# Introduction to rsimsum

#### Alessandro Gasparini

#### 2026-04-21

# rsimsum

`rsimsum` is an R package that can compute summary statistics from simulation studies. It is inspired by the user-written command `simsum` in Stata (White I.R., 2010).

The aim of `rsimsum` is helping reporting of simulation studies, including understanding the role of chance in results of simulation studies. Specifically, `rsimsum` can compute Monte Carlo standard errors of summary statistics, defined as the standard deviation of the estimated summary statistic; these are reported by default.

Formula for summary statistics and Monte Carlo standard errors are presented in the next section. Note that the terms summary statistic and performance measure are used interchangeably.

# Notation

We will use th following notation throughout this vignette:

- \(\theta\): an estimand, and its true value
- \(n_{\text{sim}}\): number of simulations
- \(i = 1, \dots, n_{\text{sim}}\): indexes a given simulation
- \(\hat{\theta}_i\): the estimated value of \(\theta\) for the \(i^{\text{th}}\) replication
- \(\widehat{\text{Var}}(\hat{\theta}_i)\): the estimated variance \(\text{Var}(\hat{\theta}_i)\) of \(\hat{\theta}_i\) for the \(i^{\text{th}}\) replication
- \(\text{Var}(\hat{\theta})\): the empirical variance of \(\hat{\theta}\)
- \(\alpha\): the nominal significance level

# Performance measures

The first performance measure of interest is bias, which quantifies whether the estimator targets the true value \(\theta\) on average. Bias is calculated as:

\[ \text{Bias} = \frac{1}{n_{\text{sim}}} \sum_{i = 1} ^ {n_{\text{sim}}} \hat{\theta}_i - \theta \]

The Monte Carlo standard error of bias is calculated as:

\[ \text{MCSE(Bias)} = \sqrt{\frac{\frac{1}{n_{\text{sim}} - 1} \sum_{i = 1} ^ {n_{\text{sim}}} (\hat{\theta}_i - \bar{\theta}) ^ 2}{n_{\text{sim}}}} \]

`rsimsum` can also compute relative bias (relative to the true value \(\theta\)), which can be interpreted similarly as with bias, but in relative terms rather than absolute. This is calculated as:

\[ \text{Relative Bias} = \frac{1}{n_{\text{sim}}} \sum_{i = 1} ^ {n_{\text{sim}}} \frac{\hat{\theta}_i - \theta}{\theta} \]

Its Monte Carlo standard error is calculated as:

\[ \text{MCSE(Relative Bias)} = \sqrt{\frac{1}{n_{\text{sim}} (n_{\text{sim}} - 1)} \sum_i^{n_{\text{sim}}} \left[ \frac{\hat{\theta}_i - \theta}{\theta} - \widehat{\text{Relative Bias}} \right]^2} \]

The empirical standard error of \(\theta\) depends only on \(\hat{\theta}\) and does not require any knowledge of \(\theta\). It estimates the standard deviation of \(\hat{\theta}\) over the \(n_{\text{sim}}\) replications:

\[ \text{Empirical SE} = \sqrt{\frac{1}{n_{\text{sim}} - 1} \sum_{i = 1} ^ {n_{\text{sim}}} (\hat{\theta}_i - \bar{\theta}) ^ 2} \]

The Monte Carlo standard error is calculated as:

\[ \text{MCSE(Emp. SE)} = \frac{\widehat{\text{Emp. SE}}}{\sqrt{2 (n_{\text{sim}} - 1)}} \]

When comparing different methods, the relative precision of a given method B against a reference method A is computed as:

\[ \text{Relative \% increase in precision} = 100 \left[ \left( \frac{\widehat{\text{Emp. SE}}_A}{\widehat{\text{Emp. SE}}_B} \right) ^ 2 - 1 \right] \]

Its (approximated) Monte Carlo standard error is:

\[ \text{MCSE(Relative \% increase in precision)} \simeq 200 \left( \frac{\widehat{\text{Emp. SE}}_A}{\widehat{\text{Emp. SE}}_B} \right)^2 \sqrt{\frac{1 - \rho^2_{AB}}{n_{\text{sim}} - 1}} \]

\(\rho^2_{AB}\) is the correlation of \(\hat{\theta}_A\) and \(\hat{\theta}_B\).

A measure that takes into account both precision and accuracy of a method is the mean squared error, which is the sum of the squared bias and variance of \(\hat{\theta}\):

\[ \text{MSE} = \frac{1}{n_{\text{sim}}} \sum_{i = 1} ^ {n_{\text{sim}}} (\hat{\theta}_i - \theta) ^ 2 \]

The Monte Carlo standard error is:

\[ \text{MCSE(MSE)} = \sqrt{\frac{\sum_{i = 1} ^ {n_{\text{sim}}} \left[ (\hat{\theta}_i - \theta) ^2 - \text{MSE} \right] ^ 2}{n_{\text{sim}} (n_{\text{sim}} - 1)}} \]

The model based standard error is computed by averaging the estimated standard errors for each replication:

\[ \text{Model SE} = \sqrt{\frac{1}{n_{\text{sim}}} \sum_{i = 1} ^ {n_{\text{sim}}} \widehat{\text{Var}}(\hat{\theta}_i)} \]

