1. Chapter 15 Nonparametric Statistics General Objectives: In Chapters 8–10, we presented statistical techniques for comparing two populations by comparing their respective population parameters (usually their population means). The techniques in Chapters 8 and 9 are applicable to data that are at least quantitative, and the techniques in Chapter 10 are applicable to data that have normal distributions. The purpose of this chapter is to present several statistical tests for comparing populations for the many types of data that do not satisfy the assumptions specified in Chapters 8–10. © 1998 Brooks/Cole Publishing/ITP

2. Specific Topics 1. Parametric versus nonparametric tests 2. The Wilcoxon rank sum test: Independent random samples 3. The sign test for a paired experiment 4. The Wilcoxon signed-rank test for a paired experiment 5. The Kruskal-Wallis H test 6. The Friedman F r test 7. The rank correlation coefficient © 1998 Brooks/Cole Publishing/ITP

3. 15.1 Introduction n Some experiments generate responses that can be ordered or ranked, but the actual value of the response cannot be measured numerically. n Here are a few examples: -The sales abilities of four sales representatives are ranked from best to worst. -The edibility and taste characteristics of five brands of raisin bran are rated on an arbitrary scale of 1 to 5. -Five automobile designs are ranked from most appealing to least appealing. n Nonparametric statistical methods can be used when data does not appear to satisfy the normality and other assumptions. © 1998 Brooks/Cole Publishing/ITP

4. n Parametric assumptions are often replaced by more general assumptions about the population distributions. n The ranks of the observations are often used in place of the actual measurements. n Many statisticians advocate the use of nonparametric statistics in all situations. n One alternative is to replace the values of the observations by their ranks and proceed as though the ranks were actual observations. © 1998 Brooks/Cole Publishing/ITP

5. 15.2 The Wilcoxon Rank Sum Test: Independent Random Samples n Two different nonparametric tests use a test statistic based on these sample ranks: - Wilcoxon rank sum test - Mann-Whitney U test n The null hypothesis to be tested is that the two population distributions are different. © 1998 Brooks/Cole Publishing/ITP

6. n These are the possibilities for the two populations: -If H 0 is true and the observations have come from the same or identical populations, then the observations from both samples should be randomly mixed when jointly ranked from small to large. The sum of the ranks should be comparable. -If, on the other hand, the observations from population 1 tend to be smaller than those from population 2, then these observations would have the smaller ranks and the sum of the ranks would be “small.” -If the observations from population 1 tend to be larger than those from population 2, the reverse would happen. n For example, see Table 15.1 for a set of observations and their ranks: Observationx 1 y 1 x 2 y 2 x 3 y 3 y 4 Data2345689 Rank1234 56 7 © 1998 Brooks/Cole Publishing/ITP

7. n The sum of ranks of the observations from a sample is called the rank sum. Formulas for the Wilcoxon Rank Sum Statistic (for Independent Samples): Let T 1  Sum of the ranks for the first sample is the value of the rank sum for n 1 if the observations had been ranked from large to small. (It is not the rank sum for the second sample). Depending on the nature of the alternative hypothesis, one of these two values will be chosen as the test statistic, T. n Table 7 in Appendix I can be used to locate critical values for the test statistic. A portion if this table appears in Table 15.2. © 1998 Brooks/Cole Publishing/ITP

8. Table 15.2 A portion of the 5% left-tailed critical values, Table 7 in Appendix I n 1 n 2 2 3 4 5 6 7 8 3 – 6 4 – 6 11 5 3 7 12 19 6 3 8 13 20 28 7 3 8 14 21 29 39 8 4 9 15 23 31 41 51 9 4 10 16 24 33 43 54 10 4 10 17 26 35 45 56

