# Using R and power analysis to inform experimental design

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# Using R and power analysis to inform experimental design

A collaborator once asked me: “can you do that thing where you take a

little bit of data and model it up to make lots more data?”

Does it sound suspicious to fake a lot of data from a little bit of data? It

depends on the context. Making up data is totally appropriate if you

want to do a power analysis.

And ‘making-up’ data (let’s call it simulation from now on) for power

analysis is a handy tactic for designing effective surveys and

experiments. This post will look at why and how.

## A brief introduction to power analysis

In the narrow-sense, power analysis it about type II error, or the

chance your data and analysis won’t be able to detect an effect that is

really there.

Type II errors are the quiet sibling to type I errors, which tend to get

more focus. The whole “<0.05 is significant”” mentality is about type

I errors.

Having a low type I is important if you want to say a new drug, which

may have side-effects, works.

But in many fields, type II errors are more consequential. In

environmental science in particular, we don’t want significant (in the

non-statistical sense of the word) environmental change to go

unnoticed. Poor power would mean we are unlikely to detect

environmental change in our acidification experiments, or from say an

oil spill decimating a seabird colony.

Pragmatically, if you are doing a PhD you have a limited amount of time

to get publishable results. So you’d want enough power to detect an

effect, should it be there.

Power analysis is also much more useful type II errors, when used in the

broader sense of the term.

Broad-sense power analysis is

about how well data and a statistical model work together to measure an

effect. So it could be about whether we measure the *right* effect (not

just whether we measure it at all).

In the broad and narrow sense, power analysis is a really helpful tool

when you are designing experiments, or a field survey.

For more on traditional power analysis in environmental stats I

recommend the textbook Quinn and Keough (or

google it to find a pdf) or in the broad-sense Bolker’s excellent

book

## Power analysis for experimental and survey design

Let’s say you want to know whether there are more fish inside a marine

reserve (that have no fishing) than outside the reserve. You are going

to do a number of standardized transects inside and outside the reserve

and count the numbers of fish.

Your fish species of interest are a very abundant sweetlips and a rather

rare humphead wrasse. What’s the chance that you would be able to detect

a two times difference in abundance for each fish species between reserves and

fished areas?

We can address this question with power analysis by simulating ‘fake’

data for the surveys where there is a doubling of abundance, then

fitting a statistical model to the fake data, then deciding whether or

not the difference is ‘significant’ (e.g. p<0.05). Then we repeat

that a 1000 times and count up the % of times we said there was a

difference. That % is the power.

So we need to decide on a few things ahead of time, the sample size of

surveys, the expected (mean) abundance values and the variance in

abundance. This is where you could draw on earlier literature to make

estimated guesses. The sample size is up for grabs and trying different

sample sizes could be part of your power analysis.

Let’s assume there are normally 10 sweetlips per transect and 1 humphead

wrasse per transect.

As the data are counts we’ll assume they are Poisson distributed. This

amounts to assuming mean = variance, so the variance of sweetlips across

transects is 10 and wrasse is 1.

## Simulating data with R

To answer this question with R we are going to use quite a few handy

packages:

```
library(purrr)
library(ggplot2)
library(broom)
library(dplyr)
library(tidyr)
```

`purrr`

is handing for creating 1000s of randomised datasets, `ggplot2`

is for plots, `broom`

is for cleaning the 1000s of models we’ll fit,

`dplyr`

and `tidyr`

are for data wrangling.

Now let’s create a function that simulates data and fits a model. This

may look overwhelming, but don’t worry about the R details if you’re not

that into R. All we are doing is creating a function that simultions

some data from two groups (reserve or not) for `n`

transects, and then

fits a

GLM

and finally it spits out a p-value for whether there was a significant

difference in the simulated data.

```
sim <- function(n, x1, x2){
x <- rep(c(x1, x2), each = n/2)
y <- rpois(n, lambda = x)
m1 <- glm(y ~ x, family = "poisson") %>% tidy()
m1
}
```

Now we can use our simulation function to simulate counting wrasse on 20

transects (10 inside and 10 outside the reserve), and then fitting the

GLM to that data:

```
set.seed(2001) #just do this to get the same result as me
sim(100, 1, 2)
## # A tibble: 2 x 5
## term estimate std.error statistic p.value
##
```
## 1 (Intercept) -0.522 0.287 -1.82 0.0690
## 2 x 0.618 0.167 3.69 0.000222

So we get a table with mean estimated difference (on log scale),

standard errors and p-values.