Its (approximated) Monte Carlo standard error is computed as:

\[ \text{MCSE(Model SE)} \simeq \sqrt{\frac{\text{Var}[\widehat{\text{Var}}(\hat{\theta}_i)]}{4 n_{\text{sim}} \widehat{\text{Model SE}}}} \]

The model standard error targets the empirical standard error. Hence, the relative error in the model standard error is an informative performance measure:

\[ \text{Relative \% error in model SE} = 100 \left( \frac{\text{Model SE}}{\text{Empirical SE}} - 1\right) \]

Its Monte Carlo standard error is computed as:

\[ \text{MCSE(Relative \% error in model SE)} = 100 \left( \frac{\text{Model SE}}{\text{Empirical SE}} \right) \sqrt{\frac{\text{Var}[\widehat{\text{Var}}(\hat{\theta}_i)]}{4 n_{\text{sim}} \widehat{\text{Model SE}} ^ 4} + \frac{1}{2(n_{\text{sim}} - 1)}} \]

Coverage is another key property of an estimator. It is defined as the probability that a confidence interval contains the true value \(\theta\), and computed as:

\[ \text{Coverage} = \frac{1}{n_{\text{sim}}} \sum_{i = 1} ^ {n_{\text{sim}}} I(\hat{\theta}_{i, \text{low}} \le \theta \le \hat{\theta}_{i, \text{upp}}) \]

where \(I(\cdot)\) is the indicator function. The Monte Carlo standard error is computed as:

\[ \text{MCSE(Coverage)} = \sqrt{\frac{\text{Coverage} \times (1 - \text{Coverage})}{n_{\text{sim}}}} \]

Under coverage is to be expected if:

1. \(\text{Bias} \ne 0\), or
2. \(\text{Models SE} < \text{Empirical SE}\), or
3. the distribution of \(\hat{\theta}\) is not normal and intervals have been constructed assuming normality, or
4. \(\widehat{\text{Var}}(\hat{\theta}_i)\) is too variable

Over coverage occurs as a result of \(\text{Models SE} > \text{Empirical SE}\).

As under coverage may be a result of bias, another useful summary statistic is bias-eliminated coverage:

\[ \text{Bias-eliminated (BE) coverage} = \frac{1}{n_{\text{sim}}} \sum_{i = 1} ^ {n_{\text{sim}}} I(\hat{\theta}_{i, \text{low}} \le \bar{\theta} \le \hat{\theta}_{i, \text{upp}}) \]

The Monte Carlo standard error is analogously as coverage:

\[ \text{MCSE(BE coverage)} = \sqrt{\frac{\text{BE coverage} \times (1 - \text{BE coverage})}{n_{\text{sim}}}} \]

Finally, power of a significance test at the \(\alpha\) level is defined as:

\[ \text{Power} = \frac{1}{n_{\text{sim}}} \sum_{i = 1} ^ {n_{\text{sim}}} I \left[ |\hat{\theta}_i| \ge z_{\alpha/2} \times \sqrt{\widehat{\text{Var}}(\hat{\theta_i})} \right] \]

The Monte Carlo standard error is analogously as coverage:

\[ \text{MCSE(Power)} = \sqrt{\frac{\text{Power} \times (1 - \text{Power})}{n_{\text{sim}}}} \]

Further information on summary statistics for simulation studies can be found in White (2010) and Morris, White, and Crowther (2019).

# Example 1: Simulation study on missing data

With this example dataset included in `rsimsum` we aim to summarise a simulation study comparing different ways to handle missing covariates when fitting a Cox model (White and Royston, 2009). One thousand datasets were simulated, each containing normally distributed covariates \(x\) and \(z\) and time-to-event outcome. Both covariates has \(20\%\) of their values deleted independently of all other variables so the data became missing completely at random (Little and Rubin, 2002). Each simulated dataset was analysed in three ways. A Cox model was fit to the complete cases (`CC`). Then two methods of multiple imputation using chained equations (van Buuren, Boshuizen, and Knook, 1999) were used. The `MI_LOGT` method multiply imputes the missing values of \(x\) and \(z\) with the outcome included as \(\log(t)\) and \(d\), where \(t\) is the survival time and \(d\) is the event indicator. The `MI_T` method is the same except that \(\log(t)\) is replaced by \(t\) in the imputation model.

