Package MKmisc

IQR

I implemented function IQrange before the standard function IQR gained the type argument. Since 2010 (r53643, r53644) the function is identical to function IQR.

x <- rnorm(100)
IQrange(x)

## [1] 1.214648

IQR(x)

## [1] 1.214648

It is also possible to compute a standardized version of the IQR leading to a normal-consistent estimate of the standard deviation.

sIQR(x)

## [1] 0.9004196

sd(x)

## [1] 0.9467541

Mean Absolute Deviation

The mean absolute deviation under the assumption of symmetry is a robust alternative to the sample standard deviation.

meanAD(x)

## [1] 0.9198986

Five Number Summary

There is a function that computes a so-called five number summary which in contrast to function fivenum uses the first and third quartile instead of the lower and upper hinge.

fiveNS(x)

##     Minimum         25%      Median         75%     Maximum 
## -2.57330400 -0.69482207 -0.08864456  0.51982554  2.24396794

Coefficient of Variation (CV)

There are functions to compute the (classical) coefficient of variation as well as two robust variants. In case of the robust variants, the mean is replaced by the median and the SD is replaced by the (standardized) MAD and the (standardized) IQR, respectively.

## 5% outliers
out <- rbinom(100, prob = 0.05, size = 1)
sum(out)

## [1] 7

x <- (1-out)*rnorm(100, mean = 10, sd = 2) + out*25
CV(x)

## [1] 0.3879403

medCV(x)

## [1] 0.1683868

iqrCV(x)

## [1] 0.1562934

Signal to Noise Ratio (SNR)

There are functions to compute the (classical) signal to noise ratio as well as two robust variants. In case of the robust variants, the mean is replaced by the median and the SD is replaced by the (standardized) MAD and the (standardized) IQR, respectively.

SNR(x)

## [1] 2.577716

medSNR(x)

## [1] 5.938708

iqrSNR(x)

## [1] 6.398224

Box- and Whisker-Plot

In contrast to the standard function boxplot which uses the lower and upper hinge for defining the box and the whiskers, the function qboxplot uses the first and third quartile.

x <- rt(10, df = 3)
par(mfrow = c(1,2))
qboxplot(x, main = "1st and 3rd quartile")
boxplot(x, main = "Lower and upper hinge")

The difference between the two versions often is hardly visible.

OR, RR and Other Risk Measures

Given the incidence of the outcome of interest in the nonexposed (p0) and exposed (p1) group, several risk measures can be computed.

## Example from Wikipedia
risks(p0 = 0.4, p1 = 0.1)

##        p0        p1        RR        OR       RRR       ARR       NNT 
## 0.4000000 0.1000000 0.2500000 0.1666667 0.7500000 0.3000000 3.3333333

risks(p0 = 0.4, p1 = 0.5)

##    p0    p1    RR    OR   RRI   ARI   NNH 
##  0.40  0.50  1.25  1.50  0.25  0.10 10.00

Given p0 or p1 and OR, we can compute the respective RR.

or2rr(or = 1.5, p0 = 0.4)

## [1] 1.25

or2rr(or = 1/6, p1 = 0.1)

## [1] 0.25

Generalized Logarithm

The generalized logarithm may be useful as a variance stabilizing transformation when also negative values are present.

curve(log, from = -3, to = 5)

## Warning in log(x): NaNs wurden erzeugt

curve(glog, from = -3, to = 5, add = TRUE, col = "orange")
legend("topleft", fill = c("black", "orange"), legend = c("log", "glog"))

As in case of function log there is also glog10 and glog2.

curve(log10(x), from = -3, to = 5)

## Warning in eval(expr, envir = ll, enclos = parent.frame()): NaNs wurden
## erzeugt

curve(glog10(x), from = -3, to = 5, add = TRUE, col = "orange")
legend("topleft", fill = c("black", "orange"), legend = c("log10", "glog10"))

There are also functions that compute the inverse of the generalized logarithm.

inv.glog(glog(10))

## [1] 10

inv.glog(glog(10, base = 3), base = 3)

## [1] 10

inv.glog10(glog10(10))

## [1] 10

inv.glog2(glog2(10))

## [1] 10

Simulate Correlated Variables

To demonstrate Pearson correlation in my lectures, I have written this simple function to simulate correlated variables and to generate a scatter plot of the data.

res <- simCorVars(n = 500, r = 0.8)

cor(res$Var1, res$Var2)

## [1] 0.8222099

Plot TSH, fT3 and fT4 Values

The thyroid function is usually investigated by determining the values of TSH, fT3 and fT4. The function thyroid can be used to visualize the measured values as relative values with respect to the provided reference ranges.

thyroid(TSH = 1.5, fT3 = 2.5, fT4 = 14, TSHref = c(0.2, 3.0),
        fT3ref = c(1.7, 4.2), fT4ref = c(7.6, 15.0))

Generalized and Negative Logarithm as Transformations

We can use the generalized logarithm for transforming the axes in ggplot2 plots.

library(ggplot2)
data(mpg)
p1 <- ggplot(mpg, aes(displ, hwy)) + geom_point()
p1

p1 + scale_x_log10()

p1 + scale_x_glog10()

p1 + scale_y_log10()

p1 + scale_y_glog10()

The negative logrithm is for instance useful for displaying p values. The interesting values are on the top. This is for instance used in a so-called volcano plot.

x <- matrix(rnorm(1000, mean = 10), nrow = 10)
g1 <- rep("control", 10)
y1 <- matrix(rnorm(500, mean = 11.25), nrow = 10)
y2 <- matrix(rnorm(500, mean = 9.75), nrow = 10)
g2 <- rep("treatment", 10)
group <- factor(c(g1, g2))
Data <- rbind(x, cbind(y1, y2))
pvals <- apply(Data, 2, function(x, group) t.test(x ~ group)$p.value,
               group = group)
## compute log-fold change
logfc <- function(x, group){
  res <- tapply(x, group, mean)
  log2(res[1]/res[2])
}
lfcs <- apply(Data, 2, logfc, group = group)
ps <- data.frame(pvals = pvals, logfc = lfcs)
ggplot(ps, aes(x = logfc, y = pvals)) + geom_point() +
    geom_hline(yintercept = 0.05) + scale_y_neglog10() +
    geom_vline(xintercept = c(-0.1, 0.1)) + xlab("log-fold change") +
    ylab("-log10(p value)") + ggtitle("A Volcano Plot")

Change Data from Wide to Long

Often it’s better to have the data in a long format than in a wide format; e.g., when plotting with package ggplot2. The necessary transformation can be done with function melt.long.

library(ggplot2)
## some random data
test <- data.frame(x = rnorm(10), y = rnorm(10), z = rnorm(10))
test.long <- melt.long(test)
test.long

##           value variable
## x1  -1.61097019        x
## x2  -0.17741403        x
## x3  -0.50071863        x
## x4  -0.62530413        x
## x5  -0.83880633        x
## x6   0.73692910        x
## x7  -1.12017453        x
## x8   0.25378171        x
## x9  -0.79050214        x
## x10 -0.90549324        x
## y1   0.37064866        y
## y2  -0.34972516        y
## y3  -0.01794129        y
## y4   0.42985343        y
## y5   1.01118395        y
## y6   0.78036989        y
## y7   0.40400337        y
## y8   0.52458138        y
## y9   0.48055958        y
## y10  0.15980025        y
## z1   0.14791703        z
## z2   0.97722176        z
## z3   0.17527069        z
## z4  -1.64406119        z
## z5   1.53996956        z
## z6  -1.38681726        z
## z7  -0.85355752        z
## z8   0.71800536        z
## z9   0.59257651        z
## z10 -0.45050563        z

ggplot(test.long, aes(x = variable, y = value)) +
  geom_boxplot(aes(fill = variable))

## introducing an additional grouping variable
group <- factor(rep(c("a","b"), each = 5))
test.long.gr <- melt.long(test, select = 1:2, group = group)
test.long.gr

##     group       value variable
## x1      a -1.61097019        x
## x2      a -0.17741403        x
## x3      a -0.50071863        x
## x4      a -0.62530413        x
## x5      a -0.83880633        x
## x6      b  0.73692910        x
## x7      b -1.12017453        x
## x8      b  0.25378171        x
## x9      b -0.79050214        x
## x10     b -0.90549324        x
## y1      a  0.37064866        y
## y2      a -0.34972516        y
## y3      a -0.01794129        y
## y4      a  0.42985343        y
## y5      a  1.01118395        y
## y6      b  0.78036989        y
## y7      b  0.40400337        y
## y8      b  0.52458138        y
## y9      b  0.48055958        y
## y10     b  0.15980025        y

ggplot(test.long.gr, aes(x = variable, y = value, fill = group)) +
  geom_boxplot()

Binomial Proportion

There are several functions for computing confidence intervals. We can compute 10 different confidence intervals for binomial proportions; e.g.

