In Detlew/PowerTOST: Power and Sample Size for (Bio)Equivalence Studies
knitr::opts_chunk$set(
collapse = TRUE,
comment = "#"
)
Introduction
The package contains functions to calculate power and estimate sample size for various study designs used in (not only bio-) equivalence studies. Power and sample size can be obtained based on different methods, amongst them prominently the TOST procedure (Two One-Sided t-Tests).\
Version r packageVersion("PowerTOST") built r packageDate("PowerTOST", date.fields = "Built") with R r getRversion().
For an overview of supported designs, methods, and defaults together with some basic examples see
Details and examples are accessible via the menu bar on top of the page and in the online manual of all functions.
Abbreviations, Definition of Terms, Models
2×2×2
: Crossover design with 2 treatments, 2 sequences, and 2 periods. In the literature also TR|RT or AB|AB. In the functions 2x2x2 or 2x2 for short.
2x2x3
: Full replicate designs with 2 treatments, 2 sequences, and 3 periods (TRT|RTR or TRR|RTT). Both T and R are administered twice to ½ of the subjects.
2x2x4
: Full replicate designs with 2 treatments, 2 sequences, and 4 periods (TRTR|RTRT, TRRT|RTTR, or TTRR|RRTT). Both T and R are administered twice to ½ of the subjects.
2×3×3
: Partial (or semi-) replicate design with 2 treatments, 3 sequences, and 3 periods (TRR|RTR|RRT or TRR|RTR). R is administered to all subjects twice and T once. The former is popular (though not optimal) and the latter (a.k.a. extra-reference design) not optimal because it is biased in the presence of period effects.
2×4×2
: Full replicate design with 2 treatments, 4 sequences, and 2 periods (TR|RT|TT|RR, Balaam’s design). Not optimal due to poor power characteristics.
2×4×4
: Full replicate designs with 2 treatments, 4 sequences, and 4 periods (TRTR|RTRT|TRRT|RTTR or TRTR|RTRT|TTRR|RRTT).
3×3, 3×6×3
: Higher-order crossover designs with 3 treatments, 3 or 6 sequences, and 3 periods (Latin Square ABC|BCA|CAB or the Williams’ design ABC|ACB|BAC|BCA|CAB|CBA). In the functions 3x3 and 3x6x3. Both have the same degrees of freedom (2n–4) in the conventional approach and therefore, require the same number of subjects.
4×4
: Higher-order crossover design with 4 treatments, 4 sequences, and 4 periods (Latin Square ABCD|BCDA|CDAB|DABC or any of the six Williams’ designs ADBC|BACD|CBDA|DCAB, ADCB|BCDA|CABD|DBAC, ACDB|BDCA|CBAD|DABC, ACBD|BADC|CDAB|DBCA, ABDC|BCAD|CDBA|DACB, ABCD|BDAC|CADB|DCBA).
ABE
: Average Bioequivalence with fixed limits based on a clinically not relevant difference $\small{\Delta}$. The common $\small{\Delta}$ 0.20 leads to $\small{\theta_1=1-\Delta,\:\theta_2=1/(1-\Delta)}$ or 80.00--125.00\%. For NTIDs (EMA and other jurisdicions) $\small{\Delta}$ 0.10 (90.00--111.11\%). For highly variable C~max~ (Russian Federation, South Africa) $\small{\Delta}$ 0.25 (75.00--133.33\%).$$H_0:\;\frac{\mu_\textrm{T}}{\mu_\textrm{R}}\ni\left{\theta_1,\,\theta_2\right}\;vs\;H_1:\;\theta_1<\frac{\mu_\textrm{T}}{\mu_\textrm{R}}<\theta_2$$
ABEL
: Average Bioequivalence with expanding limits (see also L, U). Same model like for ABE but $\small{\theta_1,\theta_2}$ are based on the CV~wR~ observed in the study.
$\alpha$
: Nominal level of the test. In tests for equivalence commonly 0.05 (except for the ratio of two means with normality on original scale based on Fieller’s (‘fiducial’) confidence interval in function sampleN.RatioF() and for non-inferiority/-superiority in function sampleN.noninf(), where it is 0.025). In the functions alpha.
