I think you are trying to rediscover the G-test or likelihood ratio test.
Your $H$ is a scaled version of the G statistic, which is defined as
$$G=2\sum_{i=1}^m O_i \log(O_i/E_i)$$
with $E_i=n/m$.
$G$ has been studied as a statistical test since Fisher's work on maximum likelihood estimation in the 1930s, although it has only been called "G" since 1957 (Woolf, 1957).
$G$ can be derived as the likelihood ratio test statistic for the null hypothesis that all the categories have equal probabilities vs the alternative that all or some probabilities are unequal.
The observed counts $O_i$ can be viewed as independent Poisson variables or as a multinomial vector---both models lead to the same likelihood ratio test.
$G$ is asymptotically equal to the Pearson $\chi^2$ statistic given in your question but is sometimes preferred when the counts are small.
Simulations show that the choice between the two isn't clear.
$G$ is asymptotically $\chi^2_{m-1}$ distributed under the null hypothesis of uniformity as $n\rightarrow\infty$ for fixed $m$.
Dunn & Smyth (2018) show that the asymptotic distribution for $G$ can be proved either by the Central Limit Theorem (CLT) applied to the individual counts $O_i$ or by an alternative theorem derived from the saddlepoint approximation.
You are correct that $G$ is related to Kullback–Leibler divergence or Shannon entropy.
$G$ is also known as the deviance in generalized linear model theory.
For example, in this simulation, the value of G is 13.964.
> set.seed(20200628)
> m <- 16
> n <- 128
> y <- sample(1:m, n, replace=TRUE)
> O <- tabulate(y)
> fit <- glm(O~1, family=poisson)
> anova(fit)
Analysis of Deviance Table
Model: poisson, link: log
Response: O
Terms added sequentially (first to last)
Df Deviance Resid. Df Resid. Dev
NULL 15 13.964
Alternatively, here is an extreme example where $O_{16}$ is ten times ther other counts, so the null hypothesis should clearly be rejected:
> O <- rep(10,16)
> O[16] <- 100
> n <- sum(O)
> E <- n/16
> G <- 2*sum(O*log(O/E))
> G
[1] 237.3735
> pchisq(G, df=15, lower.tail=FALSE)
[1] 4.90601e-42
In this case, G$=$237, which yields the tiny p-value $4.9\times 10^{-42}$.
Tail probabilities
You seem to interested in decisions using extremely small $\alpha$-levels (type I error rates) below $10^{-6}$, far beyond what would be used in most statistical contexts.
For $m=16$ and $n=128$, the $\chi^2_{m-1}$ distributional approximation for G is excellent by normal statistical standards but will still underestimate the very small tail probabilities.
You could improve the approximation materially by computing the null expectation of $G$ numerically and replacing $G$ by $G^*=[(m-1)/E(G)]G$.
This idea is my own research, based on the idea of Bartlett correlations.
If even that approximation is not good enough for your cryptography applications, then I think you would have to explore completely different goodness of fit statistics for which exact probability computations are possible.
Exact probability calculations are not at all tractable for the $G$ statistic.
References
Woolf, B. (1957). The log likelihood ratio test (the G-test). Annals of Human Genetics 21(4), 397-409. [The original paper that introduced the terminology G-test for the likelihood ratio statistic computed from a multinomial random variable.]
Dunn, PK, and Smyth, GK (2018). Generalized linear models with examples in R. Springer, New York, NY.
https://doi.org/10.1007/978-1-4419-0118-7
[Proves asymptotic chisquare distribution for $G$ (or any residual deviance) using the saddlepoint approximation.]
https://en.wikipedia.org/wiki/G-test