9. The Wilcoxon Rank Sum Test: Let n 1 denote the smaller of the two sample sizes. This sample comes from population 1. The hypotheses to be tested are : H 0 :The distribution for populations 1 and 2 are identical versus one of three alternative hypotheses: H a :The distributions for populations 1 and 2 are different (a two-tailed test) H a :The distribution for population 1 lies to the left of that for population 2 ( a left-tailed test) H a :The distribution for population 1 lies to the right of that for population 2 (a right-tailed test) 1.Rank all n 1  n 2 observations from small to large. 2. Find T 1, the rank sum for the observations in sample 1. This is the test statistic for a left-tailed test. © 1998 Brooks/Cole Publishing/ITP

10. 3.Find the sum of the ranks of the observations from population 1 if the assigned ranks had been reversed from large to small. ( The value of is not the sum of the ranks of the observations in sample 2). This is the test statistic for a right-tailed test. 4. The test statistic for a two-tailed test is T, the minimum of T 1 and 5.H 0 is rejected if the observed test statistic is less than or equal to the critical value found using table 7 in Appendix I. n The use of Table 7 is illustrated in Example 15.1. © 1998 Brooks/Cole Publishing/ITP

11. Example 15.1 The wing stroke frequencies of two species of Euglossine bees were recorded for a sample of n 1  4 Euglossa mandibularis Friese (species 1) and n 2  6 Euglossa imperialis Cockerell (species 2). The frequencies are listed in Table 15.3. Can you conclude that the distributions of wing strokes differ for these two species? Table 15.3 Species 1Species 2 235180 225169 190180 188185 178 182 © 1998 Brooks/Cole Publishing/ITP

12. Solution You first need to rank the observations from small to large, as shown in Table 15.4: Data Species Rank 169 2 1 178 2 2 180 2 3 180 2 4 182 2 5 185 2 6 188 1 7 190 1 8 225 1 9 235 1 10 The hypotheses to be tested are as follows. © 1998 Brooks/Cole Publishing/ITP

13. H 0 :The distributions of the wing stroke frequencies are the same for the two species versus H a :The distributions of the wing stroke frequencies differ for the two species Since the sample size for individuals from species 1, n 1  4, is the smaller of the two sample sizes, you have and For a two-tailed test, the test statistic is T  10, the smaller of For this two-tailed test with  .05, you can use Table 7(b) in Appendix I with n 1  4 and n 2  6. The critical value of T such that is 12, and you should reject the null hypothesis if the observed value of T is 12 or less. © 1998 Brooks/Cole Publishing/ITP

14. Since the observed value of the test statistic, T  10, is less than 12, you can reject the hypothesis of equal distributions of wing stroke frequencies at the 5% level of significance. A Minitab printout of the Wilcoxon rank sum test ( called Mann- Whitney by Minitab) for these data is given in Figure 15.1. You will find instructions for generating this output in the section “About Minitab” at the end of this chapter. Notice that the rank sum of the first sample is given as W  34.0, which agrees with our calculations. With a reported p-value of.0142 calculated by Minitab, you can reject the null hypothesis at the 5% level. © 1998 Brooks/Cole Publishing/ITP

15. Figure 15.1 Minitab printout for Example 15.1

16. Normal Approximation for the Wilcoxon Rank Sum Test - Provided n 1 is not too small, approximations to the probabilities for the statistic T can be found using a normal approximation to the distribution of T. - It can be shown that the mean and variance of T are - The distribution of is approximately normal with mean 0 and standard deviation 1 for values of n 1 and n 2 as small as 10. - If you try this approximation for Example 15.1, you get and © 1998 Brooks/Cole Publishing/ITP

17. The p-value for this test is 2P (T  34). If you use a.5 correction for continuity in calculating the value of z because n 1 and n 2 are both small, you have The Wilcoxon Rank Sum Test for Large Samples: n 1  10  and n 2  10 1.Null hypothesis: H 0 :The population distributions are identical. 2.Alternative hypothesis: H a :The two population distributions are not identical (a two-tailed test). orH a :The distribution of population 1 is shifted to the right (or left) of the distribution on population 2 (a one-tailed test ) © 1998 Brooks/Cole Publishing/ITP

