ss_buc_rm_anova_general: Necessary Sample Size to Reach Desired Power for a...

In BUCSS: Bias and Uncertainty Corrected Sample Size

Necessary Sample Size to Reach Desired Power for a Within-Subjects ANOVA With Any Number of Factors Using a Publication Bias and Uncertainty Correction Procedure

Description

ss_buc_rm_anova_general returns the necessary total sample size to achieve a desired level of statistical power for a planned study testing any type of effect (omnibus, contrast) using a fully within-subjects ANOVA with any number of factors, based on information obtained from a previous study. The effect from the previous study can be corrected for publication bias and/or uncertainty to provide a sample size that will achieve more accurate statistical power for a planned study, when compared to approaches that use a sample effect size at face value or rely on sample size only. The bias and uncertainty adjusted previous study noncentrality parameter is also returned, together with the planning effect size, the effect size the plan is built on, as Cohen's f.

Usage

ss_buc_rm_anova_general(
  F_observed,
  N,
  df_numerator,
  alpha_prior = 0.05,
  alpha_planned = 0.05,
  assurance = 0.8,
  desired_power = 0.8,
  epsilon = 1
)

Arguments

F_observed	Observed F value from a previous study used to plan sample size for a planned study.
N	Total sample size of the previous study.
df_numerator	Numerator degrees of freedom for the effect of interest.
alpha_prior	The significance level \alpha a prior result had to reach to be published (more generally, to reach you): the correction assumes you see only results with p below alpha_prior. Enter a number above 0 and at most 1. A value of 1, which may also be written "No Publication Filter", means no publication filter: every p value is at most 1, so any result would have been published whatever its p value, there is no publication bias to correct, and only the correction for uncertainty (set by assurance) remains, as for a pilot study. Anderson, Kelley, and Maxwell (2017, p. 1552) note that this level, their \alpha_P, can be set equal to 1 when publication bias is thought not to apply. The string is read without regard to case, and the result echoes it as an alpha_prior of 1.
alpha_planned	Alpha level \alpha assumed for the planned study.
assurance	Desired level of assurance: the long run proportion of planned studies whose statistical power at the true effect reaches or surpasses desired_power, when each is planned from a prior study published under the rule alpha_prior describes. The adjusted noncentrality parameter is the lower limit of a one-sided confidence interval at this level, computed from the publication-truncated distribution of the prior statistic, so assurance = .5 plans from a median unbiased estimate (correcting for publication bias only), a larger value adds the correction for uncertainty, and a value below .5 is not recommended. The term follows Kelley and Maxwell (2003), who used assurance in sample size planning for the probability that a confidence interval will be no wider than desired. With alpha_prior = 1 and assurance = .80 the plan corresponds to safeguard power, which plans for the lower limit of a two-sided 60 percent confidence interval around the prior effect size rather than for the effect size itself (see BUCSS-package for how, and for where the two differ). Enter it as a proportion in (0, 1) or as a percentage greater than 1 (for example, 80 is read as .80); a value of exactly 1 is read as 1 percent. A percentage is echoed in the result's planning-input rows as the coerced proportion (80 is echoed as .80); the same applies to desired_power.
desired_power	Desired level of statistical power for the planned study: the probability that its test rejects the null hypothesis when the effect is present (Maxwell, Delaney, & Kelley, 2027). It must exceed alpha_planned: a test's power is never below its Type I error rate, so a value at or below alpha_planned is not allowable, and the function stops rather than return a plan. Enter it as a proportion in (0, 1) or as a percentage greater than 1; a value of exactly 1 is read as 1 percent (.01), which is then refused unless alpha_planned is below .01.
epsilon	The sphericity parameter \epsilon of the effect tested, from 1/df_numerator (its lower bound) to 1 (the default, which assumes sphericity). For a prior study reported with Greenhouse-Geisser or Huynh-Feldt corrected degrees of freedom, it is the reported numerator degrees of freedom divided by the uncorrected ones. An effect with df_numerator = 1 is always spherical and takes only 1. The same value describes the planned study, and it is echoed as the epsilon row of the result. See Details.

Details

Researchers often use the sample effect size from a prior study as an estimate of the likely size of an expected future effect in sample size planning. However, sample effect size estimates should not usually be used at face value to plan sample size, due to both publication bias and uncertainty.

The approach implemented in ss_buc_rm_anova_general uses the observed F value and sample size from a previous study to correct the noncentrality parameter associated with the effect of interest for publication bias and/or uncertainty. This new estimated noncentrality parameter is then used to calculate the necessary total sample size to achieve the desired level of power in the planned study.