## default: "wilson"
binomCI(x = 12, n = 50)

## 
##  wilson confidence interval
## 
## 95 percent confidence interval:
##          2.5 %    97.5 %
## prob 0.1429739 0.3741268
## 
## sample estimate:
## prob 
## 0.24 
## 
## additional information:
## standard error of prob 
##             0.05896867

## Clopper-Pearson interval
binomCI(x = 12, n = 50, method = "clopper-pearson")

## 
##  clopper-pearson confidence interval
## 
## 95 percent confidence interval:
##          2.5 %    97.5 %
## prob 0.1306099 0.3816907
## 
## sample estimate:
## prob 
## 0.24

## identical to 
binom.test(x = 12, n = 50)$conf.int

## [1] 0.1306099 0.3816907
## attr(,"conf.level")
## [1] 0.95

For all intervals implemented see the help page of function binomCI.

Mean and SD

We can compute confidence intervals for mean and SD of a normal distribution.

x <- rnorm(50, mean = 2, sd = 3)
## mean and SD unknown
normCI(x)

## 
##  Exact confidence interval(s)
## 
## 95 percent confidence intervals:
##         2.5 %   97.5 %
## mean 2.225350 4.237621
## sd   2.957314 4.411657
## 
## sample estimates:
##     mean       sd 
## 3.231486 3.540277 
## 
## additional information:
## SE of mean 
##  0.5006708

## SD known
normCI(x, sd = 3)

## 
##  Exact confidence interval(s)
## 
## 95 percent confidence interval:
##         2.5 %   97.5 %
## mean 2.399943 4.063028
## 
## sample estimate:
##     mean 
## 3.231486 
## 
## additional information:
## SE of mean 
##  0.4242641

## mean known
normCI(x, mean = 2)

## 
##  Exact confidence interval(s)
## 
## 95 percent confidence interval:
##       2.5 %   97.5 %
## sd 2.957314 4.411657
## 
## sample estimate:
##       sd 
## 3.540277

Difference in Means

We can compute confidence interval for the difference of means assuming normal distributions.

x <- rnorm(20)
y <- rnorm(20, sd = 2)
## paired
normDiffCI(x, y, paired = TRUE)

## 
##  Confidence interval (paired)
## 
## 95 percent confidence interval:
##                          2.5 %   97.5 %
## mean of differences -0.0270875 1.399005
## 
## sample estimate:
## mean of differences 
##            0.685959 
## 
## additional information:
## SE of mean of differences 
##                 0.3406776

## compare
normCI(x-y)

## 
##  Exact confidence interval(s)
## 
## 95 percent confidence intervals:
##           2.5 %   97.5 %
## mean -0.0270875 1.399005
## sd    1.1586502 2.225264
## 
## sample estimates:
##     mean       sd 
## 0.685959 1.523557 
## 
## additional information:
## SE of mean 
##  0.3406776

## unpaired
y <- rnorm(10, mean = 1, sd = 2)
## classical
normDiffCI(x, y, method = "classical")

## 
##  Classical confidence interval (unpaired)
## 
## 95 percent confidence interval:
##                        2.5 %   97.5 %
## difference in means -1.48845 1.163204
## 
## sample estimate:
## difference in means 
##          -0.1626228 
## 
## additional information:
## SE of difference in means           Cohen's d (SMD) 
##                0.64724785               -0.09730977 
## 
##   mean of x     SD of x   mean of y     SD of y 
## -0.06592175  0.52331863  0.09670105  2.84793963

## Welch (default as in case of function t.test)
normDiffCI(x, y, method = "welch")

## 
##  Welch confidence interval (unpaired)
## 
## 95 percent confidence interval:
##                         2.5 %  97.5 %
## difference in means -2.206816 1.88157
## 
## sample estimate:
## difference in means 
##          -0.1626228 
## 
## additional information:
## SE of difference in means           Cohen's d (SMD) 
##                0.90816801               -0.05616163 
## 
##   mean of x     SD of x   mean of y     SD of y 
## -0.06592175  0.52331863  0.09670105  2.84793963

## Hsu
normDiffCI(x, y, method = "hsu")

## 
##  Hsu confidence interval (unpaired)
## 
## 95 percent confidence interval:
##                         2.5 %   97.5 %
## difference in means -2.217042 1.891796
## 
## sample estimate:
## difference in means 
##          -0.1626228 
## 
## additional information:
## SE of difference in means           Cohen's d (SMD) 
##                0.90816801               -0.05616163 
## 
##   mean of x     SD of x   mean of y     SD of y 
## -0.06592175  0.52331863  0.09670105  2.84793963

In case of unequal variances and unequal sample sizes per group the classical confidence interval may have a bad coverage (too long or too short), as is indicated by the small Monte-Carlo simulation study below.

M <- 100
CIhsu <- CIwelch <- CIclass <- matrix(NA, nrow = M, ncol = 2)
for(i in 1:M){
  x <- rnorm(10)
  y <- rnorm(30, sd = 0.1)
  CIclass[i,] <- normDiffCI(x, y, method = "classical")$conf.int
  CIwelch[i,] <- normDiffCI(x, y, method = "welch")$conf.int
  CIhsu[i,] <- normDiffCI(x, y, method = "hsu")$conf.int
}
## coverage probabilies
## classical
sum(CIclass[,1] < 0 & 0 < CIclass[,2])/M

## [1] 0.74

## Welch
sum(CIwelch[,1] < 0 & 0 < CIwelch[,2])/M

## [1] 0.96

## Hsu
sum(CIhsu[,1] < 0 & 0 < CIhsu[,2])/M

## [1] 0.96

Coefficient of Variation

We provide 11 different confidence intervals for the (classical) coefficient of variation; e.g.

x <- rnorm(100, mean = 10, sd = 2) # CV = 0.2
## default: "miller"
cvCI(x)

## 
##  Miller (1991) confidence interval
## 
## 95 percent confidence interval:
##        2.5 %    97.5 %
## CV 0.1680721 0.2248794
## 
## sample estimate:
##        CV 
## 0.1964758 
## 
## additional information:
## standard error of CV 
##           0.01449191

## Gulhar et al. (2012)
cvCI(x, method = "gulhar")

## 
##  Gulhar et al (2012) confidence interval
## 
## 95 percent confidence interval:
##        2.5 %   97.5 %
## CV 0.1725071 0.228241
## 
## sample estimate:
##        CV 
## 0.1964758

For all intervals implemented see the help page of function cvCI.

Quantiles, Median and MAD

We start with the computation of confidence intervals for quantiles.

x <- rexp(100, rate = 0.5)
## exact
quantileCI(x = x, prob = 0.95)

## 
##  exact confidence interval
## 
## 95.14464 percent confidence interval:
##                  lower    upper
## 95 % quantile 5.536315 9.984989
## 
## sample estimate:
## 95 % quantile 
##      6.546731

## asymptotic
quantileCI(x = x, prob = 0.95, method = "asymptotic")

## 
##  asymptotic confidence interval
## 
## 95 percent confidence interval:
##                  2.5 %   97.5 %
## 95 % quantile 5.536315 10.56759
## 
## sample estimate:
## 95 % quantile 
##      6.546731

Next, we consider the median.

## exact
medianCI(x = x)

## 
##  exact confidence interval
## 
## 95.23684 percent confidence intervals:
##           lower    upper
## median 1.145691 2.171415
## median 1.287856 2.371827
## 
## sample estimate:
##   median 
## 1.682672

## asymptotic
medianCI(x = x, method = "asymptotic")

## 
##  asymptotic confidence interval
## 
## 95 percent confidence interval:
##           2.5 %   97.5 %
## median 1.188723 2.194297
## 
## sample estimate:
##   median 
## 1.682672

It often happens that quantile confidence intervals are not unique. Here the minimum length interval might be of interest.

medianCI(x = x, minLength = TRUE)

## 
##  minimum length exact confidence interval
## 
## 95.23684 percent confidence interval:
##           lower    upper
## median 1.145691 2.171415
## 
## sample estimate:
##   median 
## 1.682672

Finally, we take a look at MAD (median absolute deviation) where by default the standardized MAD is used (see function mad).

## exact
madCI(x = x)

## 
##  exact confidence interval
## 
## 95.23684 percent confidence intervals:
##        lower    upper
## MAD 1.283361 2.199345
## MAD 1.431107 2.224908
## 
## sample estimate:
##      MAD 
## 1.845505

## aysymptotic
madCI(x = x, method = "asymptotic")

## 
##  asymptotic confidence interval
## 
## 95 percent confidence interval:
##       2.5 %   97.5 %
## MAD 1.39216 2.201539
## 
## sample estimate:
##      MAD 
## 1.845505

## unstandardized
madCI(x = x, constant = 1)

## 
##  exact confidence interval
## 
## 95.23684 percent confidence intervals:
##         lower    upper
## MAD 0.8656152 1.483438
## MAD 0.9652688 1.500680
## 
## sample estimate:
##      MAD 
## 1.244776

Relative Risk

There is also a function for computing an approximate confidence interval for the relative risk (RR).