We load the data in the usual way:

    library(rsimsum)
    data("MIsim", package = "rsimsum")

Let’s have a look at the first 10 rows of the dataset:

    head(MIsim, n = 10)
    #> # A tibble: 10 × 4
    #>    dataset method      b    se
    #>      <dbl> <chr>   <dbl> <dbl>
    #>  1       1 CC      0.707 0.147
    #>  2       1 MI_T    0.684 0.126
    #>  3       1 MI_LOGT 0.712 0.141
    #>  4       2 CC      0.349 0.160
    #>  5       2 MI_T    0.406 0.141
    #>  6       2 MI_LOGT 0.429 0.136
    #>  7       3 CC      0.650 0.152
    #>  8       3 MI_T    0.503 0.130
    #>  9       3 MI_LOGT 0.560 0.117
    #> 10       4 CC      0.432 0.126

The included variables are:

    str(MIsim)
    #> tibble [3,000 × 4] (S3: tbl_df/tbl/data.frame)
    #>  $ dataset: num [1:3000] 1 1 1 2 2 2 3 3 3 4 ...
    #>  $ method : chr [1:3000] "CC" "MI_T" "MI_LOGT" "CC" ...
    #>  $ b      : num [1:3000] 0.707 0.684 0.712 0.349 0.406 ...
    #>  $ se     : num [1:3000] 0.147 0.126 0.141 0.16 0.141 ...
    #>  - attr(*, "label")= chr "simsum example: data from a simulation study comparing 3 ways to handle missing"

- `dataset`, the number of the simulated dataset;

- `method`, the method used (`CC`, `MI_LOGT` or `MI_T`);

- `b`, the point estimate;

- `se`, the standard error of the point estimate.

We summarise the results of the simulation study by method using the `simsum` function:

    s1 <- simsum(data = MIsim, estvarname = "b", true = 0.50, se = "se", methodvar = "method", ref = "CC")

We set `true = 0.50` as the true value of the point estimate `b` - under which the data was simulated - is 0.50. We select `CC` as the reference method as we consider the complete cases analysis the reference method to benchmark against; if we do not set a reference method, `simsum` picks one automatically.

Using the default settings, Monte Carlo standard errors are computed and returned.

Summarising a `simsum` object, we obtain the following output:

    ss1 <- summary(s1)
    ss1
    #> Values are:
    #>  Point Estimate (Monte Carlo Standard Error)
    #>
    #> Non-missing point estimates/standard errors:
    #>    CC MI_LOGT MI_T
    #>  1000    1000 1000
    #>
    #> Average point estimate:
    #>      CC MI_LOGT   MI_T
    #>  0.5168  0.5009 0.4988
    #>
    #> Median point estimate:
    #>      CC MI_LOGT   MI_T
    #>  0.5070  0.4969 0.4939
    #>
    #> Average variance:
    #>      CC MI_LOGT   MI_T
    #>  0.0216  0.0182 0.0179
    #>
    #> Median variance:
    #>      CC MI_LOGT   MI_T
    #>  0.0211  0.0172 0.0169
    #>
    #> Bias in point estimate:
    #>               CC         MI_LOGT             MI_T
    #>  0.0168 (0.0048) 0.0009 (0.0042) -0.0012 (0.0043)
    #>
    #> Relative bias in point estimate:
    #>               CC         MI_LOGT             MI_T
    #>  0.0335 (0.0096) 0.0018 (0.0083) -0.0024 (0.0085)
    #>
    #> Empirical standard error:
    #>               CC         MI_LOGT            MI_T
    #>  0.1511 (0.0034) 0.1320 (0.0030) 0.1344 (0.0030)
    #>
    #> % gain in precision relative to method CC:
    #>               CC          MI_LOGT             MI_T
    #>  0.0000 (0.0000) 31.0463 (3.9375) 26.3682 (3.8424)
    #>
    #> Mean squared error:
    #>               CC         MI_LOGT            MI_T
    #>  0.0231 (0.0011) 0.0174 (0.0009) 0.0181 (0.0009)
    #>
    #> Model-based standard error:
    #>               CC         MI_LOGT            MI_T
    #>  0.1471 (0.0005) 0.1349 (0.0006) 0.1338 (0.0006)
    #>
    #> Relative % error in standard error:
    #>                CC         MI_LOGT             MI_T
    #>  -2.6594 (2.2055) 2.2233 (2.3323) -0.4412 (2.2695)
    #>
    #> Coverage of nominal 95% confidence interval:
    #>               CC         MI_LOGT            MI_T
    #>  0.9430 (0.0073) 0.9490 (0.0070) 0.9430 (0.0073)
    #>
    #> Bias-eliminated coverage of nominal 95% confidence interval:
    #>               CC         MI_LOGT            MI_T
    #>  0.9400 (0.0075) 0.9490 (0.0070) 0.9430 (0.0073)
    #>
    #> Power of 5% level test:
    #>               CC         MI_LOGT            MI_T
    #>  0.9460 (0.0071) 0.9690 (0.0055) 0.9630 (0.0060)

The output begins with a brief overview of the setting of the simulation study (e.g. the method variable, unique methods, etc.), and continues with each summary statistic by method (if defined, as in this case). The values that are reported are point estimates with Monte Carlo standard errors in brackets; however, it is also possible to require confidence intervals based on Monte Carlo standard errors to be reported instead:

    print(ss1, mcse = FALSE)
    #> Values are:
    #>  Point Estimate (95% Confidence Interval based on Monte Carlo Standard Errors)
    #>
    #> Non-missing point estimates/standard errors:
    #>    CC MI_LOGT MI_T
    #>  1000    1000 1000
    #>
    #> Average point estimate:
    #>      CC MI_LOGT   MI_T
    #>  0.5168  0.5009 0.4988
    #>
    #> Median point estimate:
    #>      CC MI_LOGT   MI_T
    #>  0.5070  0.4969 0.4939
    #>
    #> Average variance:
    #>      CC MI_LOGT   MI_T
    #>  0.0216  0.0182 0.0179
    #>
    #> Median variance:
    #>      CC MI_LOGT   MI_T
    #>  0.0211  0.0172 0.0169
    #>
    #> Bias in point estimate:
    #>                       CC                  MI_LOGT                      MI_T
    #>  0.0168 (0.0074, 0.0261) 0.0009 (-0.0073, 0.0091) -0.0012 (-0.0095, 0.0071)
    #>
    #> Relative bias in point estimate:
    #>                       CC                  MI_LOGT                      MI_T
    #>  0.0335 (0.0148, 0.0523) 0.0018 (-0.0145, 0.0182) -0.0024 (-0.0190, 0.0143)
    #>
    #> Empirical standard error:
    #>                       CC                 MI_LOGT                    MI_T
    #>  0.1511 (0.1445, 0.1577) 0.1320 (0.1262, 0.1378) 0.1344 (0.1285, 0.1403)
    #>
    #> % gain in precision relative to method CC:
    #>                        CC                    MI_LOGT                       MI_T
    #>  0.0000 (-0.0000, 0.0000) 31.0463 (23.3290, 38.7636) 26.3682 (18.8372, 33.8991)
    #>
    #> Mean squared error:
    #>                       CC                 MI_LOGT                    MI_T
    #>  0.0231 (0.0209, 0.0253) 0.0174 (0.0157, 0.0191) 0.0181 (0.0163, 0.0198)
    #>
    #> Model-based standard error:
    #>                       CC                 MI_LOGT                    MI_T
    #>  0.1471 (0.1461, 0.1481) 0.1349 (0.1338, 0.1361) 0.1338 (0.1327, 0.1350)
    #>
    #> Relative % error in standard error:
    #>                         CC                  MI_LOGT                      MI_T
    #>  -2.6594 (-6.9820, 1.6633) 2.2233 (-2.3480, 6.7946) -0.4412 (-4.8894, 4.0070)
    #>
    #> Coverage of nominal 95% confidence interval:
    #>                       CC                 MI_LOGT                    MI_T
    #>  0.9430 (0.9286, 0.9574) 0.9490 (0.9354, 0.9626) 0.9430 (0.9286, 0.9574)
    #>
    #> Bias-eliminated coverage of nominal 95% confidence interval:
    #>                       CC                 MI_LOGT                    MI_T
    #>  0.9400 (0.9253, 0.9547) 0.9490 (0.9354, 0.9626) 0.9430 (0.9286, 0.9574)
    #>
    #> Power of 5% level test:
    #>                       CC                 MI_LOGT                    MI_T
    #>  0.9460 (0.9320, 0.9600) 0.9690 (0.9583, 0.9797) 0.9630 (0.9513, 0.9747)

Highlighting some points of interest from the summary results above:

1. The `CC` method has small-sample bias away from the null (point estimate 0.0168, with 95% confidence interval: 0.0074 - 0.0261);
2. `CC` is inefficient compared with `MI_LOGT` and `MI_T`: the relative gain in precision for these two methods is 1.3105% and 1.2637% compared to `CC`, respectively;
3. Model-based standard errors are close to empirical standard errors;
4. Coverage of nominal 95% confidence intervals also seems fine, which is not surprising in view of the generally low (or lack of) bias and good model-based standard errors;
5. `CC` has lower power compared with `MI_LOGT` and `MI_T`, which is not surprising in view of its inefficiency.

## Tabulating summary statistics

It is straightforward to produce a table of summary statistics for use in an R Markdown document:

    library(knitr)
    #>
    #> Attaching package: 'knitr'
    #> The following object is masked from 'package:rsimsum':
    #>
    #>     kable
    kable(tidy(ss1))

