Durbin test

In a randomized block design, k treatments are applied to b blocks. In a complete block design, every treatment is run for every block and the data are arranged as follows:

	Treatment 1	Treatment 2	${\displaystyle \cdots }$	Treatment k
Block 1	X11	X12	${\displaystyle \cdots }$	X1k
Block 2	X21	X22	${\displaystyle \cdots }$	X2k
Block 3	X31	X32	${\displaystyle \cdots }$	X3k
${\displaystyle \vdots }$	${\displaystyle \vdots }$	${\displaystyle \vdots }$	${\displaystyle \ddots }$	${\displaystyle \vdots }$
Block b	Xb1	Xb2	${\displaystyle \cdots }$	Xbk

For some experiments, it may not be realistic to run all treatments in all blocks, so one may need to run an incomplete block design. In this case, it is strongly recommended to run a balanced incomplete design. A balanced incomplete block design has the following properties:

1. Every block contains k experimental units.
2. Every treatment appears in r blocks.
3. Every treatment appears with every other treatment an equal number of times.

The Durbin test is based on the following assumptions:

1. The b blocks are mutually independent. That means the results within one block do not affect the results within other blocks.
2. The data can be meaningfully ranked (i.e., the data have at least an ordinal scale).

Let R(X_ij) be the rank assigned to X_ij within block i (i.e., ranks within a given row). Average ranks are used in the case of ties. The ranks are summed to obtain

${\displaystyle R_{j}=\sum _{i=1}^{b}R(X_{ij})}$

The Durbin test is then

H₀: The treatment effects have identical effects

H_a: At least one treatment is different from at least one other treatment

The test statistic is

${\displaystyle T_{2}={\frac {T_{1}/\left(t-1\right)}{\left(bk-b-T_{1}\right)/\left(bk-b-t+1\right)}}}$

where

${\displaystyle T_{1}={\frac {t-1}{A-C}}\left(\sum _{j=1}^{t}R_{j}^{2}-rC\right)}$

${\displaystyle A=\sum _{i=1}^{b}\sum _{j=1}^{k}R(X_{ij})^{2}}$

${\displaystyle C={\frac {1}{4}}bk\left(k+1\right)^{2}}$

where t is the number of treatments, k is the number of treatments per block, b is the number of blocks, and r is the number of times each treatment appears.

For significance level α, the critical region is given by

${\displaystyle T_{2}>F_{\alpha ,k-1,bk-b-t+1}}$

where F_{α, k − 1, bk − b − t + 1} denotes the α-quantile of the F distribution with k − 1 numerator degrees of freedom and bk − b − t + 1 denominator degrees of freedom. The null hypothesis is rejected if the test statistic is in the critical region. If the hypothesis of identical treatment effects is rejected, it is often desirable to determine which treatments are different (i.e., multiple comparisons). Treatments i and j are considered different if

${\displaystyle |R_{j}-R_{i}|>t_{1-\alpha /2,bk-b-t+1}{\sqrt {{\frac {2\left(A-C\right)r}{bk-k-t+1}}\left(1-{\frac {T_{1}}{b\left(k-1\right)}}\right)}}}$

where R_j and R_i are the column sum of ranks within the blocks, t_{1 − α/2, bk − b − t + 1} denotes the 1 − α/2 quantile of the t-distribution with bk − b − t + 1 degrees of freedom.

T₁ was the original statistic proposed by James Durbin, which would have an approximate null distribution of ${\displaystyle \chi _{t-1}^{2}}$ (that is, chi-squared with ${\displaystyle t-1}$ degrees of freedom). The T₂ statistic has slightly more accurate critical regions, so it is now the preferred statistic. The T₂ statistic is the two-way analysis of variance statistic computed on the ranks R(X_ij).

Cochran's Q test is applied for the special case of a binary response variable (i.e., one that can have only one of two possible outcomes). Cochran's Q test is valid for complete block designs only.

• Analysis of variance
• Friedman test
• Kruskal-Wallis one-way analysis of variance
• Van der Waerden test

• Conover, W. J. (1999). Practical Nonparametric Statistics (Third ed.). Wiley. pp. 388–395. ISBN 0-471-16068-7.

 This article incorporates public domain material from the National Institute of Standards and Technology.