## Example from Wikipedia
rrCI(a = 15, b = 135, c = 100, d = 150)

## 
##  asymptotic confidence interval
## 
## 95 percent confidence interval:
##                   2.5 %    97.5 %
## relative risk 0.1510993 0.4136353
## 
## sample estimate:
## relative risk 
##          0.25

rrCI(a = 75, b = 75, c = 100, d = 150)

## 
##  asymptotic confidence interval
## 
## 95 percent confidence interval:
##                 2.5 %  97.5 %
## relative risk 1.00256 1.55851
## 
## sample estimate:
## relative risk 
##          1.25

Welch Two-Sample t-Test

For computing the sample size of the Welch t-test, we only consider the situation of equal group size (balanced design).

## identical results as power.t.test, since sd = sd1 = sd2 = 1
power.welch.t.test(n = 20, delta = 1)

## 
##      Two-sample Welch t test power calculation 
## 
##               n = 20
##           delta = 1
##             sd1 = 1
##             sd2 = 1
##       sig.level = 0.05
##           power = 0.8689528
##     alternative = two.sided
## 
## NOTE: n is number in *each* group

power.welch.t.test(power = .90, delta = 1)

## 
##      Two-sample Welch t test power calculation 
## 
##               n = 22.0211
##           delta = 1
##             sd1 = 1
##             sd2 = 1
##       sig.level = 0.05
##           power = 0.9
##     alternative = two.sided
## 
## NOTE: n is number in *each* group

power.welch.t.test(power = .90, delta = 1, alternative = "one.sided")

## 
##      Two-sample Welch t test power calculation 
## 
##               n = 17.84713
##           delta = 1
##             sd1 = 1
##             sd2 = 1
##       sig.level = 0.05
##           power = 0.9
##     alternative = one.sided
## 
## NOTE: n is number in *each* group

## sd1 = 0.5, sd2 = 1
power.welch.t.test(delta = 1, sd1 = 0.5, sd2 = 1, power = 0.9)

## 
##      Two-sample Welch t test power calculation 
## 
##               n = 14.53583
##           delta = 1
##             sd1 = 0.5
##             sd2 = 1
##       sig.level = 0.05
##           power = 0.9
##     alternative = two.sided
## 
## NOTE: n is number in *each* group

Hsu Two-Sample t-Test

For computing the sample size of the Hsu t-test, we only consider the situation of equal group size (balanced design).

## slightly more conservative than Welch t-test
power.hsu.t.test(n = 20, delta = 1)

## 
##      Two-sample Hsu t test power calculation 
## 
##               n = 20
##           delta = 1
##             sd1 = 1
##             sd2 = 1
##       sig.level = 0.05
##           power = 0.8506046
##     alternative = two.sided
## 
## NOTE: n is number in *each* group

power.hsu.t.test(power = .90, delta = 1)

## 
##      Two-sample Hsu t test power calculation 
## 
##               n = 23.02186
##           delta = 1
##             sd1 = 1
##             sd2 = 1
##       sig.level = 0.05
##           power = 0.9
##     alternative = two.sided
## 
## NOTE: n is number in *each* group

power.hsu.t.test(power = .90, delta = 1, alternative = "one.sided")

## 
##      Two-sample Hsu t test power calculation 
## 
##               n = 18.5674
##           delta = 1
##             sd1 = 1
##             sd2 = 1
##       sig.level = 0.05
##           power = 0.9
##     alternative = one.sided
## 
## NOTE: n is number in *each* group

## sd1 = 0.5, sd2 = 1
power.welch.t.test(delta = 0.5, sd1 = 0.5, sd2 = 1, power = 0.9)

## 
##      Two-sample Welch t test power calculation 
## 
##               n = 53.86822
##           delta = 0.5
##             sd1 = 0.5
##             sd2 = 1
##       sig.level = 0.05
##           power = 0.9
##     alternative = two.sided
## 
## NOTE: n is number in *each* group

power.hsu.t.test(delta = 0.5, sd1 = 0.5, sd2 = 1, power = 0.9)

## 
##      Two-sample Hsu t test power calculation 
## 
##               n = 54.49421
##           delta = 0.5
##             sd1 = 0.5
##             sd2 = 1
##       sig.level = 0.05
##           power = 0.9
##     alternative = two.sided
## 
## NOTE: n is number in *each* group

Two Negative Binomial Rates

When we consider two negative binomial rates, we can compute sample size or power applying function power.nb.test.

## examples from Table III in Zhu and Lakkis (2014)
power.nb.test(mu0 = 5.0, RR = 2.0, theta = 1/0.5, duration = 1, power = 0.8, approach = 1)

## 
##      Power calculation for comparing two negative binomial rates 
## 
##               n = 22.37386
##              n1 = 22.37386
##             mu0 = 5
##              RR = 2
##           theta = 2
##        duration = 1
##       sig.level = 0.05
##           power = 0.8
##     alternative = two.sided
## 
## NOTE: n = sample size of control group, n1 = sample size of treatment group

power.nb.test(mu0 = 5.0, RR = 2.0, theta = 1/0.5, duration = 1, power = 0.8, approach = 2)

## 
##      Power calculation for comparing two negative binomial rates 
## 
##               n = 21.23734
##              n1 = 21.23734
##             mu0 = 5
##              RR = 2
##           theta = 2
##        duration = 1
##       sig.level = 0.05
##           power = 0.8
##     alternative = two.sided
## 
## NOTE: n = sample size of control group, n1 = sample size of treatment group

power.nb.test(mu0 = 5.0, RR = 2.0, theta = 1/0.5, duration = 1, power = 0.8, approach = 3)

## 
##      Power calculation for comparing two negative binomial rates 
## 
##               n = 20.85564
##              n1 = 20.85564
##             mu0 = 5
##              RR = 2
##           theta = 2
##        duration = 1
##       sig.level = 0.05
##           power = 0.8
##     alternative = two.sided
## 
## NOTE: n = sample size of control group, n1 = sample size of treatment group

Moderated t-Test

The function to compute the moderated t-test was motivated by the fact that my students have problems to understand and correctly adapt the code of the limma package.

## One-sample test
X <- matrix(rnorm(10*20, mean = 1), nrow = 10, ncol = 20)
mod.t.test(X)

##         mean      2.5%     97.5%        t      p.value  adj.p.value
## 1  0.5087996 0.1038840 0.9137152 2.513590 1.465866e-02 1.465866e-02
## 2  0.7813481 0.3622029 1.2004933 3.728998 4.288804e-04 5.361005e-04
## 3  0.8918729 0.4564595 1.3272863 4.097447 1.274410e-04 1.820585e-04
## 4  1.1559184 0.7110024 1.6008343 5.197103 2.569496e-06 6.853782e-06
## 5  1.2209407 0.8060725 1.6358090 5.887034 1.906366e-07 9.531828e-07
## 6  1.2645726 0.7761898 1.7529555 5.179591 2.741513e-06 6.853782e-06
## 7  1.4837387 1.0657152 1.9017623 7.100171 1.703756e-09 1.703756e-08
## 8  0.9248638 0.5004022 1.3493253 4.358645 5.220173e-05 8.700289e-05
## 9  0.6746272 0.2008917 1.1483626 2.848657 6.009242e-03 6.676936e-03
## 10 1.0041004 0.6076027 1.4005981 5.065807 4.169611e-06 8.339222e-06
##             B
## 1  -3.9188424
## 2  -0.6509869
## 3   0.5026442
## 4   4.2647451
## 5   6.7970983
## 6   4.2018584
## 7  11.4165844
## 8   1.3569612
## 9  -3.1120015
## 10  3.7952104

## Two-sample test
set.seed(123)
X <- rbind(matrix(rnorm(5*20), nrow = 5, ncol = 20),
           matrix(rnorm(5*20, mean = 1), nrow = 5, ncol = 20))
g2 <- factor(c(rep("group 1", 10), rep("group 2", 10)))
mod.t.test(X, group = g2)

##    difference in means       2.5%     97.5%           t   p.value
## 1          -0.30099317 -1.1337943 0.5318079 -0.71317027 0.4766640
## 2           0.13637650 -0.6964246 0.9691776  0.32312914 0.7469725
## 3          -0.49260925 -1.3254104 0.3401919 -1.16718354 0.2446801
## 4           0.15266680 -0.6801343 0.9854679  0.36172723 0.7179801
## 5          -0.05546448 -0.8882656 0.7773366 -0.13141699 0.8955922
## 6          -0.03152278 -0.8643239 0.8012783 -0.07468976 0.9405445
## 7          -0.69311916 -1.5259203 0.1396820 -1.64226977 0.1022800
## 8          -0.17595066 -1.0087518 0.6568505 -0.41689577 0.6772514
## 9          -0.54524220 -1.3780433 0.2875589 -1.29189154 0.1980510
## 10         -0.01770155 -0.8505027 0.8150996 -0.04194188 0.9665915
##    adj.p.value         B mean of group 1 mean of group 2
## 1    0.9665915 -4.608912      0.07083562     0.371828786
## 2    0.9665915 -4.619655      0.13562592    -0.000750575
## 3    0.8156005 -4.586223     -0.30436677     0.188242477
## 4    0.9665915 -4.618953      0.18497579     0.032308986
## 5    0.9665915 -4.621971      0.08494719     0.140411667
## 6    0.9665915 -4.622282      1.11828347     1.149806246
## 7    0.8156005 -4.550748      0.67404426     1.367163425
## 8    0.9665915 -4.617811      0.53111339     0.707064052
## 9    0.8156005 -4.578072      0.92210638     1.467348578
## 10   0.9665915 -4.622384      0.48495033     0.502651884