$\beta$
: Probability that the Null-hypothesis of inequivalence is falsely not rejected. Also the type II error or producer’s risk, where $\small{\beta=1-\pi}$.
$\beta_0$
: Assumed or true slope of the (linearized) power model of dose-proportionality $\small{x=\alpha\cdot dose^{\,\beta},\:\log_{e}x=\alpha+\beta\cdot \log_{e}dose}$. Argument beta0.
CV
: Coefficient of variation
: Calculated from the residual error of the model of log-transformed data as $\small{CV=\sqrt{\exp (\sigma^2)+1}}$.
<ul>
<li>In crossover designs the within- (intra-) subject CV. Argument `CV`.</li>
<li>In parallel designs the total (pooled) CV. Argument `CV`.</li>
<li>In replicate designs the intra-subject CV (assuming homoscedasticity, argument `CV`). If heteroscedasticity is assumed, `CV` has to given as a vector with two elements `CV = c(x, y)`, where `CV[1]` is <a href="#CVwT">CV~wT~</a> and `CV[2]` is <a href="#CVwR">CV~wR~</a>.</li>
</ul>
CV~b~
: Between- (inter-) subject coefficient of variation. Argument CVb is required in function sampleN.RatioF() and in function sampleN.dp() if design = "IBD" (incomplete block design).
CV~cap~
: Upper cap in ABEL. If CV~wR~ > CV~cap~, expanding is based on CV~cap~ (and not on CV~wR~). In all jurisdictions 50\%, except for Health Canada, where CV~cap~ ≈57.4\%.
CV~switch~
: Switching coefficient of variation in reference-scaling. Only above this value reference-scaling is acceptable. For highly variable drugs / drug products 30\% (CV~0~ 0.30, s~0~ 0.294).
CV~wR~
: Within-subject coefficient of variation of R; can be estimated in any replicate design.
CV~wT~
: Within-subject coefficient of variation of T; can be estimated only in full replicate designs.
$\small{\Delta}$
: Clinically not relevant difference. Commonly 0.20. For NTIDs (EMA and other jurisdictions) $\small{\Delta}$ 0.10, for C~max~ (Russian Federation, South Africa) $\small{\Delta}$ 0.25.
HVD(P)
: Highly variable drug (product); commonly defined with a CV~wR~ of ≥30\%. HVDs exhibit highly variable clearances (CV~wR~ ≥30\% if administered as a solution), whereas HVDPs may additionally – or solely – show highly variable absorption. HVDP(s) generally are ones with a flat dose-response curve.
k
: Regulatory constant (also $\small{\theta_\textrm{s}}$)
: **<a href="#abel">ABEL</a>**: Based on the switching coefficient of variation $\small{CV_0=30\%}$. $\small{k=\log_{e}1.25/\sqrt{\log_{e}(CV_{0}^{2}+1)}\approx 0.760}$.
: **<a href="#rsabe">RSABE</a>**: Based on the switching standard deviation $\small{s_0=0.25}$. $\small{k=\log_{e}1.25/0.25\approx 0.8926}$.
L, U
: ABEL, RSABE
: **<a href="#abel">ABEL</a>**: Lower and upper expanded limits.
<ul>
<li>30% < <a href="#CVwR">CV~wR~</a> ≤ 50%: Based on $\small{s_\textrm{wR}}$, where $\small{\left\{ {L,\,U} \right\}= 100\cdot \exp (\mp 0.760 \cdot {s_\textrm{wR}})}$</li>
<li><a href="#CVwR">CV~wR~</a> > <a href="#CVcap">CV~cap~</a>: Applying $\small{s^*_\textrm{wR}=\sqrt{\log_{e}(CV_\textrm{cap}^{2}+1)}}$ in the expansion formula: $\small{\left\{ {L,\,U} \right\} = {69.84 - 143.19\%}}$. All jurisdictions except Health Canada, where $\small{\left\{ {L,\,U} \right\} = {66.7 - 150.0\%}}$.</li>
</ul>
: **<a href="#rsabe">RSABE</a>**: Lower and upper ‘implied limits’.