The approach uses a likelihood function of a truncated noncentral F distribution, where the truncation occurs due to small effect sizes being unobserved due to publication bias. The numerator of the likelihood function is the density of a noncentral F distribution. The denominator is the power of the test, which serves to truncate the distribution. Thus, the ratio of the numerator and the denominator is a truncated noncentral F distribution. (See Taylor & Muller, 1996, Equation 2.1; Anderson, Kelley, & Maxwell, 2017, Equation 3; and Anderson & Maxwell, 2017, for more details.)

Assurance is the proportion of times that power will be at or above the desired level, if the experiment were to be reproduced many times. For example, assurance = .5 means that power will be above the desired level half of the time, but below the desired level the other half of the time. Selecting assurance = .5 (selecting the noncentrality parameter at the 50th percentile of the likelihood distribution) results in a median unbiased estimate of the population noncentrality parameter and does not correct for uncertainty. In order to correct for uncertainty, assurance > .5 can be selected, which corresponds to selecting the noncentrality parameter associated with the (1 - assurance) quantile of the likelihood distribution.

alpha_prior is the significance level a prior result had to reach to be published: the correction assumes that only results with p values below alpha_prior reach the literature, and so reach you. Different \alpha levels represent differing amounts of publication bias. For example, setting alpha_prior = .20 assumes that studies with p values less than .20 are published, whereas those with larger p values are not, which reflects less severe publication bias than the default of .05. If the previous study of interest has not been subjected to publication bias (e.g., a pilot study), set alpha_prior = 1, which may also be written alpha_prior = "No Publication Filter"; Anderson, Kelley, and Maxwell (2017, p. 1552) note that it can be set equal to 1 when publication bias is thought not to apply. Because no p value exceeds 1, this means no publication filter at all: any result would have been published whatever its p value, so there is no publication bias to correct, and only the correction for uncertainty, set by assurance, remains.

In some cases, the corrected noncentrality parameter for a given level of assurance will be estimated to be zero. This is an indication that, at the desired level of assurance, the previous study's effect cannot be accurately estimated due to high levels of uncertainty and bias. When this happens, subsequent sample size planning is not possible with the chosen specifications, and the function stops with an informative error rather than returning a result. The error reports the largest assurance the prior result can support, which is 1 - p/\alpha, where p is the prior study's p value and \alpha is alpha_prior; at any higher assurance the corrected noncentrality parameter is driven to zero. Two remedies are available. First, users can select a lower value of assurance (e.g., .8 instead of .95), at or below the reported ceiling. Second, users can reduce the influence of publication bias by setting alpha_prior at a value greater than .05, which raises the ceiling. Note that alpha_prior is not a property of the prior study, which is fixed, but the analyst's assumption about the publication threshold its literature faced. When the ceiling is at or below the recommended floor of .5, lowering assurance cannot help and alpha_prior is the only remaining lever. It is possible to correct for uncertainty only by setting alpha_prior = 1 and choosing the desired level of assurance. We encourage users to make the adjustments as minimal as possible.

The returned actual_power is the statistical power of the plan this function reports: the power of a study of the returned sample size when the effect is the returned bias and uncertainty adjusted noncentrality parameter. Because a sample size must be a whole number, actual_power is never below the desired_power that was requested and is usually a little above it.

Sphericity. The default epsilon = 1 assumes sphericity, as the uncorrected within-subjects test does. When a prior study reports Greenhouse-Geisser (1959) or Huynh-Feldt (1976) corrected degrees of freedom, supply epsilon, the reported numerator degrees of freedom divided by the uncorrected ones. For example, F(1.73, 50.2) for an effect with 2 numerator degrees of freedom gives epsilon = 1.73/2, about .865, and the denominator agrees: 50.2/58 is also about .865. The ratio of the two reported degrees of freedom, 50.2/1.73 = 29.0, is one less than the number of subjects the analysis used, here the study's 30; when it points to a different number (after dropping subjects with missing data, say), that number is the N to supply. An implied epsilon above 1 or below its lower bound (see Arguments) means the reported degrees of freedom are not a Greenhouse-Geisser or Huynh-Feldt correction of this effect; a Huynh-Feldt estimate above 1 is reported as the uncorrected degrees of freedom, which is epsilon = 1. ss_buc_rm_anova_general then applies the approximation of Muller and Barton (1989) to both studies: the prior F is treated as noncentral F with both degrees of freedom and the noncentrality parameter multiplied by epsilon, the publication threshold is the critical value at the corrected degrees of freedom, and the planned study's power is computed the same way. Each within-subjects effect has its own \epsilon, so supply the one reported for the effect you plan from. The returned ncp_adjusted stays on the sphericity scale, so it is comparable across values of epsilon, and the planned test's corrected degrees of freedom are the df_effect and df_error attributes. One epsilon describes both studies, because it is a property of the covariance matrix of the repeated measures, which the planned study shares with the prior one; the reported value is the prior study's estimate of it, and re-running across the values you find plausible shows how much the plan depends on it. The value used is echoed as the epsilon row of the result, 1 when sphericity is assumed.