## Paired two-sample test
mod.t.test(X, group = g2, paired = TRUE)

##    mean of differences       2.5%       97.5%           t     p.value
## 1          -0.30099317 -0.7260027  0.12401634 -1.39744874 0.163998732
## 2           0.13637650 -0.2886330  0.56138600  0.63316773 0.527427738
## 3          -0.49260925 -0.9176188 -0.06759974 -2.28708237 0.023354856
## 4           0.15266680 -0.2723427  0.57767631  0.70880025 0.479365424
## 5          -0.05546448 -0.4804740  0.36954503 -0.25751005 0.797079211
## 6          -0.03152278 -0.4565323  0.39348673 -0.14635370 0.883805952
## 7          -0.69311916 -1.1181287 -0.26810966 -3.21800824 0.001531067
## 8          -0.17595066 -0.6009602  0.24905885 -0.81690235 0.415064109
## 9          -0.54524220 -0.9702517 -0.12023269 -2.53144623 0.012215144
## 10         -0.01770155 -0.4427111  0.40730796 -0.08218462 0.934591222
##    adj.p.value         B
## 1   0.40999683 -5.193223
## 2   0.75346820 -5.932720
## 3   0.07784952 -3.631339
## 4   0.75346820 -5.884358
## 5   0.93459122 -6.092149
## 6   0.93459122 -6.113540
## 7   0.01531067 -1.189400
## 8   0.75346820 -5.805769
## 9   0.06107572 -3.070283
## 10  0.93459122 -6.120528

Moderated 1-Way ANOVA

The function to compute a moderated 1-way ANOVA was motivated by the fact that my students have problems to understand and correctly adapt the code of the limma package.

set.seed(123)
X <- rbind(matrix(rnorm(5*20), nrow = 5, ncol = 20),
           matrix(rnorm(5*20, mean = 1), nrow = 5, ncol = 20))
gr <- factor(c(rep("A1", 5), rep("B2", 5), rep("C3", 5), rep("D4", 5)))
mod.oneway.test(X, gr)

##           A-B        A-C         A-D         B-C        B-D         C-D
## 1   1.0974330  0.2271669  0.26827976 -0.87026609 -0.8291532  0.04111286
## 2   0.0769194  0.9622020 -0.61252965  0.88528264 -0.6894491 -1.57473169
## 3  -0.3105477 -0.7130963 -0.58266984 -0.40254866 -0.2721221  0.13042651
## 4  -0.5832304 -0.2440290 -0.03386782  0.33920142  0.5493626  0.21016117
## 5  -0.9579128 -0.4501003 -0.61874146  0.50781250  0.3391713 -0.16864116
## 6  -0.6013595 -0.5109767 -0.15342834  0.09038278  0.4479311  0.35754833
## 7   0.3471695 -0.3493145 -0.68975433 -0.69648400 -1.0369239 -0.34043986
## 8  -0.9277388 -0.5691081 -0.71053196  0.35863064  0.2172068 -0.14142382
## 9  -0.5998638 -1.5488157 -0.14153255 -0.94895185  0.4583313  1.40728311
## 10  1.5527067  0.5179562  0.99934740 -1.03475050 -0.5533593  0.48139118
##     grand mean         F    p.value adj.p.value
## 1   0.22133220 1.4119467 0.23709800   0.5868380
## 2   0.06743767 2.5678204 0.05255479   0.1751826
## 3  -0.05806215 0.6094415 0.60879068   0.7253749
## 4   0.10864239 0.4386138 0.72537489   0.7253749
## 5   0.11267943 0.9691456 0.40611786   0.5868380
## 6   1.13404486 0.5002131 0.68212276   0.7253749
## 7   1.02060384 1.2185746 0.30111975   0.5868380
## 8   0.61908872 0.9594030 0.41078662   0.5868380
## 9   1.19472748 2.9871234 0.02980893   0.1751826
## 10  0.49380111 2.6903326 0.04456696   0.1751826

Pairwise moderated t-tests

As a optional post-hoc analysis after mod.oneway.test one can use pairwise moderated t-tests. One should carefully think about the adjustment of p values in this context.

pairwise.mod.t.test(X, gr)

##         A1-B2   A1-B2: t    A1-B2: p A1-B2: adj.p  A1-B2: B      A1-C3
## 1   1.0974330  1.9176595 0.056935659   0.26739434 -4.150296  0.2271669
## 2   0.0769194  0.1344093 0.893247840   0.89324784 -5.826707  0.9622020
## 3  -0.3105477 -0.5426525 0.588124185   0.65347132 -5.700081 -0.7130963
## 4  -0.5832304 -1.0191395 0.309675276   0.44239325 -5.359162 -0.2440290
## 5  -0.9579128 -1.6738612 0.096111665   0.26739434 -4.551426 -0.4501003
## 6  -0.6013595 -1.0508183 0.294926580   0.44239325 -5.329122 -0.5109767
## 7   0.3471695  0.6066456 0.544945915   0.65347132 -5.666387 -0.3493145
## 8  -0.9277388 -1.6211350 0.106957735   0.26739434 -4.631016 -0.5691081
## 9  -0.5998638 -1.0482048 0.296125067   0.44239325 -5.331635 -1.5488157
## 10  1.5527067  2.7132069 0.007393498   0.07393498 -2.462559  0.5179562
##      A1-C3: t    A1-C3: p A1-C3: adj.p  A1-C3: B       A1-D4    A1-D4: t
## 1   0.3969525 0.691931480   0.69193148 -5.757494  0.26827976  0.46879329
## 2   1.6813563 0.094644661   0.47322331 -4.535810 -0.61252965 -1.07033714
## 3  -1.2460679 0.214560903   0.61819096 -5.119000 -0.58266984 -1.01815997
## 4  -0.4264174 0.670376894   0.69193148 -5.746391 -0.03386782 -0.05918078
## 5  -0.7865073 0.432733671   0.61819096 -5.546500 -0.61874146 -1.08119168
## 6  -0.8928830 0.373260796   0.61819096 -5.464740 -0.15342834 -0.26810139
## 7  -0.6103937 0.542467061   0.67808383 -5.659092 -0.68975433 -1.20527990
## 8  -0.9944622 0.321499481   0.61819096 -5.376999 -0.71053196 -1.24158683
## 9  -2.7064076 0.007539705   0.07539705 -2.477381 -0.14153255 -0.24731463
## 10  0.9050791 0.366784330   0.61819096 -5.454705  0.99934740  1.74626427
##      A1-D4: p A1-D4: adj.p  A1-D4: B       B2-C3   B2-C3: t   B2-C3: p
## 1  0.63985549    0.8944242 -4.606903 -0.87026609 -1.5207070 0.13030713
## 2  0.28607955    0.5168984 -4.593186  0.88528264  1.5469470 0.12385169
## 3  0.31013903    0.5168984 -4.594801 -0.40254866 -0.7034154 0.48281925
## 4  0.95288197    0.9528820 -4.610107  0.33920142  0.5927221 0.55420392
## 5  0.28123878    0.5168984 -4.592840  0.50781250  0.8873539 0.37622030
## 6  0.78896661    0.8944242 -4.609094  0.09038278  0.1579353 0.87470693
## 7  0.22987482    0.5168984 -4.588637 -0.69648400 -1.2170394 0.22538132
## 8  0.21620608    0.5168984 -4.587321  0.35863064  0.6266728 0.53176683
## 9  0.80498180    0.8944242 -4.609252 -0.94895185 -1.6582029 0.09923575
## 10 0.08268426    0.5168984 -4.564982 -1.03475050 -1.8081278 0.07246459
##    B2-C3: adj.p  B2-C3: B      B2-D4   B2-D4: t   B2-D4: p B2-D4: adj.p
## 1     0.3257678 -4.575899 -0.8291532 -1.4488662 0.14933196    0.6213576
## 2     0.3257678 -4.574706 -0.6894491 -1.2047465 0.23008017    0.6213576
## 3     0.6157821 -4.602828 -0.2721221 -0.4755075 0.63507382    0.7047841
## 4     0.6157821 -4.604954  0.5493626  0.9599587 0.33852439    0.6213576
## 5     0.6157821 -4.598493  0.3391713  0.5926696 0.55423902    0.6927988
## 6     0.8747069 -4.609789  0.4479311  0.7827169 0.43495030    0.6213576
## 7     0.4507626 -4.588215 -1.0369239 -1.8119255 0.07187282    0.6213576
## 8     0.6157821 -4.604340  0.2172068  0.3795482 0.70478410    0.7047841
## 9     0.3257678 -4.569423  0.4583313  0.8008902 0.42438292    0.6213576
## 10    0.3257678 -4.561724 -0.5533593 -0.9669426 0.33503202    0.6213576
##     B2-D4: B       C3-D4   C3-D4: t    C3-D4: p C3-D4: adj.p  C3-D4: B
## 1  -4.579059  0.04111286  0.0718408 0.942818328   0.94281833 -5.862037
## 2  -4.588656 -1.57473169 -2.7516934 0.006613244   0.06613244 -2.377508
## 3  -4.606809  0.13042651  0.2279079 0.820008840   0.91112093 -5.840494
## 4  -4.596506  0.21016117  0.3672366 0.713927813   0.91112093 -5.802308
## 5  -4.604955 -0.16864116 -0.2946843 0.768617018   0.91112093 -5.824423
## 6  -4.601082  0.35754833  0.6247816 0.533004365   0.91112093 -5.684652
## 7  -4.561521 -0.34043986 -0.5948862 0.552759917   0.91112093 -5.701444
## 8  -4.608024 -0.14142382 -0.2471246 0.805128573   0.91112093 -5.836290
## 9  -4.600656  1.40728311  2.4590930 0.014993757   0.07496878 -3.079639
## 10 -4.596307  0.48139118  0.8411852 0.401499618   0.91112093 -5.538559