<ul>
<li>If $\small{s_\textrm{wR}\geq 0.294: \left\{ {L,\: U} \right\} = 100\cdot \exp (\mp 0.8926 \cdot {s_\textrm{wR}})}$</li>
</ul>
: Dose-Proportionality
: $\small{\left\{ {L,\,U} \right\}=\left[1+\log_{e}0.80/\log_{e}rd,\:1+\log_{e}1.25/\log_{e}rd \right]}$
margin
: Non-inferiority/-superiority margin (example for logscale = TRUE where $\theta_0=\mu_\textrm{T}/\mu_\textrm{R}$).
: **Non-inferiority**: If margin < 1, <u>higher</u> responses are are assumed to be better.
$$\small{H_0:\,\theta_0 \leq \log_{e}\textrm{margin}\:vs\:H_1:\,\theta_0>\log_{e}\textrm{margin}}$$
: **Non-superiority**: If margin > 1, <u>lower</u> responses are are assumed to be better.
$$\small{H_0:\,\theta_0 \geq \log_{e}\textrm{margin}\:vs\:H_1:\,\theta_0<\log_{e}\textrm{margin}}$$
n
: (Total) number of subjects.
n~seq~
: Number of sequences.
NTID
: Narrow therapeutic index drug, i.e., with a steep dose-response curve. A.k.a. NRD (Narrow Range Drug).
$\pi$
: Target (or desired) power in study planning. Commonly set to 0.80 – 0.90. In the functions targetpower.
R
: Reference (treatment, product).
rd
: Ratio of the highest/lowest dose. In the functions rd.
robust
: Selects degrees of freedom according to Senn’s basic estimator, where $\small{df=n-n_\textrm{seq}}$.
RSABE
: Reference-scaled Average Bioequivalence (U.S. FDA, China NMPA-CDE). Applicable if the intra-subject variability of the reference treatment s~wR~ ≥0.294 (CV~wR~ ≈ 30\%). The linearized model is $$\small{H_0:(\mu_\textrm{T}/\mu_\textrm{R})^2-\theta_\textrm{s}\cdot s_\textrm{wR}^{2}>0\:vs\:H_1:(\mu_\textrm{T}/\mu_\textrm{R})^2-\theta_\textrm{s}\cdot s_\textrm{wR}^{2}\leq 0}$$
See also ABEL.
$\theta_0$
: Assumed or true T/R-ratio (logscale = TRUE) or difference T – R (logscale = FALSE). In the functions theta0.
$\theta_1,\theta_2$
: Lower and upper limits of the equivalence range. In the functions theta1 and theta2.
$\theta_s$
: Regulatory constant in reference-scaling (see also k).
T
: Test (treatment, product).
TIE (type I error)
: Probability that the Null-hypothesis of inequivalence is falsely rejected (i.e., equivalence is concluded). Also the patient’s risk. Can be assessed with the power-functions setting theta0 = theta2 or theta0 = theta1.
Exact, except in reference-scaling based on simulations (power.scABEL(), power.RSABE(), power.NTIDFDA(), power.HVNTID()).
A Note on Rounding{#round}
In all functions sample sizes are estimated based on equivalence margins [$\small{\theta_1,\theta_2}$] in full numeric precision.
The widened margins for highly variable C~max~ are $\small{\theta_1=0.75,}$ $\small{\theta_2=1/\theta_1=1.\dot{3}}$ and not the rounded 75.00 – 133.33% according to the guidelines of the Russian Federation, the EEU, and the GCC. If for a NTID theta1 = 0.90 is specified, $\small{\theta_2=1/\theta_1=1.\dot{1}}$ and not the rounded 111.11% as in the guidelines. Health Canada requires rounding to only one decimal place with bioequivalence margins for NTIDs of 90.0 – 112.0%.\
Estimated sample sizes are generally not affected or – in extremely rare cases – conservative.