stat | est | mcse | method | lower | upper
--- | --- | --- | --- | --- | ---
nsim | 1000.0000000 | NA | CC | NA | NA
thetamean | 0.5167662 | NA | CC | NA | NA
thetamedian | 0.5069935 | NA | CC | NA | NA
se2mean | 0.0216373 | NA | CC | NA | NA
se2median | 0.0211425 | NA | CC | NA | NA
bias | 0.0167662 | 0.0047787 | CC | 0.0074001 | 0.0261322
rbias | 0.0335323 | 0.0095574 | CC | 0.0148003 | 0.0522644
empse | 0.1511150 | 0.0033807 | CC | 0.1444889 | 0.1577411
mse | 0.0230940 | 0.0011338 | CC | 0.0208717 | 0.0253163
relprec | 0.0000000 | 0.0000001 | CC | -0.0000002 | 0.0000002
modelse | 0.1470963 | 0.0005274 | CC | 0.1460626 | 0.1481300
relerror | -2.6593842 | 2.2054817 | CC | -6.9820490 | 1.6632806
cover | 0.9430000 | 0.0073315 | CC | 0.9286305 | 0.9573695
becover | 0.9400000 | 0.0075100 | CC | 0.9252807 | 0.9547193
power | 0.9460000 | 0.0071473 | CC | 0.9319915 | 0.9600085
nsim | 1000.0000000 | NA | MI_LOGT | NA | NA
thetamean | 0.5009231 | NA | MI_LOGT | NA | NA
thetamedian | 0.4969223 | NA | MI_LOGT | NA | NA
se2mean | 0.0182091 | NA | MI_LOGT | NA | NA
se2median | 0.0172157 | NA | MI_LOGT | NA | NA
bias | 0.0009231 | 0.0041744 | MI_LOGT | -0.0072586 | 0.0091048
rbias | 0.0018462 | 0.0083488 | MI_LOGT | -0.0145172 | 0.0182096
empse | 0.1320064 | 0.0029532 | MI_LOGT | 0.1262182 | 0.1377947
mse | 0.0174091 | 0.0008813 | MI_LOGT | 0.0156818 | 0.0191364
relprec | 31.0463410 | 3.9374726 | MI_LOGT | 23.3290364 | 38.7636456
modelse | 0.1349413 | 0.0006046 | MI_LOGT | 0.1337563 | 0.1361263
relerror | 2.2232593 | 2.3323382 | MI_LOGT | -2.3480396 | 6.7945582
cover | 0.9490000 | 0.0069569 | MI_LOGT | 0.9353647 | 0.9626353
becover | 0.9490000 | 0.0069569 | MI_LOGT | 0.9353647 | 0.9626353
power | 0.9690000 | 0.0054808 | MI_LOGT | 0.9582579 | 0.9797421
nsim | 1000.0000000 | NA | MI_T | NA | NA
thetamean | 0.4988092 | NA | MI_T | NA | NA
thetamedian | 0.4939111 | NA | MI_T | NA | NA
se2mean | 0.0179117 | NA | MI_T | NA | NA
se2median | 0.0169319 | NA | MI_T | NA | NA
bias | -0.0011908 | 0.0042510 | MI_T | -0.0095226 | 0.0071409
rbias | -0.0023817 | 0.0085020 | MI_T | -0.0190452 | 0.0142819
empse | 0.1344277 | 0.0030074 | MI_T | 0.1285333 | 0.1403221
mse | 0.0180542 | 0.0009112 | MI_T | 0.0162682 | 0.0198401
relprec | 26.3681613 | 3.8423791 | MI_T | 18.8372366 | 33.8990859
modelse | 0.1338346 | 0.0005856 | MI_T | 0.1326867 | 0.1349824
relerror | -0.4412233 | 2.2695216 | MI_T | -4.8894038 | 4.0069573
cover | 0.9430000 | 0.0073315 | MI_T | 0.9286305 | 0.9573695
becover | 0.9430000 | 0.0073315 | MI_T | 0.9286305 | 0.9573695
power | 0.9630000 | 0.0059692 | MI_T | 0.9513006 | 0.9746994

Using `tidy()` in combination with R packages such as xtable, kableExtra, tables can yield a variety of tables that should suit most purposes.

More information on producing tables directly from R can be found in the CRAN Task View on Reproducible Research.

## Plotting summary statistics

In this section, we show how to plot and compare summary statistics using the popular R package ggplot.

Plotting bias by method with \(95\%\) confidence intervals based on Monte Carlo standard errors:

    library(ggplot2)
    ggplot(tidy(ss1, stats = "bias"), aes(x = method, y = est, ymin = lower, ymax = upper)) +
      geom_hline(yintercept = 0, color = "red", lty = "dashed") +
      geom_point() +
      geom_errorbar(width = 1 / 3) +
      theme_bw() +
      labs(x = "Method", y = "Bias")

Conversely, say we want to visually compare coverage for the three methods compared with this simulation study:

    ggplot(tidy(ss1, stats = "cover"), aes(x = method, y = est, ymin = lower, ymax = upper)) +
      geom_hline(yintercept = 0.95, color = "red", lty = "dashed") +
      geom_point() +
      geom_errorbar(width = 1 / 3) +
      coord_cartesian(ylim = c(0, 1)) +
      theme_bw() +
      labs(x = "Method", y = "Coverage")

## Dropping large estimates and standard errors

`rsimsum` allows to automatically drop estimates and standard errors that are larger than a predefined value. Specifically, the argument of `simsum` that control this behaviour is `dropbig`, with tuning parameters `dropbig.max` and `dropbig.semax` that can be passed via the `control` argument.

Set `dropbig` to `TRUE` and standardised estimates larger than `max` in absolute value will be dropped; standard errors larger than `semax` times the average standard error will be dropped too. By default, robust standardisation is used (based on median and inter-quartile range); however, it is also possible to request regular standardisation (based on mean and standard deviation) by setting the control parameter `dropbig.robust = FALSE`.