Estimation

There are two functions that can be used to calculate and test AUC values. First function AUC, which computes the area under the receiver operating characteristic curve (AUC under ROC curve) using the connection of AUC to the Wilcoxon rank sum test. We use some random data and groups to demonstrate the use of this function.

x <- c(runif(50, max = 0.6), runif(50, min = 0.4))
g <- c(rep(0, 50), rep(1, 50))
AUC(x, group = g)

## [1] 0.9212

Sometimes the labels of the group should be switched to avoid an AUC smaller than 0.5, which represents a result worse than a pure random choice.

g <- c(rep(1, 50), rep(0, 50))
AUC(x, group = g)

## Warning in AUC(x, group = g): The computed AUC value 0.0788 will be
## replaced by 0.9212 which can be achieved be interchanging the sample
## labels!

## [1] 0.9212

## no switching
AUC(x, group = g, switchAUC = FALSE)

## [1] 0.0788

Testing

We can also perform statistical tests for AUC. First, the one-sample test which corresponds to the Wilcoxon signed rank test.

g <- c(rep(0, 50), rep(1, 50))
AUC.test(pred1 = x, lab1 = g)

## $Variable1
##       AUC        SE    low CI     up CI 
## 0.9212000 0.0285512 0.8652407 0.9771593 
## 
## $Test
## 
##  Wilcoxon rank sum test with continuity correction
## 
## data:  0 and 1
## W = 197, p-value = 3.995e-13
## alternative hypothesis: true AUC is not equal to 0.5

We can also compare two AUC using the test of Hanley and McNeil (1982).

x2 <- c(runif(50, max = 0.7), runif(50, min = 0.3))
g2 <- c(rep(0, 50), rep(1, 50))
AUC.test(pred1 = x, lab1 = g, pred2 = x2, lab2 = g2)

## $Variable1
##       AUC        SE    low CI     up CI 
## 0.9212000 0.0285512 0.8652407 0.9771593 
## 
## $Variable2
##        AUC         SE     low CI      up CI 
## 0.78560000 0.04585469 0.69572646 0.87547354 
## 
## $Test
## 
##  Hanley and McNeil test for two AUCs
## 
## data:  x and x2
## z = 2.5103, p-value = 0.01206
## alternative hypothesis: true difference in AUC is not equal to 0
## 95 percent confidence interval:
##  0.02972886 0.24147114
## sample estimates:
## Difference in AUC 
##            0.1356

Pairwise

There is also a function for pairwise comparison if there are more than two groups.

x3 <- c(x, x2)
g3 <- c(g, c(rep(2, 50), rep(3, 50)))
pairwise.auc(x = x3, g = g3)

## Warning in AUC(xi, xj): The computed AUC value 0.0788 will be replaced by
## 0.9212 which can be achieved be interchanging the sample labels!

## Warning in AUC(xi, xj): The computed AUC value 0.4076 will be replaced by
## 0.5924 which can be achieved be interchanging the sample labels!

## Warning in AUC(xi, xj): The computed AUC value 0.1588 will be replaced by
## 0.8412 which can be achieved be interchanging the sample labels!

## Warning in AUC(xi, xj): The computed AUC value 0.2144 will be replaced by
## 0.7856 which can be achieved be interchanging the sample labels!

## 0 vs 1 0 vs 2 0 vs 3 1 vs 2 1 vs 3 2 vs 3 
## 0.9212 0.5924 0.8412 0.8992 0.6568 0.7856

In addition to the pairwise.auc there are further functions for pairwise comparisons.

FC and logFC

In the analysis of omics data, the FC or logFC are important measures and are often used in combination with (adjusted) p values.

x <- rnorm(100) ## assumed as log-data
g <- factor(sample(1:4, 100, replace = TRUE))
levels(g) <- c("a", "b", "c", "d")
## modified FC
pairwise.fc(x, g)

##    a vs b    a vs c    a vs d    b vs c    b vs d    c vs d 
##  1.025526  1.028896 -1.063345  1.003286 -1.090489 -1.094072

## "true" FC
pairwise.fc(x, g, mod.fc = FALSE)

##    a vs b    a vs c    a vs d    b vs c    b vs d    c vs d 
## 1.0255264 1.0288962 0.9404284 1.0032859 0.9170201 0.9140168

## without any transformation
pairwise.logfc(x, g)

##       a vs b       a vs c       a vs d       b vs c       b vs d 
##  0.036364688  0.041097415 -0.088609974  0.004732726 -0.124974662 
##       c vs d 
## -0.129707388

The function returns a modified FC. That is, if the FC is smaller than 1 it is transformed to -1/FC. One can also use other functions than the mean for the aggregation of the data.

pairwise.logfc(x, g, ave = median)

##      a vs b      a vs c      a vs d      b vs c      b vs d      c vs d 
##  0.06301909  0.19666124 -0.00200599  0.13364215 -0.06502508 -0.19866723

Arbitrary Criteria

Furthermore, function pairwise.fun enables the application of arbitrary functions for pairwise comparisons.

pairwise.wilcox.test(airquality$Ozone, airquality$Month, 
                     p.adjust.method = "none")

## Warning in wilcox.test.default(xi, xj, paired = paired, ...): cannot
## compute exact p-value with ties

## Warning in wilcox.test.default(xi, xj, paired = paired, ...): cannot
## compute exact p-value with ties

## Warning in wilcox.test.default(xi, xj, paired = paired, ...): cannot
## compute exact p-value with ties

## Warning in wilcox.test.default(xi, xj, paired = paired, ...): cannot
## compute exact p-value with ties

## Warning in wilcox.test.default(xi, xj, paired = paired, ...): cannot
## compute exact p-value with ties

## Warning in wilcox.test.default(xi, xj, paired = paired, ...): cannot
## compute exact p-value with ties

## Warning in wilcox.test.default(xi, xj, paired = paired, ...): cannot
## compute exact p-value with ties

## Warning in wilcox.test.default(xi, xj, paired = paired, ...): cannot
## compute exact p-value with ties

## Warning in wilcox.test.default(xi, xj, paired = paired, ...): cannot
## compute exact p-value with ties

## Warning in wilcox.test.default(xi, xj, paired = paired, ...): cannot
## compute exact p-value with ties

## 
##  Pairwise comparisons using Wilcoxon rank sum test 
## 
## data:  airquality$Ozone and airquality$Month 
## 
##   5       6       7       8      
## 6 0.19250 -       -       -      
## 7 3e-05   0.01414 -       -      
## 8 0.00012 0.02591 0.86195 -      
## 9 0.11859 0.95887 0.00074 0.00325
## 
## P value adjustment method: none

## To avoid the warnings
library(exactRankTests)

##  Package 'exactRankTests' is no longer under development.
##  Please consider using package 'coin' instead.

pairwise.fun(airquality$Ozone, airquality$Month, 
             fun = function(x, y) wilcox.exact(x, y)$p.value)

##       5 vs 6       5 vs 7       5 vs 8       5 vs 9       6 vs 7 
## 1.897186e-01 1.087205e-05 6.108735e-05 1.171796e-01 1.183753e-02 
##       6 vs 8       6 vs 9       7 vs 8       7 vs 9       8 vs 9 
## 2.333564e-02 9.528659e-01 8.595683e-01 5.281796e-04 2.714694e-03

PPV and NPV

In case of medical diagnostic tests, usually sensitivity and specificity of the tests are known and there is also at least a rough estimate of the prevalence of the tested disease. In the practival application, the positive predictive value (PPV) and the negative predictive value are of crucial importance.

## Example: HIV test 
## 1. ELISA screening test (4th generation)
predValues(sens = 0.999, spec = 0.998, prev = 0.001)

##       PPV       NPV 
## 0.3333333 0.9999990

## 2. Western-Plot confirmation test
predValues(sens = 0.998, spec = 0.999996, prev = 1/3)

##      PPV      NPV 
## 0.999992 0.999001

Performance Measures and Scores

In the development of diagnostic tests and more general in binary classification a variety of performance measures and scores can be found in literature. Functions perfMeasures and prefScores compute several of them.