Example for a HVDP ($\small{\theta_0}$ 0.90, design 2x2x4) and a NTID ($\small{\theta_0}$ 0.975, design 2x2x2):
library(PowerTOST)
res <- data.frame(CV = c(rep(0.574, 3), rep(0.1, 2)),
regulator = c("EMA", "HC", "RU/EEU/GGC", "EMA", "HC"),
method = c(rep("ABEL", 2), rep("ABE", 3)),
L = NA, U = NA, n.GL = NA, theta1 = NA, theta2 = NA, n = NA,
stringsAsFactors = FALSE) # this line for R <4.0.0
for (i in 1:nrow(res)) {
if (i <= 2) {
LU <- scABEL(CV = res$CV[i], regulator = res$regulator[i])
if (i == 1) {
res[i, 4:5] <- sprintf("%.2f%%", 100*LU)
res[i, c(6, 9)] <- sampleN.scABEL(CV = res$CV[i], regulator = res$regulator[i],
design = "2x2x4", print = FALSE,
details = FALSE)[["Sample size"]]
res[i, 7:8] <- sprintf("%.6f", LU)
} else {
res[i, 4:5] <- sprintf("%.1f %%", 100*LU)
res[i, 7:8] <- sprintf("%.6f", LU)
res[i, c(6, 9)] <- sampleN.scABEL(CV = res$CV[i], regulator = res$regulator[i],
design = "2x2x4", print = FALSE,
details = FALSE)[["Sample size"]]
}
}
if (i == 3) {
LU <- c(0.75, 1/0.75)
res[i, 4:5] <- sprintf("%.2f%%", 100*LU)
res[i, 6] <- sampleN.TOST(CV = res$CV[i], theta1 = round(LU[1], 4),
theta2 = round(LU[2], 4), design = "2x2x4",
print = FALSE, details = FALSE)[["Sample size"]]
res[i, 7:8] <- sprintf("%.6f", LU)
res[i, 9] <- sampleN.TOST(CV = res$CV[i], theta1 = LU[1], theta2 = LU[2],
design = "2x2x4", print = FALSE,
details = FALSE)[["Sample size"]]
}
if (i == 4) {
LU <- c(0.9, 1/0.9)
res[i, 4:5] <- sprintf("%.2f%%", 100*LU)
res[i, 6] <- sampleN.TOST(CV = res$CV[i], theta0 = 0.975,
theta1 = round(LU[1], 4), theta2 = round(LU[2], 4),
print = FALSE, details = FALSE)[["Sample size"]]
res[i, 7:8] <- sprintf("%.6f", LU)
res[i, 9] <- sampleN.TOST(CV = res$CV[i], theta0 = 0.975, theta1 = LU[1],
theta2 = LU[2], print = FALSE,
details = FALSE)[["Sample size"]]
}
if (i == 5) {
LU <- c(0.9, 1/0.9)
res[i, 4:5] <- sprintf("%.1f %%", c(90, 112))
res[i, 6] <- sampleN.TOST(CV = res$CV[i], theta0 = 0.975,
theta1 = 0.9, theta2 = 1.12,
print = FALSE, details = FALSE)[["Sample size"]]
res[i, 7:8] <- sprintf("%.6f", LU)
res[i, 9] <- sampleN.TOST(CV = res$CV[i], theta0 = 0.975, theta1 = LU[1],
theta2 = LU[2], print = FALSE,
details = FALSE)[["Sample size"]]
}
}
names(res)[c(2, 4:6)] <- c("agency", "L ", "U ", "n")
print(res, row.names = FALSE)
Installation
You can install the released version of PowerTOST from CRAN with …
package <- "PowerTOST"
inst <- package %in% installed.packages()
if (length(package[!inst]) > 0) install.packages(package[!inst])
… and the development version from GitHub with
# install.packages("remotes")
remotes::install_github("Detlew/PowerTOST")
Skips installation from a github remote if the SHA-1 has not changed since last install. Use force = TRUE to force installation.