For instance, say we want to drop standardised estimates larger than \(3\) in absolute value and standard errors larger than \(1.5\) times the average standard error:

    s1.2 <- simsum(data = MIsim, estvarname = "b", true = 0.50, se = "se", methodvar = "method", ref = "CC", dropbig = TRUE, control = list(dropbig.max = 4, dropbig.semax = 1.5))

Some estimates were dropped, as we can see from the number of non-missing point estimates, standard errors:

    summary(s1.2, stats = "nsim")
    #> Values are:
    #>  Point Estimate (Monte Carlo Standard Error)
    #>
    #> Non-missing point estimates/standard errors:
    #>   CC MI_LOGT MI_T
    #>  958     951  944

Everything else works analogously as before; for instance, to summarise the results:

    summary(s1.2)
    #> Values are:
    #>  Point Estimate (Monte Carlo Standard Error)
    #>
    #> Non-missing point estimates/standard errors:
    #>   CC MI_LOGT MI_T
    #>  958     951  944
    #>
    #> Average point estimate:
    #>      CC MI_LOGT   MI_T
    #>  0.5142  0.4978 0.4973
    #>
    #> Median point estimate:
    #>      CC MI_LOGT   MI_T
    #>  0.5065  0.4934 0.4939
    #>
    #> Average variance:
    #>      CC MI_LOGT   MI_T
    #>  0.0213  0.0175 0.0173
    #>
    #> Median variance:
    #>      CC MI_LOGT   MI_T
    #>  0.0211  0.0170 0.0167
    #>
    #> Bias in point estimate:
    #>               CC          MI_LOGT             MI_T
    #>  0.0142 (0.0048) -0.0022 (0.0043) -0.0027 (0.0043)
    #>
    #> Relative bias in point estimate:
    #>               CC          MI_LOGT             MI_T
    #>  0.0283 (0.0096) -0.0044 (0.0086) -0.0055 (0.0086)
    #>
    #> Empirical standard error:
    #>               CC         MI_LOGT            MI_T
    #>  0.1493 (0.0034) 0.1320 (0.0030) 0.1323 (0.0030)
    #>
    #> % gain in precision relative to method CC:
    #>               CC          MI_LOGT             MI_T
    #>  0.0000 (0.0000) 27.9890 (3.9442) 27.4611 (4.0317)
    #>
    #> Mean squared error:
    #>               CC         MI_LOGT            MI_T
    #>  0.0225 (0.0011) 0.0174 (0.0009) 0.0175 (0.0009)
    #>
    #> Model-based standard error:
    #>               CC         MI_LOGT            MI_T
    #>  0.1459 (0.0005) 0.1323 (0.0005) 0.1314 (0.0005)
    #>
    #> Relative % error in standard error:
    #>                CC         MI_LOGT             MI_T
    #>  -2.2821 (2.2545) 0.2271 (2.3291) -0.6949 (2.3128)
    #>
    #> Coverage of nominal 95% confidence interval:
    #>               CC         MI_LOGT            MI_T
    #>  0.9447 (0.0074) 0.9464 (0.0073) 0.9417 (0.0076)
    #>
    #> Bias-eliminated coverage of nominal 95% confidence interval:
    #>               CC         MI_LOGT            MI_T
    #>  0.9426 (0.0075) 0.9453 (0.0074) 0.9439 (0.0075)
    #>
    #> Power of 5% level test:
    #>               CC         MI_LOGT            MI_T
    #>  0.9457 (0.0073) 0.9685 (0.0057) 0.9661 (0.0059)

# Example 2: Simulation study on survival modelling

    data("relhaz", package = "rsimsum")

Let’s have a look at the first 10 rows of the dataset:

    head(relhaz, n = 10)
    #>    dataset  n    baseline       theta        se model
    #> 1        1 50 Exponential -0.88006151 0.3330172   Cox
    #> 2        2 50 Exponential -0.81460242 0.3253010   Cox
    #> 3        3 50 Exponential -0.14262887 0.3050516   Cox
    #> 4        4 50 Exponential -0.33251820 0.3144033   Cox
    #> 5        5 50 Exponential -0.48269940 0.3064726   Cox
    #> 6        6 50 Exponential -0.03160756 0.3097203   Cox
    #> 7        7 50 Exponential -0.23578090 0.3121350   Cox
    #> 8        8 50 Exponential -0.05046332 0.3136058   Cox
    #> 9        9 50 Exponential -0.22378715 0.3066037   Cox
    #> 10      10 50 Exponential -0.45326446 0.3330173   Cox

The included variables are:

    str(relhaz)
    #> 'data.frame':    1200 obs. of  6 variables:
    #>  $ dataset : int  1 2 3 4 5 6 7 8 9 10 ...
    #>  $ n       : num  50 50 50 50 50 50 50 50 50 50 ...
    #>  $ baseline: chr  "Exponential" "Exponential" "Exponential" "Exponential" ...
    #>  $ theta   : num  -0.88 -0.815 -0.143 -0.333 -0.483 ...
    #>  $ se      : num  0.333 0.325 0.305 0.314 0.306 ...
    #>  $ model   : chr  "Cox" "Cox" "Cox" "Cox" ...

- `dataset`, simulated dataset number;

- `n`, sample size of the simulate dataset;

- `baseline`, baseline hazard function of the simulated dataset;

- `model`, method used (Cox model or Royston-Parmar model with 2 degrees of freedom);

- `theta`, point estimate for the log-hazard ratio;

- `se`, standard error of the point estimate.