## example from dataset infert
fit <- glm(case ~ spontaneous+induced, data = infert, family = binomial())
pred <- predict(fit, type = "response")

## with group numbers
perfMeasures(pred, truth = infert$case, namePos = 1)

##                                       Measure Value
## 1                              accuracy (ACC) 0.714
## 2  probabiliy of correct classification (PCC) 0.714
## 3     probability of missclassification (PMC) 0.286
## 4                                  error rate 0.286
## 5                                 sensitivity 0.337
## 6                                 specificity 0.903
## 7                                  prevalence 0.335
## 8                         no information rate 0.665
## 9                    weighted accuracy (wACC) 0.620
## 10                   balanced accuracy (BACC) 0.620
## 11                               informedness 0.240
## 12                       Youden's J statistic 0.240
## 13            positive likelihood ratio (PLR) 3.479
## 14            negative likelihood ratio (NLR) 0.734
## 15            positive predictive value (PPV) 0.636
## 16            negative predictive value (NPV) 0.730
## 17                                 markedness 0.367
## 18                  weighted predictive value 0.683
## 19                  balanced predictive value 0.683
## 20                                   F1 score 0.441
## 21    Matthews' correlation coefficient (MCC) 0.297
## 22         proportion of positive predictions 0.177
## 23                          expected accuracy 0.607
## 24                  Cohen's kappa coefficient 0.272
## 25                             detection rate 0.113

perfScores(pred, truth = infert$case, namePos = 1)

##                            Score Value
## 1 area under the ROC curve (AUC) 0.729
## 2                     Gini index 0.457
## 3                    Brier score 0.191
## 4           positive Brier score 0.361
## 5           negative Brier score 0.106
## 6           weighted Brier score 0.233
## 7           balanced Brier score 0.233

## with group names
my.case <- factor(infert$case, labels = c("control", "case"))
perfMeasures(pred, truth = my.case, namePos = "case")

##                                       Measure Value
## 1                              accuracy (ACC) 0.714
## 2  probabiliy of correct classification (PCC) 0.714
## 3     probability of missclassification (PMC) 0.286
## 4                                  error rate 0.286
## 5                                 sensitivity 0.337
## 6                                 specificity 0.903
## 7                                  prevalence 0.335
## 8                         no information rate 0.665
## 9                    weighted accuracy (wACC) 0.620
## 10                   balanced accuracy (BACC) 0.620
## 11                               informedness 0.240
## 12                       Youden's J statistic 0.240
## 13            positive likelihood ratio (PLR) 3.479
## 14            negative likelihood ratio (NLR) 0.734
## 15            positive predictive value (PPV) 0.636
## 16            negative predictive value (NPV) 0.730
## 17                                 markedness 0.367
## 18                  weighted predictive value 0.683
## 19                  balanced predictive value 0.683
## 20                                   F1 score 0.441
## 21    Matthews' correlation coefficient (MCC) 0.297
## 22         proportion of positive predictions 0.177
## 23                          expected accuracy 0.607
## 24                  Cohen's kappa coefficient 0.272
## 25                             detection rate 0.113

perfScores(pred, truth = my.case, namePos = "case")

##                            Score Value
## 1 area under the ROC curve (AUC) 0.729
## 2                     Gini index 0.457
## 3                    Brier score 0.191
## 4           positive Brier score 0.361
## 5           negative Brier score 0.106
## 6           weighted Brier score 0.233
## 7           balanced Brier score 0.233

## using weights
perfMeasures(pred, truth = infert$case, namePos = 1, weight = 0.3)

##                                       Measure Value
## 1                              accuracy (ACC) 0.714
## 2  probabiliy of correct classification (PCC) 0.714
## 3     probability of missclassification (PMC) 0.286
## 4                                  error rate 0.286
## 5                                 sensitivity 0.337
## 6                                 specificity 0.903
## 7                                  prevalence 0.335
## 8                         no information rate 0.665
## 9                    weighted accuracy (wACC) 0.733
## 10                   balanced accuracy (BACC) 0.620
## 11                               informedness 0.240
## 12                       Youden's J statistic 0.240
## 13            positive likelihood ratio (PLR) 3.479
## 14            negative likelihood ratio (NLR) 0.734
## 15            positive predictive value (PPV) 0.636
## 16            negative predictive value (NPV) 0.730
## 17                                 markedness 0.367
## 18                  weighted predictive value 0.702
## 19                  balanced predictive value 0.683
## 20                                   F1 score 0.441
## 21    Matthews' correlation coefficient (MCC) 0.297
## 22         proportion of positive predictions 0.177
## 23                          expected accuracy 0.607
## 24                  Cohen's kappa coefficient 0.272
## 25                             detection rate 0.113

perfScores(pred, truth = infert$case, namePos = 1, weight = 0.3)

##                            Score Value
## 1 area under the ROC curve (AUC) 0.729
## 2                     Gini index 0.457
## 3                    Brier score 0.191
## 4           positive Brier score 0.361
## 5           negative Brier score 0.106
## 6           weighted Brier score 0.182
## 7           balanced Brier score 0.233

Optimal Cutoff

The function optCutoff computes the optimal cutoff for various performance weasures for binary classification. More precisely, all performance measures that are implemented in function perfMeasures.

## example from dataset infert
fit <- glm(case ~ spontaneous+induced, data = infert, family = binomial())
pred <- predict(fit, type = "response")
optCutoff(pred, truth = infert$case, namePos = 1)

##      Optimal Cut-off Youden's J statistic 
##              0.37504              0.34700

The computation of an optimal cut-off doesn’t make any sense for continuous scoring rules as their computation does not involve any cut-off (discretization/dichotomization).

Hosmer-Lemeshow and le Cessie-van Houwelingen-Copas-Hosmer

These tests are used to investigate the goodness of fit in logistic regression.

## Hosmer-Lemeshow goodness of fit tests for C and H statistic 
HLgof.test(fit = pred, obs = infert$case)

## Warning in HLgof.test(fit = pred, obs = infert$case): Found only 6
## different groups for Hosmer-Lemesho C statistic.

## $C
## 
##  Hosmer-Lemeshow C statistic
## 
## data:  pred and infert$case
## X-squared = 4.4272, df = 4, p-value = 0.3513
## 
## 
## $H
## 
##  Hosmer-Lemeshow H statistic
## 
## data:  pred and infert$case
## X-squared = 6.3168, df = 8, p-value = 0.6118

## e Cessie-van Houwelingen-Copas-Hosmer global goodness of fit test
HLgof.test(fit = pred, obs = infert$case, 
           X = model.matrix(case ~ spontaneous+induced, data = infert))

## Warning in HLgof.test(fit = pred, obs = infert$case, X = model.matrix(case
## ~ : Found only 6 different groups for Hosmer-Lemesho C statistic.

## $C
## 
##  Hosmer-Lemeshow C statistic
## 
## data:  pred and infert$case
## X-squared = 4.4272, df = 4, p-value = 0.3513
## 
## 
## $H
## 
##  Hosmer-Lemeshow H statistic
## 
## data:  pred and infert$case
## X-squared = 6.3168, df = 8, p-value = 0.6118
## 
## 
## $gof
## 
##  le Cessie-van Houwelingen-Copas-Hosmer global goodness of fit
##  test
## 
## data:  pred and infert$case
## z = 1.7533, p-value = 0.07954

Sample Size Calculation

Given an expected sensitivity and specificity we can compute sample size, power, delta or significance level of diagnostic test.

## see n2 on page 1202 of Chu and Cole (2007)
power.diagnostic.test(sens = 0.99, delta = 0.14, power = 0.95) # 40

## 
##      Diagnostic test exact power calculation 
## 
##            sens = 0.99
##               n = 40
##              n1 = 40
##           delta = 0.14
##       sig.level = 0.05
##           power = 0.95
##            prev = NULL
## 
## NOTE: n is number of cases, n1 is number of controls

power.diagnostic.test(sens = 0.99, delta = 0.13, power = 0.95) # 43

## 
##      Diagnostic test exact power calculation 
## 
##            sens = 0.99
##               n = 43
##              n1 = 43
##           delta = 0.13
##       sig.level = 0.05
##           power = 0.95
##            prev = NULL
## 
## NOTE: n is number of cases, n1 is number of controls

power.diagnostic.test(sens = 0.99, delta = 0.12, power = 0.95) # 47

## 
##      Diagnostic test exact power calculation 
## 
##            sens = 0.99
##               n = 47
##              n1 = 47
##           delta = 0.12
##       sig.level = 0.05
##           power = 0.95
##            prev = NULL
## 
## NOTE: n is number of cases, n1 is number of controls

The sample size planning for developing binary classifiers in case of high dimensional data, we can apply function ssize.pcc, which is based on the probability of correct classification (PCC).