Contributors
- Detlew Labes (author, maintainer)
- Helmut Schütz (author)
- Benjamin Lang (author)
License{#license}
GPL-3 r Sys.Date() Helmut Schütz
Detlew/PowerTOST documentation built on March 26, 2024, 12:18 a.m.
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knitr::opts_chunk$set( collapse = TRUE, comment = "#" )
Introduction
The package contains functions to calculate power and estimate sample size for various study designs used in (not only bio-) equivalence studies. Power and sample size can be obtained based on different methods, amongst them prominently the TOST procedure (Two One-Sided t-Tests).\
Version r packageVersion("PowerTOST") built r packageDate("PowerTOST", date.fields = "Built") with R r getRversion().
For an overview of supported designs, methods, and defaults together with some basic examples see
Details and examples are accessible via the menu bar on top of the page and in the online manual of all functions.
Abbreviations, Definition of Terms, Models
2×2×2
: Crossover design with 2 treatments, 2 sequences, and 2 periods. In the literature also TR|RT or AB|AB. In the functions 2x2x2 or 2x2 for short.
2x2x3 : Full replicate designs with 2 treatments, 2 sequences, and 3 periods (TRT|RTR or TRR|RTT). Both T and R are administered twice to ½ of the subjects.
2x2x4 : Full replicate designs with 2 treatments, 2 sequences, and 4 periods (TRTR|RTRT, TRRT|RTTR, or TTRR|RRTT). Both T and R are administered twice to ½ of the subjects.
2×3×3 : Partial (or semi-) replicate design with 2 treatments, 3 sequences, and 3 periods (TRR|RTR|RRT or TRR|RTR). R is administered to all subjects twice and T once. The former is popular (though not optimal) and the latter (a.k.a. extra-reference design) not optimal because it is biased in the presence of period effects.
2×4×2 : Full replicate design with 2 treatments, 4 sequences, and 2 periods (TR|RT|TT|RR, Balaam’s design). Not optimal due to poor power characteristics.
2×4×4 : Full replicate designs with 2 treatments, 4 sequences, and 4 periods (TRTR|RTRT|TRRT|RTTR or TRTR|RTRT|TTRR|RRTT).
3×3, 3×6×3
: Higher-order crossover designs with 3 treatments, 3 or 6 sequences, and 3 periods (Latin Square ABC|BCA|CAB or the Williams’ design ABC|ACB|BAC|BCA|CAB|CBA). In the functions 3x3 and 3x6x3. Both have the same degrees of freedom (2n–4) in the conventional approach and therefore, require the same number of subjects.
4×4 : Higher-order crossover design with 4 treatments, 4 sequences, and 4 periods (Latin Square ABCD|BCDA|CDAB|DABC or any of the six Williams’ designs ADBC|BACD|CBDA|DCAB, ADCB|BCDA|CABD|DBAC, ACDB|BDCA|CBAD|DABC, ACBD|BADC|CDAB|DBCA, ABDC|BCAD|CDBA|DACB, ABCD|BDAC|CADB|DCBA).
ABE : Average Bioequivalence with fixed limits based on a clinically not relevant difference $\small{\Delta}$. The common $\small{\Delta}$ 0.20 leads to $\small{\theta_1=1-\Delta,\:\theta_2=1/(1-\Delta)}$ or 80.00--125.00\%. For NTIDs (EMA and other jurisdicions) $\small{\Delta}$ 0.10 (90.00--111.11\%). For highly variable C~max~ (Russian Federation, South Africa) $\small{\Delta}$ 0.25 (75.00--133.33\%).$$H_0:\;\frac{\mu_\textrm{T}}{\mu_\textrm{R}}\ni\left{\theta_1,\,\theta_2\right}\;vs\;H_1:\;\theta_1<\frac{\mu_\textrm{T}}{\mu_\textrm{R}}<\theta_2$$
ABEL : Average Bioequivalence with expanding limits (see also L, U). Same model like for ABE but $\small{\theta_1,\theta_2}$ are based on the CV~wR~ observed in the study.
