Consider a random set of numbers that are normally distributed:

`x <- rnorm(n=1000, mean=10)`

We’d like to know the mean and the standard error on the mean so we do the following:

`se <- function(x) { sd(x)/sqrt(length(x)) } mean(x) # something near 10.0 units se(x) # something near 0.03 units`

Great!

However, let’s assume we don’t necessarily know that our original distribution follows a normal distribution. We log-transform the data and perform the same standard error calculation.

`z <- log(x, base=10) mean(z) # something near 1 log units se(z) # something near 0.001 log units`

Cool, but now we need to back-transform to get our answer in units NOT log units.

`10^mean(z) # something near 10.0 units 10^se(z) # something near 1.00 units`

My question: Why, for a normal distribution, does the standard error differ depending on whether it was calculated from the distribution itself or if it was transformed, calculated, and back-transformed? Note: the means came out the same regardless of the transformation.

EDIT #1: Ultimately, I am interested in calculating a mean and confidence intervals for non-normally distributed data, so if you can give some guidance on how to calculate 95% CI’s on transformed data including how to back-transform to their native units, I would appreciate it!

END EDIT #1EDIT #2: I tried using the quantile function to get the 95% confidence intervals:

`quantile(x, probs = c(0.05, 0.95)) # around [8.3, 11.6] 10^quantile(z, probs = c(0.05, 0.95)) # around [8.3, 11.6]`

So, that converged on the same answer, which is good. However, using this method doesn’t provide the exact same interval using non-normal data with “small” sample sizes:

`t <- rlnorm(10) mean(t) # around 1.46 units 10^mean(log(t, base=10)) # around 0.92 units quantile(t, probs = c(0.05, 0.95)) # around [0.211, 4.79] 10^(quantile(log(t, base=10), probs = c(0.05, 0.95))) # around [0.209, 4.28]`

Which method would be considered “more correct”. I assume one would pick the most conservative estimate?

As an example, would you report this result for the non-normal data (t) as having a mean of 0.92 units with a 95% confidence interval of [0.211, 4.79]?

END EDIT #2Thanks for your time!

**Answer**

Your main problem with the initial calculation is there’s no good reason why esd(log(Y)) should be like sd(Y). It’s generally quite different.

In some situations, you can compute a rough approximation of sd(Y) from sd(log(Y)) via Taylor expansion.

Var(g(X))≈(g′(μX))2σ2X.

If we consider X to be the random variable on the log scale, here, g(X)=exp(X)

If Var(exp(X))≈exp(μX)2σ2X

then sd(exp(X))≈exp(μX)σX

These notions carry across to sampling distributions.

This tends to work reasonably well if the standard deviation is really small compared to the mean, as in your example.

```
> mean(y)
[1] 10
> sd(y)
[1] 0.03
> lm=mean(log(y))
> ls=sd(log(y))
> exp(lm)*ls
[1] 0.0300104
```

If you want to transform a CI for a *parameter*, that works by transforming the endpoints.

If you’re trying to transform back to obtain point estimate and interval for the mean on the original (unlogged) scale, you will also want to unbias the estimate of the mean (see the above link): E(exp(X))≈exp(μX)⋅(1+σ2X/2), so a (*very*) rough large sample interval for the mean might be (c.exp(L),c.exp(U)), where L,U are the upper and lower limits of a log-scale interval, and c is some consistent estimate of 1+σ2X/2.

If your data are approximately normal on the log scale, you may want to treat it as a problem of producing an interval for a lognormal mean.

(There are other approaches to unbiasing mean estimates across transformations; e.g. see Duan, N., 1983. Smearing estimate: a nonparametric retransformation method. JASA,

78, 605-610)

**Attribution***Source : Link , Question Author : baffled , Answer Author : Glen_b*