The correction under epsilon is an approximation. Below sphericity the distribution of a within-subjects F depends on the whole covariance matrix of the repeated measures, and on how the effect lines up with it, not on \epsilon alone. In simulations of raw data (one-way designs of 4 and 6 levels with \epsilon from .45 to .86, prior studies of 12 to 40 subjects published when their Greenhouse-Geisser test reached p < .05, and a 2 x 4 split-plot interaction), planning from each published study with its own reported Greenhouse-Geisser estimate at an assurance of .80 gave a plan reaching .80 power for the Greenhouse-Geisser test in .70 to .80 of replications when the effect followed the dominant pattern of variation (a linear trend over autocorrelated occasions), and in .92 to .99 when it lay in the least variable contrasts. Ignoring the departure (epsilon = 1) reached it in .26 to .64 of replications for the trend-like effects and in .70 to .87 for the effects in the least variable contrasts. The shortfall does not shrink as the prior study grows, and is not larger near the lower bound of \epsilon. The planned study's power is approximated the same way. Separate simulations of planned one-way studies of 10 to 30 subjects, with 4, 6, or 8 levels, measured the real power of the Greenhouse-Geisser test, whose estimate of \epsilon is biased downward. For a trend-like effect (a linear trend over occasions with first-order autoregressive correlations of .3 to .9, \epsilon from .50 to .94) it fell below actual_power by about .04 to .08 with four levels and .06 to .13 with six, the larger shortfalls for the smaller plans; a planned study analyzed with the Huynh-Feldt correction tracks actual_power more closely. Even when sphericity holds and epsilon = 1, a planned study analyzed with the Greenhouse-Geisser correction anyway, as some software does by default, has less power than actual_power, the power of the uncorrected test: about .02 to .06 less with four levels, .03 to .11 with six, and .04 to .15 with eight, for plans of 30 down to 10 subjects (the Huynh-Feldt test is within about .02). When a paper reports both corrections, supply the Greenhouse-Geisser one: the Huynh-Feldt estimate is larger, and planning from it attained about .02 to .09 less, the larger differences from the smaller prior studies. When sphericity in fact holds but the prior study reported a Greenhouse-Geisser correction anyway, supplying it is conservative, with a median plan 7 to 34 percent larger.

The planning effect size and other power software. Here f_planning is Cohen's f relative to the effect's own error term, whose variance already reflects the correlation among the repeated measures, so f^2/(1 + f^2) is the population value of the partial eta squared a paper reports for the effect. It is not the f that power functions for repeated measures designs usually take, such as ss_power_rm_anova() in the sibling package DMAR: those standardize the effect by the standard deviation of the raw scores and take the correlation among the measures as a separate argument, so giving them f_planning, with any correlation, plans a different study. For a one-way design with a levels (df_numerator = a - 1), the value that reproduces this plan in ss_power_rm_anova(), with the correlation set to 0 and the same epsilon, is f_planning times \sqrt{(a - 1)/a}.

Value

An object of class bucss_plan: a data.frame with a character term column and a numeric value column, in the same shape as the sibling package DMAR's planners. The design results come first: the necessary total sample size for the planned study, named for its unit (necessary_n_per_group, necessary_n_per_cell, or necessary_N); for the per-group and per-cell designs, total_N, the implied total sample size; actual_power, the power of the plan returned, that is, of the returned sample size at the returned noncentrality parameter (see Details); ncp_adjusted, the publication bias and uncertainty adjusted prior study noncentrality parameter, on the scale of the F statistic, at the prior study's sample size, and on the sphericity scale for every epsilon (see Details); and the planning effect size, f_planning, Cohen's f for the effect tested, relative to its own error term, \sqrt{\lambda/(kN)}, where \lambda is ncp_adjusted, N the prior number of subjects, and k is df_numerator (the error degrees of freedom per subject), so f^2/(1 + f^2) is the population partial eta squared for the effect; like ncp_adjusted it is on the sphericity scale, and for epsilon below 1 the power statement that follows holds under the same Muller and Barton (1989) approximation, with the corrected degrees of freedom and noncentrality parameter; it is not the f that power functions for repeated measures take (see Details).