$\alpha$
: Nominal level of the test. In tests for equivalence commonly 0.05 (except for the ratio of two means with normality on original scale based on Fieller’s (‘fiducial’) confidence interval in function sampleN.RatioF() and for non-inferiority/-superiority in function sampleN.noninf(), where it is 0.025). In the functions alpha.
$\beta$ : Probability that the Null-hypothesis of inequivalence is falsely not rejected. Also the type II error or producer’s risk, where $\small{\beta=1-\pi}$.
$\beta_0$
: Assumed or true slope of the (linearized) power model of dose-proportionality $\small{x=\alpha\cdot dose^{\,\beta},\:\log_{e}x=\alpha+\beta\cdot \log_{e}dose}$. Argument beta0.
CV : Coefficient of variation
: Calculated from the residual error of the model of log-transformed data as $\small{CV=\sqrt{\exp (\sigma^2)+1}}$.
<ul>
<li>In crossover designs the within- (intra-) subject CV. Argument `CV`.</li>
<li>In parallel designs the total (pooled) CV. Argument `CV`.</li>
<li>In replicate designs the intra-subject CV (assuming homoscedasticity, argument `CV`). If heteroscedasticity is assumed, `CV` has to given as a vector with two elements `CV = c(x, y)`, where `CV[1]` is <a href="#CVwT">CV~wT~</a> and `CV[2]` is <a href="#CVwR">CV~wR~</a>.</li>
</ul>
CV~b~
: Between- (inter-) subject coefficient of variation. Argument CVb is required in function sampleN.RatioF() and in function sampleN.dp() if design = "IBD" (incomplete block design).
CV~cap~ : Upper cap in ABEL. If CV~wR~ > CV~cap~, expanding is based on CV~cap~ (and not on CV~wR~). In all jurisdictions 50\%, except for Health Canada, where CV~cap~ ≈57.4\%.
CV~switch~ : Switching coefficient of variation in reference-scaling. Only above this value reference-scaling is acceptable. For highly variable drugs / drug products 30\% (CV~0~ 0.30, s~0~ 0.294).
CV~wR~ : Within-subject coefficient of variation of R; can be estimated in any replicate design.
CV~wT~ : Within-subject coefficient of variation of T; can be estimated only in full replicate designs.
$\small{\Delta}$ : Clinically not relevant difference. Commonly 0.20. For NTIDs (EMA and other jurisdictions) $\small{\Delta}$ 0.10, for C~max~ (Russian Federation, South Africa) $\small{\Delta}$ 0.25.
HVD(P) : Highly variable drug (product); commonly defined with a CV~wR~ of ≥30\%. HVDs exhibit highly variable clearances (CV~wR~ ≥30\% if administered as a solution), whereas HVDPs may additionally – or solely – show highly variable absorption. HVDP(s) generally are ones with a flat dose-response curve.
k : Regulatory constant (also $\small{\theta_\textrm{s}}$)
: **<a href="#abel">ABEL</a>**: Based on the switching coefficient of variation $\small{CV_0=30\%}$. $\small{k=\log_{e}1.25/\sqrt{\log_{e}(CV_{0}^{2}+1)}\approx 0.760}$. : **<a href="#rsabe">RSABE</a>**: Based on the switching standard deviation $\small{s_0=0.25}$. $\small{k=\log_{e}1.25/0.25\approx 0.8926}$.