## see Table 2 of Dobbin et al. (2008)
g <- 0.1
fc <- 1.6
ssize.pcc(gamma = g, stdFC = fc, nrFeatures = 22000)

## 
##      Sample Size Planning for Developing Classifiers Using High Dimensional Data 
## 
##           gamma = 0.1
##            prev = 0.5
##      nrFeatures = 22000
##              n1 = 21
##              n2 = 21
## 
## NOTE: n1 is number of cases, n2 is number of controls

Aggregating Technical Replicates

In case of omics experiments it is often the case that technical replicates are determined and hence it is part of the preprocessing of the raw data to aggregate these technical replicates. This is the purpose of function repMeans.

M <- matrix(rnorm(100), ncol = 5)
FL <- matrix(rpois(100, lambda = 10), ncol = 5) # only for this example
repMeans(x = M, flags = FL, use.flags = "max", ndups = 5, spacing = 4)

## $exprs
##            [,1]       [,2]       [,3]       [,4]       [,5]
## [1,] -1.1561674  1.6659909 -0.7913139 -1.9251453 -0.3599751
## [2,]  0.1467085 -1.1392006  0.4605913  0.4127695  0.1887531
## [3,] -0.0974125  1.5408878  0.5620414 -1.1852888 -0.8445834
## [4,]  0.9112097 -0.5272343 -0.3865341  0.3013137 -0.5722881
## 
## $flags
##      [,1] [,2] [,3] [,4] [,5]
## [1,]   11   11   18   13   14
## [2,]   13   13    9   17   15
## [3,]   13   12   12   14   13
## [4,]   17    8   18   15   13

1- and 2-Way ANOVA

Functions oneWayAnova and twoWayAnova return a function that can be used to perform a 1- or 2-way ANOVA, respectively.

af <- oneWayAnova(c(rep(1,5),rep(2,5)))
## p value
af(rnorm(10))

## [1] 0.4775058

x <- matrix(rnorm(12*10), nrow = 10)
## 2-way ANOVA with interaction
af1 <- twoWayAnova(c(rep(1,6),rep(2,6)), rep(c(rep(1,3), rep(2,3)), 2))
## p values
apply(x, 1, af1)

##                  [,1]      [,2]      [,3]       [,4]      [,5]      [,6]
## cov1        0.8600392 0.3933937 0.3637042 0.25648878 0.6445050 0.3662116
## cov2        0.8735542 0.2238443 0.8970489 0.04185771 0.8627222 0.7268275
## interaction 0.7134877 0.4613755 0.3382075 0.95756365 0.6680431 0.9783548
##                   [,7]      [,8]      [,9]     [,10]
## cov1        0.07973061 0.5322539 0.5296932 0.1703228
## cov2        0.01711811 0.2941207 0.2012428 0.9128464
## interaction 0.01450295 0.4349538 0.3198896 0.9204181

## 2-way ANOVA without interaction
af2 <- twoWayAnova(c(rep(1,6),rep(2,6)), rep(c(rep(1,3), rep(2,3)), 2), 
                   interaction = FALSE)
## p values
apply(x, 1, af2)

##           [,1]      [,2]      [,3]       [,4]      [,5]      [,6]
## cov1 0.8524495 0.3801684 0.3616139 0.22726078 0.6275373 0.3362318
## cov2 0.8666834 0.2103309 0.8969023 0.03037705 0.8557404 0.7100415
##            [,7]      [,8]      [,9]     [,10]
## cov1 0.18581834 0.5228496 0.5304601 0.1447322
## cov2 0.06095909 0.2823267 0.2000102 0.9073261

Correlation Distance Matrix

In the analysis of omics data correlation and absolute correlation distance matrices are often used during quality control. Function corDist can compute the Pearson, Spearman, Kendall or Cosine sample correlation and absolute correlation as well as the minimum covariance determinant or the orthogonalized Gnanadesikan-Kettenring correlation and absolute correlation.

M <- matrix(rcauchy(1000), nrow = 5)
## Pearson
corDist(M)

##           1         2         3         4
## 2 0.9958159                              
## 3 1.0054874 1.0293796                    
## 4 1.0700867 0.9880482 1.0138094          
## 5 0.9996421 0.9906085 1.0014355 0.4217543

## Spearman
corDist(M, method = "spearman")

##           1         2         3         4
## 2 1.0799925                              
## 3 0.9866692 1.0113658                    
## 4 0.8290512 1.0834606 1.1585555          
## 5 0.9807935 1.0018795 0.8963924 1.0837111

## Minimum Covariance Determinant
corDist(M, method = "mcd")

##           1         2         3         4
## 2 0.9975890                              
## 3 1.0935537 0.9548022                    
## 4 0.8083605 1.0899254 1.2154796          
## 5 0.8453323 0.9413417 1.0646901 1.0704574

MAD Matrix

In case of outliers the MAD may be useful as dispersion measure.

madMatrix(t(M))

##          [,1]     [,2]     [,3]     [,4]     [,5]
## [1,] 0.000000 3.625866 3.226823 2.826532 2.876544
## [2,] 3.625866 0.000000 3.213304 2.626208 2.768792
## [3,] 3.226823 3.213304 0.000000 3.013375 2.721847
## [4,] 2.826532 2.626208 3.013375 0.000000 2.824410
## [5,] 2.876544 2.768792 2.721847 2.824410 0.000000

Similarity Matrices

First, we can plot a similarity matrix based on correlation.

M <- matrix(rnorm(1000), ncol = 20)
colnames(M) <- paste("Sample", 1:20)
M.cor <- cor(M)
corPlot(M.cor, minCor = min(M.cor), labels = colnames(M))

Next, we can use the MAD.

## random data
x <- matrix(rnorm(1000), ncol = 10)
## outliers
x[1:20,5] <- x[1:20,5] + 10
madPlot(x, new = TRUE, maxMAD = 2.5, labels = TRUE,
        title = "MAD: Outlier visible")

## in contrast
corPlot(x, new = TRUE, minCor = -0.5, labels = TRUE,
        title = "Correlation: Outlier masked")

Colors for Heatmaps

Nowadays there are better solutions e.g. provided by Bioconductor package complexHeatmaps. This was my solution to get a better coloring of heatmaps.

## generate some random data
data.plot <- matrix(rnorm(100*50, sd = 1), ncol = 50)
colnames(data.plot) <- paste("patient", 1:50)
rownames(data.plot) <- paste("gene", 1:100)
data.plot[1:70, 1:30] <- data.plot[1:70, 1:30] + 3
data.plot[71:100, 31:50] <- data.plot[71:100, 31:50] - 1.4
data.plot[1:70, 31:50] <- rnorm(1400, sd = 1.2)
data.plot[71:100, 1:30] <- rnorm(900, sd = 1.2)
nrcol <- 128
## Load required packages
library(gplots)

## 
## Attaching package: 'gplots'

## The following object is masked from 'package:stats':
## 
##     lowess

library(RColorBrewer)
myCol <- rev(colorRampPalette(brewer.pal(10, "RdBu"))(nrcol))
heatmap.2(data.plot, col =  myCol, trace = "none", tracecol = "black",
          main = "standard colors")

farbe <- heatmapCol(data = data.plot, col = myCol, 
                    lim = min(abs(range(data.plot)))-1)
heatmap.2(data.plot, col = farbe, trace = "none", tracecol = "black",
          main = "heatmapCol colors")

String Distances

In Bioinformatics the (pairwise and multiple) alignment of strings is an important topic. For this one can use the distance or similarity between strings. The Hamming and the the Levenshtein (edit) distance are implemented in function stringDist.

x <- "GACGGATTATG"
y <- "GATCGGAATAG"
## Hamming distance
stringDist(x, y)

##             GACGGATTATG
## GATCGGAATAG           3

## Levenshtein distance
d <- stringDist(x, y)
d

##             GACGGATTATG
## GATCGGAATAG           3

In case of the Levenshtein (edit) distance, the respective scoring and traceback matrices are attached as attributes to the result.

attr(d, "ScoringMatrix")

##     gap  G A T C G G A A T  A  G
## gap   0  1 2 3 4 5 6 7 8 9 10 11
## G     1  0 1 2 3 4 5 6 7 8  9 10
## A     2  1 0 1 2 3 4 5 6 7  8  9
## C     3  2 1 1 1 2 3 4 5 6  7  8
## G     4  3 2 2 2 1 2 3 4 5  6  7
## G     5  4 3 3 3 2 1 2 3 4  5  6
## A     6  5 4 4 4 3 2 1 2 3  4  5
## T     7  6 5 4 5 4 3 2 2 2  3  4
## T     8  7 6 5 5 5 4 3 3 2  3  4
## A     9  8 7 6 6 6 5 4 3 3  2  3
## T    10  9 8 7 7 7 6 5 4 3  3  3
## G    11 10 9 8 8 7 7 6 5 4  4  3

attr(d, "TraceBackMatrix")