## Narrow-sense power analysis

Now we use `purrr`

to do this 1000 times:

```
mout <- map(1:1000, ~sim(20, 1, 2))
```

Which results in 1000 lists, yuck. Let’s do some data wrangling on the

output:

```
mout2 <- mout %>%
bind_rows(.id = "rep") %>%
filter(term != "(Intercept)") %>%
mutate(Signif = p.value < 0.05,
rep = as.numeric(rep))
head(data.frame(mout2))
## rep term estimate std.error statistic p.value Signif
## 1 1 x 6.931472e-01 0.4082471 1.697862e+00 0.089533876 FALSE
## 2 2 x 8.266786e-01 0.4531632 1.824240e+00 0.068115744 FALSE
## 3 3 x 5.877867e-01 0.3220304 1.825252e+00 0.067963001 FALSE
## 4 4 x 1.145132e+00 0.4339488 2.638865e+00 0.008318414 TRUE
## 5 5 x 1.823216e-01 0.3496022 5.215114e-01 0.602010565 FALSE
## 6 6 x -2.823275e-13 0.3429971 -8.231194e-13 1.000000000 FALSE
```

Now we get a dataframe of the 1000 simulations, indicating whether p for

the difference between reserve vs unreserved was <0.05 (column

‘Signif’).

To get the power, we just sum `Signif`

and divide by the 1000 trials:

```
sum(mout2$Signif)/1000
## [1] 0.408
```

So an ~40% chance we’d detect a 2x difference in wrasse abundance with

20 transects. This is the 2-sided probability, arguably for this question

we could also use a one-sided test.

Try it again for the sweetlips (expected abundance doubling from 10 to

20). You’ll see you get much more power with this more abundance species

(almost 100%).

You could try this with different sample sizes to get an idea of how

much effort you need to invest in doing transects in order to see a

difference (if the difference is really there of course).

## Broad-sense power analysis

How close does our approach get us to the 2x difference? We can also

answer that by looking at the estimates from the GLM:

```
ggplot(mout2, aes(x = exp(estimate))) +
geom_density(fill = "tomato") +
theme_bw() +
geom_vline(xintercept = 2) +
xlab("Estimated times difference")
```

This distribution shows the expected outcomes we’d estimate over 1000

repeats of the surveys. So the solid vertical line is the ‘real’

difference. Note the long tail to the left of drastic overestimates. It

is common with small sample sizes that we might overestimate the true

effect size. More on this later.

I took the exponent of the `estimate`

(estimated mean difference),

because the Poisson GLM has a log link, so the estimate is on the log

scale. Taking its exponent means it is now interpreted as a times

difference (as per the x-axis label).

## Bias in significant estimates

It is reasonably well known that over-use of p-values can contribute to

publication bias, where scientists tend to publish papers about

significant and possibly overestimated effect sizes, but never publish

the non-significant results. This bias can be particularly bad with small

sample sizes, because there’s a reasonable chance we’ll see a big

difference and therefore, make a big deal about it.

We can look at this phenomena in our simulations. First, let’s take the

mean of our estimated effect sizes for those trials that were significant

and those that were not:

```
signif_mean <- mean(exp(filter(mout2, Signif)$estimate))
nonsignif_mean <- mean(exp(filter(mout2, !Signif)$estimate))
all_mean <- mean(exp(mout2$estimate))
c(all_mean, signif_mean, nonsignif_mean)
## [1] 2.210280 3.062810 1.622725
```

So average effect size for the significant trials is >3x (remember

the real difference is 2x). If we take the average across all trials it

is closer to the truth (2.3x).

Clearly if we only publish the significant results, over many studies

this will add up to a much bigger difference than is really there. This

can be a problem in some fields. I don’t think publication bias

particularly affects studies of marine reserves, because typically there

are multiple research questions, so the researchers will publish anyway.

Let’s look at this as a plot. We’ll do the same distribution as above,

but with different colours for significant versus non-significant.

```
ggplot(mout2, aes(x = exp(estimate), fill = Signif)) +
geom_density(alpha = 0.5) +
theme_bw() +
geom_vline(xintercept = 2) +
xlab("Estimated times difference") +
xlim(0,5)
```

You can clearly see the significant trials almost always overestimate

the true difference (vertical line).

What’s the solution? Make sure you report on non-significant results. And

try to aim for larger sample sizes.

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