L, U : ABEL, RSABE
: **<a href="#abel">ABEL</a>**: Lower and upper expanded limits. <ul> <li>30% < <a href="#CVwR">CV~wR~</a> ≤ 50%: Based on $\small{s_\textrm{wR}}$, where $\small{\left\{ {L,\,U} \right\}= 100\cdot \exp (\mp 0.760 \cdot {s_\textrm{wR}})}$</li> <li><a href="#CVwR">CV~wR~</a> > <a href="#CVcap">CV~cap~</a>: Applying $\small{s^*_\textrm{wR}=\sqrt{\log_{e}(CV_\textrm{cap}^{2}+1)}}$ in the expansion formula: $\small{\left\{ {L,\,U} \right\} = {69.84 - 143.19\%}}$. All jurisdictions except Health Canada, where $\small{\left\{ {L,\,U} \right\} = {66.7 - 150.0\%}}$.</li> </ul> : **<a href="#rsabe">RSABE</a>**: Lower and upper ‘implied limits’. <ul> <li>If $\small{s_\textrm{wR}\geq 0.294: \left\{ {L,\: U} \right\} = 100\cdot \exp (\mp 0.8926 \cdot {s_\textrm{wR}})}$</li> </ul>
: Dose-Proportionality
: $\small{\left\{ {L,\,U} \right\}=\left[1+\log_{e}0.80/\log_{e}rd,\:1+\log_{e}1.25/\log_{e}rd \right]}$
margin
: Non-inferiority/-superiority margin (example for logscale = TRUE where $\theta_0=\mu_\textrm{T}/\mu_\textrm{R}$).
: **Non-inferiority**: If margin < 1, <u>higher</u> responses are are assumed to be better. $$\small{H_0:\,\theta_0 \leq \log_{e}\textrm{margin}\:vs\:H_1:\,\theta_0>\log_{e}\textrm{margin}}$$ : **Non-superiority**: If margin > 1, <u>lower</u> responses are are assumed to be better. $$\small{H_0:\,\theta_0 \geq \log_{e}\textrm{margin}\:vs\:H_1:\,\theta_0<\log_{e}\textrm{margin}}$$
n : (Total) number of subjects.
n~seq~ : Number of sequences.
NTID : Narrow therapeutic index drug, i.e., with a steep dose-response curve. A.k.a. NRD (Narrow Range Drug).
$\pi$
: Target (or desired) power in study planning. Commonly set to 0.80 – 0.90. In the functions targetpower.
R : Reference (treatment, product).
rd
: Ratio of the highest/lowest dose. In the functions rd.
robust
: Selects degrees of freedom according to Senn’s basic estimator, where $\small{df=n-n_\textrm{seq}}$.
RSABE : Reference-scaled Average Bioequivalence (U.S. FDA, China NMPA-CDE). Applicable if the intra-subject variability of the reference treatment s~wR~ ≥0.294 (CV~wR~ ≈ 30\%). The linearized model is $$\small{H_0:(\mu_\textrm{T}/\mu_\textrm{R})^2-\theta_\textrm{s}\cdot s_\textrm{wR}^{2}>0\:vs\:H_1:(\mu_\textrm{T}/\mu_\textrm{R})^2-\theta_\textrm{s}\cdot s_\textrm{wR}^{2}\leq 0}$$ See also ABEL.
$\theta_0$
: Assumed or true T/R-ratio (logscale = TRUE) or difference T – R (logscale = FALSE). In the functions theta0.
$\theta_1,\theta_2$
: Lower and upper limits of the equivalence range. In the functions theta1 and theta2.
$\theta_s$ : Regulatory constant in reference-scaling (see also k).
T : Test (treatment, product).
TIE (type I error)
: Probability that the Null-hypothesis of inequivalence is falsely rejected (i.e., equivalence is concluded). Also the patient’s risk. Can be assessed with the power-functions setting theta0 = theta2 or theta0 = theta1.
Exact, except in reference-scaling based on simulations (power.scABEL(), power.RSABE(), power.NTIDFDA(), power.HVNTID()).
A Note on Rounding{#round}
In all functions sample sizes are estimated based on equivalence margins [$\small{\theta_1,\theta_2}$] in full numeric precision.
The widened margins for highly variable C~max~ are $\small{\theta_1=0.75,}$ $\small{\theta_2=1/\theta_1=1.\dot{3}}$ and not the rounded 75.00 – 133.33% according to the guidelines of the Russian Federation, the EEU, and the GCC. If for a NTID theta1 = 0.90 is specified, $\small{\theta_2=1/\theta_1=1.\dot{1}}$ and not the rounded 111.11% as in the guidelines. Health Canada requires rounding to only one decimal place with bioequivalence margins for NTIDs of 90.0 – 112.0%.\
Estimated sample sizes are generally not affected or – in extremely rare cases – conservative.
