The problem of finding the expected number of standard Uniform variables to get a sum greater than 1 is quite famous. In this post, we deal with the same problem but for a given target t.
This problem is not too difficult. Knowing that the sum of uniform random variables follows the Irwin-Hall distribution and the CDF of this distribution has a closed form solves the problem easily.
For example, if we let N be the random variable denoting the number of draws needed to get the sum exceed t for the first time, then
\displaystyle \mathbb{P}(N>n)=\mathbb{P}(U_1+U_2+\cdots+U_n \leq t)=\frac{1}{n!}\sum_{k=0}^{\lfloor t \rfloor}(-1)^k\binom{n}{k}(t-k)^n
Then \mathbb{P}(N=n)=\mathbb{P}(N>n-1)-\mathbb{P}(N>n)
But we can get this more directly using the idea in Excercise 6.65 (more importantly, its solution) of Concrete Mathematics.
For standard uniform random variables U_1,U_2,\cdots,U_n, let X_1=\{U_1\}, X_2=\{U_1+U_2\} and so on, where \{x\} denotes the fractional part of x.
It can be easily seen that X_k's are all independently distributed uniform random variables. More importantly, the number of descents in the sequence of X_k's is \lfloor U_1+U_2+\cdots+U_n\rfloor.
Therefore, for integer t, the sum of n uniform random variables exceeding t for the first time corresponds to the sequence of X_1,X_2,\cdots,X_n that has exactly t descents and end with a descent.
The probability of such a sequence is related to the permutation of numbers 1,2,\cdots,n that has exactly t and end with the descent. We have already seen in this blog regarding this exact problem. Using that result, we finally have,
\displaystyle\mathbb{P}(N=n)=\frac{(n-t)A(n-1,t-1)}{n!}
Though we have solved this for integer t, with a giant leap in faith guided by some experimentation, we can also see that this works any real t.
With this, we get,
\mathbb{E}(\text{No. of Uniform variables needed to get a sum greater than }\pi)\approx 6.949504
\mathbb{E}(\text{No. of Uniform variables needed to get a sum greater than }e)\approx 6.104002
Hope you enjoyed this. See ya soon.
Until then, Yours Aye
Me
No comments:
Post a Comment