A planning effect size (the row whose name ends in _planning) is an adjusted effect size: the value, in the design's usual effect size metric, used to plan the sample size given the situation at hand (the prior study's result, the publication bias assumed through alpha_prior, and the uncertainty allowed for through assurance). It is ncp_adjusted restated in that metric and is what the plan is built on, not an estimate of the population effect to report: above an assurance of .5 it is deliberately conservative (a lower confidence limit), and at .5 it is the median unbiased estimate. Because it restates ncp_adjusted, actual_power is the ordinary power of a study of the returned sample size when the population effect is the planning effect size.

Rows echoing the planning inputs follow the design results, so the assumptions travel with the result. The design, the unit the sample size is counted in, the largest assurance this prior can support (the assurance ceiling), and the planned test's degrees of freedom (df_effect, and df_error where the test has a denominator) travel on attributes. print.bucss_plan shows the design, for the regression planners the predictor frame, the unit, and the ceiling beneath the table; tidy() and glance() give the compact and wide views, the latter with every attribute as a column.

Author(s)

Ken Kelley ([e-mail]) and Samantha F. Anderson ([e-mail])

References

Anderson, S. F., & Kelley, K. (2024). Sample size planning for replication studies: The devil is in the design. Psychological Methods, 29, 844–867. \Sexpr[results=rd]{tools:::Rd_expr_doi("10.1037/met0000520")}

Anderson, S. F., Kelley, K., & Maxwell, S. E. (2017). Sample-size planning for more accurate statistical power: A method adjusting sample effect sizes for publication bias and uncertainty. Psychological Science, 28, 1547–1562. \Sexpr[results=rd]{tools:::Rd_expr_doi("10.1177/0956797617723724")}

Anderson, S. F., & Maxwell, S. E. (2017). Addressing the "replication crisis": Using original studies to design replication studies with appropriate statistical power. Multivariate Behavioral Research, 52, 305–324. \Sexpr[results=rd]{tools:::Rd_expr_doi("10.1080/00273171.2017.1289361")}

Kelley, K., & Maxwell, S. E. (2003). Sample size for multiple regression: Obtaining regression coefficients that are accurate, not simply significant. Psychological Methods, 8, 305–321. \Sexpr[results=rd]{tools:::Rd_expr_doi("10.1037/1082-989X.8.3.305")}

Maxwell, S. E., Delaney, H. D., & Kelley, K. (2027). Designing experiments and analyzing data: A model comparison perspective (4th ed.). Routledge.

Taylor, D. J., & Muller, K. E. (1996). Bias in linear model power and sample size calculation due to estimating noncentrality. Communications in Statistics: Theory and Methods, 25, 1595–1610. \Sexpr[results=rd]{tools:::Rd_expr_doi("10.1080/03610929608831787")}

Greenhouse, S. W., & Geisser, S. (1959). On methods in the analysis of profile data. Psychometrika, 24, 95–112. \Sexpr[results=rd]{tools:::Rd_expr_doi("10.1007/BF02289823")}

Huynh, H., & Feldt, L. S. (1976). Estimation of the Box correction for degrees of freedom from sample data in randomized block and split-plot designs. Journal of Educational Statistics, 1, 69–82. \Sexpr[results=rd]{tools:::Rd_expr_doi("10.3102/10769986001001069")}

Muller, K. E., & Barton, C. N. (1989). Approximate power for repeated-measures ANOVA lacking sphericity. Journal of the American Statistical Association, 84, 549–555. \Sexpr[results=rd]{tools:::Rd_expr_doi("10.1080/01621459.1989.10478802")}

Examples

result <- ss_buc_rm_anova_general(F_observed = 6.5, N = 80, df_numerator = 1,
  alpha_prior = .05, alpha_planned = .05, assurance = .50, desired_power = .80)
result

# A prior study reported with Greenhouse-Geisser corrected degrees of
# freedom, 1.4 and 40.6, for an effect with 2 numerator degrees of freedom
# and 30 subjects: the correction is 1.4/2 (under sphericity, the plan is
# 46 subjects).
ss_buc_rm_anova_general(F_observed = 8, N = 30, df_numerator = 2,
  epsilon = .7)

# Requesting more assurance than the prior result can support stops with an
# informative error naming the largest workable assurance (here near .74):
try(ss_buc_rm_anova_general(F_observed = 6.5, N = 80, df_numerator = 1,
  assurance = .95))

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