Example for a HVDP ($\small{\theta_0}$ 0.90, design 2x2x4) and a NTID ($\small{\theta_0}$ 0.975, design 2x2x2):
library(PowerTOST) res <- data.frame(CV = c(rep(0.574, 3), rep(0.1, 2)), regulator = c("EMA", "HC", "RU/EEU/GGC", "EMA", "HC"), method = c(rep("ABEL", 2), rep("ABE", 3)), L = NA, U = NA, n.GL = NA, theta1 = NA, theta2 = NA, n = NA, stringsAsFactors = FALSE) # this line for R <4.0.0 for (i in 1:nrow(res)) { if (i <= 2) { LU <- scABEL(CV = res$CV[i], regulator = res$regulator[i]) if (i == 1) { res[i, 4:5] <- sprintf("%.2f%%", 100*LU) res[i, c(6, 9)] <- sampleN.scABEL(CV = res$CV[i], regulator = res$regulator[i], design = "2x2x4", print = FALSE, details = FALSE)[["Sample size"]] res[i, 7:8] <- sprintf("%.6f", LU) } else { res[i, 4:5] <- sprintf("%.1f %%", 100*LU) res[i, 7:8] <- sprintf("%.6f", LU) res[i, c(6, 9)] <- sampleN.scABEL(CV = res$CV[i], regulator = res$regulator[i], design = "2x2x4", print = FALSE, details = FALSE)[["Sample size"]] } } if (i == 3) { LU <- c(0.75, 1/0.75) res[i, 4:5] <- sprintf("%.2f%%", 100*LU) res[i, 6] <- sampleN.TOST(CV = res$CV[i], theta1 = round(LU[1], 4), theta2 = round(LU[2], 4), design = "2x2x4", print = FALSE, details = FALSE)[["Sample size"]] res[i, 7:8] <- sprintf("%.6f", LU) res[i, 9] <- sampleN.TOST(CV = res$CV[i], theta1 = LU[1], theta2 = LU[2], design = "2x2x4", print = FALSE, details = FALSE)[["Sample size"]] } if (i == 4) { LU <- c(0.9, 1/0.9) res[i, 4:5] <- sprintf("%.2f%%", 100*LU) res[i, 6] <- sampleN.TOST(CV = res$CV[i], theta0 = 0.975, theta1 = round(LU[1], 4), theta2 = round(LU[2], 4), print = FALSE, details = FALSE)[["Sample size"]] res[i, 7:8] <- sprintf("%.6f", LU) res[i, 9] <- sampleN.TOST(CV = res$CV[i], theta0 = 0.975, theta1 = LU[1], theta2 = LU[2], print = FALSE, details = FALSE)[["Sample size"]] } if (i == 5) { LU <- c(0.9, 1/0.9) res[i, 4:5] <- sprintf("%.1f %%", c(90, 112)) res[i, 6] <- sampleN.TOST(CV = res$CV[i], theta0 = 0.975, theta1 = 0.9, theta2 = 1.12, print = FALSE, details = FALSE)[["Sample size"]] res[i, 7:8] <- sprintf("%.6f", LU) res[i, 9] <- sampleN.TOST(CV = res$CV[i], theta0 = 0.975, theta1 = LU[1], theta2 = LU[2], print = FALSE, details = FALSE)[["Sample size"]] } } names(res)[c(2, 4:6)] <- c("agency", "L ", "U ", "n") print(res, row.names = FALSE)
Installation
You can install the released version of PowerTOST from CRAN with …
package <- "PowerTOST" inst <- package %in% installed.packages() if (length(package[!inst]) > 0) install.packages(package[!inst])
… and the development version from GitHub with
# install.packages("remotes")
remotes::install_github("Detlew/PowerTOST")
Skips installation from a github remote if the SHA-1 has not changed since last install. Use force = TRUE to force installation.
Contributors
- Detlew Labes (author, maintainer)
- Helmut Schütz (author)
- Benjamin Lang (author)
License{#license}
GPL-3 r Sys.Date() Helmut Schütz
R Package Documentation
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