In statistics, the *k*th **order statistic** of a statistical sample is equal to its *k*th-smallest value.^{[1]} Together with rank statistics, order statistics are among the most fundamental tools in non-parametric statistics and inference.

Important special cases of the order statistics are the minimum and maximum value of a sample, and (with some qualifications discussed below) the sample median and other sample quantiles.

When using probability theory to analyze order statistics of random samples from a continuous distribution, the cumulative distribution function is used to reduce the analysis to the case of order statistics of the uniform distribution.

For example, suppose that four numbers are observed or recorded, resulting in a sample of size 4. If the sample values are

- 6, 9, 3, 8,

the order statistics would be denoted

where the subscript (*i*) enclosed in parentheses indicates the *i*th order statistic of the sample.

The **first order statistic** (or **smallest order statistic**) is always the minimum of the sample, that is,

where, following a common convention, we use upper-case letters to refer to random variables, and lower-case letters (as above) to refer to their actual observed values.

Similarly, for a sample of size *n*, the *n*th order statistic (or **largest order statistic**) is the maximum, that is,

The sample range is the difference between the maximum and minimum. It is a function of the order statistics:

A similar important statistic in exploratory data analysis that is simply related to the order statistics is the sample interquartile range.

The sample median may or may not be an order statistic, since there is a single middle value only when the number *n* of observations is odd. More precisely, if *n* = 2*m*+1 for some integer *m*, then the sample median is and so is an order statistic. On the other hand, when *n* is even, *n* = 2*m* and there are two middle values, and , and the sample median is some function of the two (usually the average) and hence not an order statistic. Similar remarks apply to all sample quantiles.

Given any random variables *X*_{1}, *X*_{2}..., *X*_{n}, the order statistics X_{(1)}, X_{(2)}, ..., X_{(n)} are also random variables, defined by sorting the values (realizations) of *X*_{1}, ..., *X*_{n} in increasing order.

When the random variables *X*_{1}, *X*_{2}..., *X*_{n} form a sample they are independent and identically distributed. This is the case treated below. In general, the random variables *X*_{1}, ..., *X*_{n} can arise by sampling from more than one population. Then they are independent, but not necessarily identically distributed, and their joint probability distribution is given by the Bapat–Beg theorem.

From now on, we will assume that the random variables under consideration are continuous and, where convenient, we will also assume that they have a probability density function (PDF), that is, they are absolutely continuous. The peculiarities of the analysis of distributions assigning mass to points (in particular, discrete distributions) are discussed at the end.

For a random sample as above, with cumulative distribution , the order statistics for that sample have cumulative distributions as follows^{[2]}
(where *r* specifies which order statistic):

the corresponding probability density function may be derived from this result, and is found to be

Moreover, there are two special cases, which have CDFs that are easy to compute.

Which can be derived by careful consideration of probabilities.

In this section we show that the order statistics of the uniform distribution on the unit interval have marginal distributions belonging to the beta distribution family. We also give a simple method to derive the joint distribution of any number of order statistics, and finally translate these results to arbitrary continuous distributions using the cdf.

We assume throughout this section that is a random sample drawn from a continuous distribution with cdf . Denoting we obtain the corresponding random sample from the standard uniform distribution. Note that the order statistics also satisfy .

The probability density function of the order statistic is equal to^{[3]}

that is, the *k*th order statistic of the uniform distribution is a beta-distributed random variable.^{[3]}^{[4]}

The proof of these statements is as follows. For to be between *u* and *u* + *du*, it is necessary that exactly *k* − 1 elements of the sample are smaller than *u*, and that at least one is between *u* and *u* + d*u*. The probability that more than one is in this latter interval is already , so we have to calculate the probability that exactly *k* − 1, 1 and *n* − *k* observations fall in the intervals , and respectively. This equals (refer to multinomial distribution for details)

and the result follows.

The mean of this distribution is *k* / (*n* + 1).

Similarly, for *i* < *j*, the joint probability density function of the two order statistics *U*_{(i)} < *U*_{(j)} can be shown to be

which is (up to terms of higher order than ) the probability that *i* − 1, 1, *j* − 1 − *i*, 1 and *n* − *j* sample elements fall in the intervals , , , , respectively.

One reasons in an entirely analogous way to derive the higher-order joint distributions. Perhaps surprisingly, the joint density of the *n* order statistics turns out to be *constant*:

One way to understand this is that the unordered sample does have constant density equal to 1, and that there are *n*! different permutations of the sample corresponding to the same sequence of order statistics. This is related to the fact that 1/*n*! is the volume of the region . It is also related with another particularity of order statistics of uniform random variables: It follows from the BRS-inequality that the maximum expected number of uniform U(0,1] random variables one can choose from a sample of size n with a sum up not exceeding is bounded above by
, which is thus invariant on the set of all
with constant product .