`rsimsum` can summarise results from simulation studies with several data-generating mechanisms. For instance, with this example we show how to compute summary statistics by baseline hazard function and sample size.

In order to summarise results by data-generating factors, it is sufficient to define the “by” factors in the call to `simsum`:

    s2 <- simsum(data = relhaz, estvarname = "theta", true = -0.50, se = "se", methodvar = "model", by = c("baseline", "n"))
    #> 'ref' method was not specified, Cox set as the reference
    s2
    #> Summary of a simulation study with a single estimand.
    #> True value of the estimand: -0.5
    #>
    #> Method variable: model
    #>  Unique methods: Cox, Exp, RP(2)
    #>  Reference method: Cox
    #>
    #> By factors: baseline, n
    #>
    #> Monte Carlo standard errors were computed.

The difference between `methodvar` and `by` is as follows: `methodvar` represents methods (e.g. the two models, in this example) compared with this simulation study, while `by` represents all possible data-generating factors that varied when simulating data (in this case, sample size and the true baseline hazard function).

Summarising the results will be printed out for each method and combination of data-generating factors:

    ss2 <- summary(s2)
    ss2
    #> Values are:
    #>  Point Estimate (Monte Carlo Standard Error)
    #>
    #> Non-missing point estimates/standard errors:
    #>     baseline   n Cox Exp RP(2)
    #>  Exponential  50 100 100   100
    #>  Exponential 250 100 100   100
    #>      Weibull  50 100 100   100
    #>      Weibull 250 100 100   100
    #>
    #> Average point estimate:
    #>     baseline   n     Cox     Exp   RP(2)
    #>  Exponential  50 -0.4785 -0.4761 -0.4817
    #>  Exponential 250 -0.5215 -0.5214 -0.5227
    #>      Weibull  50 -0.5282 -0.3491 -0.5348
    #>      Weibull 250 -0.5120 -0.3518 -0.5139
    #>
    #> Median point estimate:
    #>     baseline   n     Cox     Exp   RP(2)
    #>  Exponential  50 -0.4507 -0.4571 -0.4574
    #>  Exponential 250 -0.5184 -0.5165 -0.5209
    #>      Weibull  50 -0.5518 -0.3615 -0.5425
    #>      Weibull 250 -0.5145 -0.3633 -0.5078
    #>
    #> Average variance:
    #>     baseline   n    Cox    Exp  RP(2)
    #>  Exponential  50 0.1014 0.0978 0.1002
    #>  Exponential 250 0.0195 0.0191 0.0194
    #>      Weibull  50 0.0931 0.0834 0.0898
    #>      Weibull 250 0.0174 0.0164 0.0172
    #>
    #> Median variance:
    #>     baseline   n    Cox    Exp  RP(2)
    #>  Exponential  50 0.1000 0.0972 0.0989
    #>  Exponential 250 0.0195 0.0190 0.0194
    #>      Weibull  50 0.0914 0.0825 0.0875
    #>      Weibull 250 0.0174 0.0164 0.0171
    #>
    #> Bias in point estimate:
    #>     baseline   n              Cox              Exp            RP(2)
    #>  Exponential  50  0.0215 (0.0328)  0.0239 (0.0326)  0.0183 (0.0331)
    #>  Exponential 250 -0.0215 (0.0149) -0.0214 (0.0151) -0.0227 (0.0149)
    #>      Weibull  50 -0.0282 (0.0311)  0.1509 (0.0204) -0.0348 (0.0311)
    #>      Weibull 250 -0.0120 (0.0133)  0.1482 (0.0093) -0.0139 (0.0137)
    #>
    #> Relative bias in point estimate:
    #>     baseline   n              Cox              Exp            RP(2)
    #>  Exponential  50 -0.0430 (0.0657) -0.0478 (0.0652) -0.0366 (0.0662)
    #>  Exponential 250  0.0430 (0.0298)  0.0427 (0.0301)  0.0455 (0.0298)
    #>      Weibull  50  0.0564 (0.0623) -0.3018 (0.0408)  0.0695 (0.0622)
    #>      Weibull 250  0.0241 (0.0267) -0.2963 (0.0186)  0.0279 (0.0274)
    #>
    #> Empirical standard error:
    #>     baseline   n             Cox             Exp           RP(2)
    #>  Exponential  50 0.3285 (0.0233) 0.3258 (0.0232) 0.3312 (0.0235)
    #>  Exponential 250 0.1488 (0.0106) 0.1506 (0.0107) 0.1489 (0.0106)
    #>      Weibull  50 0.3115 (0.0221) 0.2041 (0.0145) 0.3111 (0.0221)
    #>      Weibull 250 0.1333 (0.0095) 0.0929 (0.0066) 0.1368 (0.0097)
    #>
    #> % gain in precision relative to method Cox:
    #>     baseline   n             Cox                Exp            RP(2)
    #>  Exponential  50 0.0000 (0.0000)    1.6773 (3.2902) -1.6228 (1.7887)
    #>  Exponential 250 0.0000 (0.0000)   -2.3839 (3.0501) -0.1491 (0.9916)
    #>      Weibull  50 0.0000 (0.0000) 132.7958 (16.4433)  0.2412 (3.7361)
    #>      Weibull 250 0.0000 (0.0000) 105.8426 (12.4932) -4.9519 (2.0647)
    #>
    #> Mean squared error:
    #>     baseline   n             Cox             Exp           RP(2)
    #>  Exponential  50 0.1073 (0.0149) 0.1056 (0.0146) 0.1089 (0.0154)
    #>  Exponential 250 0.0224 (0.0028) 0.0229 (0.0028) 0.0225 (0.0028)
    #>      Weibull  50 0.0968 (0.0117) 0.0640 (0.0083) 0.0970 (0.0117)
    #>      Weibull 250 0.0177 (0.0027) 0.0305 (0.0033) 0.0187 (0.0028)
    #>
    #> Model-based standard error:
    #>     baseline   n             Cox             Exp           RP(2)
    #>  Exponential  50 0.3185 (0.0013) 0.3127 (0.0010) 0.3165 (0.0012)
    #>  Exponential 250 0.1396 (0.0002) 0.1381 (0.0002) 0.1394 (0.0002)
    #>      Weibull  50 0.3052 (0.0014) 0.2888 (0.0005) 0.2996 (0.0012)
    #>      Weibull 250 0.1320 (0.0002) 0.1281 (0.0001) 0.1313 (0.0002)
    #>
    #> Relative % error in standard error:
    #>     baseline   n              Cox               Exp            RP(2)
    #>  Exponential  50 -3.0493 (6.9011)  -4.0156 (6.8286) -4.4305 (6.8013)
    #>  Exponential 250 -6.2002 (6.6679)  -8.3339 (6.5160) -6.4133 (6.6528)
    #>      Weibull  50 -2.0115 (6.9776) 41.4993 (10.0594) -3.6873 (6.8549)
    #>      Weibull 250 -0.9728 (7.0397)  37.7762 (9.7917) -4.0191 (6.8228)
    #>
    #> Coverage of nominal 95% confidence interval:
    #>     baseline   n             Cox             Exp           RP(2)
    #>  Exponential  50 0.9500 (0.0218) 0.9400 (0.0237) 0.9500 (0.0218)
    #>  Exponential 250 0.9300 (0.0255) 0.9200 (0.0271) 0.9300 (0.0255)
    #>      Weibull  50 0.9700 (0.0171) 0.9900 (0.0099) 0.9500 (0.0218)
    #>      Weibull 250 0.9400 (0.0237) 0.8500 (0.0357) 0.9400 (0.0237)
    #>
    #> Bias-eliminated coverage of nominal 95% confidence interval:
    #>     baseline   n             Cox             Exp           RP(2)
    #>  Exponential  50 0.9500 (0.0218) 0.9500 (0.0218) 0.9500 (0.0218)
    #>  Exponential 250 0.9400 (0.0237) 0.9400 (0.0237) 0.9400 (0.0237)
    #>      Weibull  50 0.9500 (0.0218) 1.0000 (0.0000) 0.9500 (0.0218)
    #>      Weibull 250 0.9500 (0.0218) 0.9900 (0.0099) 0.9400 (0.0237)
    #>
    #> Power of 5% level test:
    #>     baseline   n             Cox             Exp           RP(2)
    #>  Exponential  50 0.3600 (0.0480) 0.3800 (0.0485) 0.3700 (0.0483)
    #>  Exponential 250 0.9800 (0.0140) 0.9900 (0.0099) 0.9900 (0.0099)
    #>      Weibull  50 0.4300 (0.0495) 0.0900 (0.0286) 0.4700 (0.0499)
    #>      Weibull 250 0.9700 (0.0171) 0.8600 (0.0347) 0.9700 (0.0171)