##     gap     G     A     T      C        G      G     A     A      T  
## gap "start" "i"   "i"   "i"    "i"      "i"    "i"   "i"   "i"    "i"
## G   "d"     "m"   "i"   "i"    "i"      "m/i"  "m/i" "i"   "i"    "i"
## A   "d"     "d"   "m"   "i"    "i"      "i"    "i"   "m/i" "m/i"  "i"
## C   "d"     "d"   "d"   "mm"   "m"      "i"    "i"   "i"   "i"    "i"
## G   "d"     "d/m" "d"   "d/mm" "d/mm"   "m"    "m/i" "i"   "i"    "i"
## G   "d"     "d/m" "d"   "d/mm" "d/mm"   "d/m"  "m"   "i"   "i"    "i"
## A   "d"     "d"   "d/m" "d/mm" "d/mm"   "d"    "d"   "m"   "m/i"  "i"
## T   "d"     "d"   "d"   "m"    "d/mm/i" "d"    "d"   "d"   "mm"   "m"
## T   "d"     "d"   "d"   "d/m"  "mm"     "d"    "d"   "d"   "d/mm" "m"
## A   "d"     "d"   "d/m" "d"    "d/mm"   "d/mm" "d"   "d/m" "m"    "d"
## T   "d"     "d"   "d"   "d/m"  "d/mm"   "d/mm" "d"   "d"   "d"    "m"
## G   "d"     "d/m" "d"   "d"    "d/mm"   "m"    "d/m" "d"   "d"    "d"
##     A      G     
## gap "i"    "i"   
## G   "i"    "m/i" 
## A   "m/i"  "i"   
## C   "i"    "i"   
## G   "i"    "m/i" 
## G   "i"    "m/i" 
## A   "m/i"  "i"   
## T   "i"    "i"   
## T   "mm/i" "mm/i"
## A   "m"    "i"   
## T   "d"    "mm"  
## G   "d/mm" "m"

The characters in the trace-back matrix reflect insertion of a gap in string y (d: deletion), match (m), mismatch (mm), and insertion of a gap in string x (i).

String Similarities

The function stringSim computes the optimal alignment scores for global (Needleman-Wunsch) and local (Smith-Waterman) alignments with constant gap penalties. Scoring and trace-back matrix are again attached as attributes to the results.

## optimal global alignment score
d <- stringSim(x, y)
d

##             GACGGATTATG
## GATCGGAATAG           6

attr(d, "ScoringMatrix")

##     gap  G  A  T  C  G  G  A  A  T   A   G
## gap   0 -1 -2 -3 -4 -5 -6 -7 -8 -9 -10 -11
## G    -1  1  0 -1 -2 -3 -4 -5 -6 -7  -8  -9
## A    -2  0  2  1  0 -1 -2 -3 -4 -5  -6  -7
## C    -3 -1  1  1  2  1  0 -1 -2 -3  -4  -5
## G    -4 -2  0  0  1  3  2  1  0 -1  -2  -3
## G    -5 -3 -1 -1  0  2  4  3  2  1   0  -1
## A    -6 -4 -2 -2 -1  1  3  5  4  3   2   1
## T    -7 -5 -3 -1 -2  0  2  4  4  5   4   3
## T    -8 -6 -4 -2 -2 -1  1  3  3  5   4   3
## A    -9 -7 -5 -3 -3 -2  0  2  4  4   6   5
## T   -10 -8 -6 -4 -4 -3 -1  1  3  5   5   5
## G   -11 -9 -7 -5 -5 -3 -2  0  2  4   4   6

attr(d, "TraceBackMatrix")

##     gap     G     A     T      C      G     G     A     A      T   A     
## gap "start" "i"   "i"   "i"    "i"    "i"   "i"   "i"   "i"    "i" "i"   
## G   "d"     "m"   "i"   "i"    "i"    "m/i" "m/i" "i"   "i"    "i" "i"   
## A   "d"     "d"   "m"   "i"    "i"    "i"   "i"   "m/i" "m/i"  "i" "m/i" 
## C   "d"     "d"   "d"   "mm"   "m"    "i"   "i"   "i"   "i"    "i" "i"   
## G   "d"     "d/m" "d"   "d/mm" "d"    "m"   "m/i" "i"   "i"    "i" "i"   
## G   "d"     "d/m" "d"   "d/mm" "d"    "d/m" "m"   "i"   "i"    "i" "i"   
## A   "d"     "d"   "d/m" "d/mm" "d"    "d"   "d"   "m"   "m/i"  "i" "m/i" 
## T   "d"     "d"   "d"   "m"    "d/i"  "d"   "d"   "d"   "mm"   "m" "i"   
## T   "d"     "d"   "d"   "d/m"  "mm"   "d"   "d"   "d"   "d/mm" "m" "mm/i"
## A   "d"     "d"   "d/m" "d"    "d/mm" "d"   "d"   "d/m" "m"    "d" "m"   
## T   "d"     "d"   "d"   "d/m"  "d/mm" "d"   "d"   "d"   "d"    "m" "d"   
## G   "d"     "d/m" "d"   "d"    "d/mm" "m"   "d/m" "d"   "d"    "d" "d/mm"
##     G     
## gap "i"   
## G   "m/i" 
## A   "i"   
## C   "i"   
## G   "m/i" 
## G   "m/i" 
## A   "i"   
## T   "i"   
## T   "mm/i"
## A   "i"   
## T   "mm"  
## G   "m"

## optimal local alignment score
d <- stringSim(x, y, global = FALSE)
d

##             GACGGATTATG
## GATCGGAATAG           6

attr(d, "ScoringMatrix")

##     gap G A T C G G A A T A G
## gap   0 0 0 0 0 0 0 0 0 0 0 0
## G     0 1 0 0 0 1 1 0 0 0 0 1
## A     0 0 2 1 0 0 0 2 1 0 1 0
## C     0 0 1 1 2 1 0 1 1 0 0 0
## G     0 1 0 0 1 3 2 1 0 0 0 1
## G     0 1 0 0 0 2 4 3 2 1 0 1
## A     0 0 2 1 0 1 3 5 4 3 2 1
## T     0 0 1 3 2 1 2 4 4 5 4 3
## T     0 0 0 2 2 1 1 3 3 5 4 3
## A     0 0 1 1 1 1 0 2 4 4 6 5
## T     0 0 0 2 1 0 0 1 3 5 5 5
## G     0 1 0 1 1 2 1 0 2 4 4 6

attr(d, "TraceBackMatrix")

##     gap     G        A           T           C        G            
## gap "start" "i"      "i"         "i"         "i"      "i"          
## G   "d"     "m"      "i/stop"    "stop"      "stop"   "m"          
## A   "d"     "d/stop" "m"         "i"         "i/stop" "d/stop"     
## C   "d"     "stop"   "d"         "mm"        "m"      "i"          
## G   "d"     "m"      "d/i/stop"  "d/mm/stop" "d"      "m"          
## G   "d"     "m"      "mm/i/stop" "stop"      "d/stop" "d/m"        
## A   "d"     "d/stop" "m"         "i"         "i/stop" "d"          
## T   "d"     "stop"   "d"         "m"         "i"      "i"          
## T   "d"     "stop"   "d/stop"    "d/m"       "mm"     "mm/i"       
## A   "d"     "stop"   "m"         "d"         "d/mm"   "mm"         
## T   "d"     "stop"   "d/stop"    "m"         "i"      "d/mm/i/stop"
## G   "d"     "m"      "i/stop"    "d"         "mm"     "m"          
##     G             A          A             T           A        G         
## gap "i"           "i"        "i"           "i"         "i"      "i"       
## G   "m"           "i/stop"   "stop"        "stop"      "stop"   "m"       
## A   "d/mm/stop"   "m"        "m/i"         "i/stop"    "m"      "d/i/stop"
## C   "i/stop"      "d"        "mm"          "mm/i/stop" "d/stop" "mm/stop" 
## G   "m/i"         "i"        "d/mm/i/stop" "mm/stop"   "stop"   "m"       
## G   "m"           "i"        "i"           "i"         "i/stop" "m"       
## A   "d"           "m"        "m/i"         "i"         "m/i"    "i"       
## T   "d"           "d"        "mm"          "m"         "i"      "i"       
## T   "d"           "d"        "d/mm"        "m"         "mm/i"   "mm/i"    
## A   "d/mm/i/stop" "d/m"      "m"           "d"         "m"      "i"       
## T   "mm/stop"     "d"        "d"           "m"         "d"      "mm"      
## G   "m/i"         "d/i/stop" "d"           "d"         "d/mm"   "m"

The entry stop indicates that the minimum similarity score has been reached.

Optimal Alignment

Finally, the function traceBack computes an optimal global or local alignment based on a trace back matrix as provided by function stringDist or stringSim.

x <- "GACGGATTATG"
y <- "GATCGGAATAG"
## Levenshtein distance
d <- stringDist(x, y)
## optimal global alignment
traceBack(d)

##    pairwise global alignment
## x' "GA-CGGATTATG"           
## y' "GATCGGAATA-G"

## Optimal global alignment score
d <- stringSim(x, y)
## optimal global alignment
traceBack(d)

##    pairwise global alignment
## x' "GA-CGGATTATG"           
## y' "GATCGGAATA-G"

## Optimal local alignment score
d <- stringSim(x, y, global = FALSE)
## optimal local alignment
traceBack(d, global = FALSE)

##    pairwise local alignment
## x' "GA-CGGATTA"            
## y' "GATCGGAATA"