):
## Test statistic df p-value
## sex "15.382" "6" "0.017"
##
## modified ANOVA-Type Statistic (MATS):
## Test statistic
## sex 55.725
##
## p-values resampling:
## paramBS (WTS) paramBS (MATS)
## sex "0.031" "<0.001"
Since the global hypothesis is rejected at 5% level, we continue with the univariate calculations:
EEG1 <- MANOVA.wide(brainrate_temporal ~ sex, data = EEGwide, iter = 1000, seed = 987, CPU = 1)
EEG2 <- MANOVA.wide(brainrate_central ~ sex, data = EEGwide, iter = 1000, seed = 987, CPU = 1)
EEG3 <- MANOVA.wide(brainrate_frontal ~ sex, data = EEGwide, iter = 1000, seed = 987, CPU = 1)
EEG4 <- MANOVA.wide(complexity_temporal ~ sex, data = EEGwide, iter = 1000, seed = 987, CPU = 1)
EEG5 <- MANOVA.wide(complexity_central ~ sex, data = EEGwide, iter = 1000, seed = 987, CPU = 1)
EEG6 <- MANOVA.wide(complexity_frontal ~ sex, data = EEGwide, iter = 1000, seed = 987, CPU = 1)
Adjust for multiple testing using the parametric bootstrap MATS and Bonferroni adjustment:
p.adjust(c(EEG1$resampling[, 2], EEG2$resampling[, 2], EEG3$resampling[, 2],
EEG4$resampling[, 2], EEG5$resampling[, 2], EEG6$resampling[, 2]),
method = "bonferroni")
## [1] 0.036 0.078 0.012 0.012 0.096 0.006
This reveals that the central variables (comparison 2 and 5) do not contribute to the significant difference between male and female patients.
To create a data example for a nested design, we use the curdies data set from the GFD package and extend it by introducing an artificial second outcome variable. In this data set, the levels of the nested factor (site) are named uniquely, i.e., levels 1-3 of factor site belong to “WINTER”, whereas levels 4-6 belong to “SUMMER”. Therefore, nested.levels.unique must be set to TRUE. The code for the analysis using both wide and long format is presented below.
if (requireNamespace("GFD", quietly = TRUE)) {
library(GFD)
data(curdies)
set.seed(123)
curdies$dug2 <- curdies$dugesia + rnorm(36)
# first possibility: MANOVA.wide
fit1 <- MANOVA.wide(cbind(dugesia, dug2) ~ season + season:site, data = curdies, iter = 1000, nested.levels.unique = TRUE, seed = 123, CPU = 1)
# second possibility: MANOVA (long format)
dug <- c(curdies$dugesia, curdies$dug2)
season <- rep(curdies$season, 2)
site <- rep(curdies$site, 2)
curd <- data.frame(dug, season, site, subject = rep(1:36, 2))
fit2 <- MANOVA(dug ~ season + season:site, data = curd, subject = "subject", nested.levels.unique = TRUE, seed = 123, iter = 1000,
CPU = 1)
# comparison of results
summary(fit1)
summary(fit2)
}
## Call:
## cbind(dugesia, dug2) ~ season + season:site
##
## Descriptive:
## season site n dugesia dug2
## 1 SUMMER 4 6 0.419 -0.050
## 2 SUMMER 5 6 0.229 0.028
## 3 SUMMER 6 6 0.194 0.763
## 4 WINTER 1 6 2.049 2.497
## 5 WINTER 2 6 4.182 4.123
## 6 WINTER 3 6 0.678 0.724
##
## Wald-Type Statistic (WTS):
## Test statistic df p-value
## season "6.999" "2" "0.03"
## season:site "16.621" "8" "0.034"
##
## modified ANOVA-Type Statistic (MATS):
## Test statistic
## season 12.296
## season:site 15.064
##
## p-values resampling:
## paramBS (WTS) paramBS (MATS)
## season "0.064" "0.032"
## season:site "0.275" "0.216"
## Call:
## dug ~ season + season:site
##
## Descriptive:
## season site n Mean 1 Mean 2
## 1 SUMMER 4 6 0.419 -0.050
## 2 SUMMER 5 6 0.229 0.028
## 3 SUMMER 6 6 0.194 0.763
## 4 WINTER 1 6 2.049 2.497
## 5 WINTER 2 6 4.182 4.123
## 6 WINTER 3 6 0.678 0.724
##
## Wald-Type Statistic (WTS):
## Test statistic df p-value
## season "6.999" "2" "0.03"
## season:site "16.621" "8" "0.034"
##
## modified ANOVA-Type Statistic (MATS):
## Test statistic
## season 12.296
## season:site 15.064
##
## p-values resampling:
## paramBS (WTS) paramBS (MATS)
## season "0.064" "0.032"
## season:site "0.275" "0.216"
The MANOVA.RM package is equipped with an optional graphical user interface, which is based on RGtk2. The GUI may be started in R (if RGtk2 is installed) using the
command GUI.RM() and GUI.MANOVA() or GUI.MANOVAwide() for repeated measures designs and multivariate data, respectively.
if (requireNamespace("RGtk2", quietly = TRUE)) {
GUI.MANOVA()
}
The user can specify the data location
(either directly or via the “load data” button), the formula, the number of iterations for the resampling approach and
the significance level. Furthermore, one needs to specify the number of sub-plot factors (for the repeated measures design only),
the 'subject' variable in the
data frame and the resampling method.
Additionally, one can specify whether or not headers are
included in the data file, and which separator (e.g., ',' for *.csv files) and character symbols are used for decimals
in the data file.
The GUI for RM also provides a plotting option, which generates a new window
for specifying the factors to be plotted (in higher-way layouts) along with a few plotting
parameters.
Bathke, A. et al. (2018). Testing Mean Differences among Groups: Multivariate and Repeated Measures Analysis with Minimal Assumptions. Multivariate Behavioral Research, 53(3), 348-359, DOI: 10.1080/00273171.2018.1446320.
Brunner, E. (2001). Asymptotic and approximate analysis of repeated measures designs under heteroscedasticity. Mathematical Statistics with Applications in Biometry.
Friedrich, S., Brunner, E. and Pauly, M. (2017). Permuting longitudinal data in spite of the dependencies. Journal of Multivariate Analysis, 153, 255-265.
Friedrich, S., and Pauly, M. (2018). MATS: Inference for potentially singular and heteroscedastic MANOVA. Journal of Multivariate Analysis, 165, 166-179, DOI: 10.1016/j.jmva.2017.12.008.
Friedrich, S., Konietschke, F., and Pauly, M. (2018). Analysis of Multivariate Data and Repeated Measures Designs with the R Package MANOVA.RM. arXiv preprint arXiv:1801.08002.
Konietschke, F., Bathke, A. C., Harrar, S. W. and Pauly, M. (2015). Parametric and nonparametric bootstrap methods for general MANOVA. Journal of Multivariate Analysis, 140, 291-301.