## Plotting summary statistics

Tables could get cumbersome when there are many different data-generating mechanisms. Plots are generally easier to interpret, and can be generated as easily as before.

Say we want to compare bias for each method by baseline hazard function and sample size using faceting:

    ggplot(tidy(ss2, stats = "bias"), aes(x = model, y = est, ymin = lower, ymax = upper)) +
      geom_hline(yintercept = 0, color = "red", lty = "dashed") +
      geom_point() +
      geom_errorbar(width = 1 / 3) +
      facet_grid(baseline ~ n) +
      theme_bw() +
      labs(x = "Method", y = "Bias")

# References

- White, I.R. 2010. simsum: Analyses of simulation studies including Monte Carlo error. The Stata Journal 10(3): 369-385
- Morris, T.P., White, I.R. and Crowther, M.J. 2019. Using simulation studies to evaluate statistical methods. Statistics in Medicine 38:2074-2102
- White, I.R., and P. Royston. 2009. Imputing missing covariate values for the Cox model. Statistics in Medicine 28(15):1982-1998
- Little, R.J.A., and D.B. Rubin. 2002. Statistical analysis with missing data. 2nd ed. Hoboken, NJ: Wiley
- van Buuren, S., H.C. Boshuizen, and D.L. Knook. 1999. Multiple imputation of missing blood pressure covariates in survival analysis. Statistics in Medicine 18(6):681-694