Using the above formulas, one can derive the distribution of the range of the order statistics, that is the distribution of , i.e. maximum minus the minimum. More generally, for , also has a beta distribution:

From these formulas we can derive the covariance between two order statistics:

The formula follows from noting that

and comparing that with

where , which is the actual distribution of the difference.

For a random sample of size *n* from an exponential distribution with parameter *λ*, the order statistics *X*_{(i)} for *i* = 1,2,3, ..., *n* each have distribution

where the *Z*_{j} are iid standard exponential random variables (i.e. with rate parameter 1). This result was first published by Alfréd Rényi.^{[5]}^{[6]}

The Laplace transform of order statistics may be sampled from an Erlang distribution via a path counting method^{[clarification needed]}.^{[7]}

If *F*_{X} is absolutely continuous, it has a density such that , and we can use the substitutions

and

to derive the following probability density functions for the order statistics of a sample of size *n* drawn from the distribution of *X*:

- where

- where

An interesting question is how well the order statistics perform as estimators of the quantiles of the underlying distribution.

The simplest case to consider is how well the sample median estimates the population median.

As an example, consider a random sample of size 6. In that case, the sample median is usually defined as the midpoint of the interval delimited by the 3rd and 4th order statistics. However, we know from the preceding discussion that the probability that this interval actually contains the population median is^{[clarification needed]}

Although the sample median is probably among the best distribution-independent point estimates of the population median, what this example illustrates is that it is not a particularly good one in absolute terms. In this particular case, a better confidence interval for the median is the one delimited by the 2nd and 5th order statistics, which contains the population median with probability

With such a small sample size, if one wants at least 95% confidence, one is reduced to saying that the median is between the minimum and the maximum of the 6 observations with probability 31/32 or approximately 97%. Size 6 is, in fact, the smallest sample size such that the interval determined by the minimum and the maximum is at least a 95% confidence interval for the population median.

For the uniform distribution, as *n* tends to infinity, the *p*^{th} sample quantile is asymptotically normally distributed, since it is approximated by

For a general distribution *F* with a continuous non-zero density at *F*^{ −1}(*p*), a similar asymptotic normality applies:

where *f* is the density function, and *F*^{ −1} is the quantile function associated with *F*. One of the first people to mention and prove this result was Frederick Mosteller in his seminal paper in 1946.^{[8]} Further research led in the 1960s to the Bahadur representation which provides information about the errorbounds.

An interesting observation can be made in the case where the distribution is symmetric, and the population median equals the population mean. In this case, the sample mean, by the central limit theorem, is also asymptotically normally distributed, but with variance σ^{2}*/n* instead. This asymptotic analysis suggests that the mean outperforms the median in cases of low kurtosis, and vice versa. For example, the median achieves better confidence intervals for the Laplace distribution, while the mean performs better for *X* that are normally distributed.

It can be shown that

where

with *Z _{i}* being independent identically distributed exponential random variables with rate 1. Since

Moments of the distribution for the first order statistic can be used to develop a non-parametric density estimator.^{[9]} Suppose, we want to estimate the density at the point . Consider the random variables , which are i.i.d with distribution function . In particular, .

The expected value of the first order statistic given a sample of total observations yields,

where is the quantile function associated with the distribution , and . This equation in combination with a jackknifing technique becomes the basis for the following density estimation algorithm,

Input: A sample of observations. points of density evaluation. Tuning parameter (usually 1/3). Output: estimated density at the points of evaluation.

1: Set 2: Set 3: Create an matrix which holds subsets with observations each. 4: Create a vector to hold the density evaluations. 5:fordo6:fordo7: Find the nearest distance to the current point within the th subset 8:end for9: Compute the subset average of distances to 10: Compute the density estimate at 11:end for12:return

In contrast to the bandwidth/length based tuning parameters for histogram and kernel based approaches, the tuning parameter for the order statistic based density estimator is the size of sample subsets. Such an estimator is more robust than histogram and kernel based approaches, for example densities like the Cauchy distribution (which lack finite moments) can be inferred without the need for specialized modifications such as IQR based bandwidths. This is because the first moment of the order statistic always exists if the expected value of the underlying distribution does, but the converse is not necessarily true.^{[10]}

Suppose are i.i.d. random variables from a discrete distribution with cumulative distribution function and probability mass function . To find the probabilities of the order statistics, three values are first needed, namely

The cumulative distribution function of the order statistic can be computed by noting that

Similarly, is given by

Note that the probability mass function of is just the difference of these values, that is to say

Main articles: Selection algorithm and Sampling in order |

The problem of computing the *k*th smallest (or largest) element of a list is called the selection problem and is solved by a selection algorithm. Although this problem is difficult for very large lists, sophisticated selection algorithms have been created that can solve this problem in time proportional to the number of elements in the list, even if the list is totally unordered. If the data is stored in certain specialized data structures, this time can be brought down to O(log *n*). In many applications all order statistics are required, in which case a sorting algorithm can be used and the time taken is O(*n* log *n*).