18. 3.Test statistic: 4.Rejection region: a.For a two-tailed test, reject H 0 if z  z  /2 or z   z  /2. b.For a one-tailed test in the right tail, reject H 0 if z  z  /2. c.For a one-tailed test in the left tail, reject H 0 if z   z  /2. Or reject H 0 if p value   Tabulated values of z are found in Table 3 of Appendix I. n If procedures indicate either nonnormality or inequality of variance, then the Wilcoxon Rank Sum Test is appropriate instead of the two-sample unpaired t test. © 1998 Brooks/Cole Publishing/ITP

19. 15.3 The Sign Test for a Paired Experiment n In Section 10.5, you used the paired-difference or matched pairs design to compare the average wear for two types of tires. n The sign test is a fairly simple procedure that can be used to compare two populations when the samples consist of paired observations. n In general, for each pair, you measure whether the first response—say, A—exceeds the second response—say, B. n The test statistic is x, the number of times that A exceeds B in the n pairs of observations. n Only pairs without ties are included in the test. n Critical values for the rejection region or exact p-values can be found using the cumulative binomial tables in Appendix I. © 1998 Brooks/Cole Publishing/ITP

20. The Sign Test for Comparing Two Populations: 1.Null hypothesis: H 0 : The two population distributions are identical and P (A exceeds B)  p .5 2.Alternative hypothesis: a.H a :The population distributions are not identical and p .5 b. H a :The population of A measurements is shifted to the right of the population of B measurements and p .5 c.H a : The population of A measurements is shifted to the left of the population of B measurements and p .5 3.Test statistic: For n, the number of pairs with no ties, use x, the number of the number of times that (A  B) is positive. 4.Rejection region: a.For the two-tailed test H a : p .5, reject H 0 if x  x L or x  x U, where P(x  x L )  2 and P(x  x U )  2 for x having a binomial distribution with p .5. © 1998 Brooks/Cole Publishing/ITP

21. b.For H a : p .5, reject H 0 if x  x U with P(x  x U )    c.For H a : p .5, reject H 0 if x  x L with P(x  x L )    Or calculate the p-value and reject H 0 if p-value    n If there are tied observations, delete the tied pairs and reduce n, the total number of pairs. Normal Approximation for the Sign Test When the number of pairs n is large, the critical values for rejection of H 0 and the approximate p-values can be found using a normal approximation to the distribution of x, which was discussed in Section 6.4. Because the binomial distribution is perfectly symmetric when p .5, this approximation works very well, even for n as small as 10. © 1998 Brooks/Cole Publishing/ITP

22. Sign Test for Large Samples: n  25 1.Null hypothesizes: H 0 : p .5 (one treatment is not preferred to a second treatment) 2.Alternative hypothesis: H a : p .5, for a two tailed test (Note: We use the two-tailed test as an example. Many analyses might require a one-tailed test.) 3.Test statistic: 4.Rejection region: Reject H 0 if z  z  /2 or z  z  /2, where z  /2 is the z-value from Table 3 in Appendix I corresponding to an area of   /  2 in the upper tail of the normal distribution. n See Example 15.4 for an application of the sign test. © 1998 Brooks/Cole Publishing/ITP

23. Example 15.4 A production superintendent claims that there is no difference between the employee accident rates for the day versus the evening shifts in a large manufacturing plant. The number of accidents per day is recorded for both the day and evening shifts for n  100 days. It is found that the number of accidents per day for the evening shift x E exceeded the corresponding number of accidents in the day shift x D on 63 of the 100 days. Do these results provide sufficient evidence to indicate that more accidents tend to occur on one shift than on the other or, equivalently, that P(x E  x D )  1/2? © 1998 Brooks/Cole Publishing/ITP

24. Solution This study is a paired-difference experiment, with n  100 pairs of observations corresponding to the 100 days. To test the null hypothesis that the two distributions of accidents are identical, you can use the test statistic where x is the number of days in which the number of accidents on the evening shift exceeded the number of accidents on the day shift. Then for .05, you can reject the null hypothesis if Substituting into the formula for z, you get © 1998 Brooks/Cole Publishing/ITP

25. n When there are doubts about the validity of the assumptions for the paired t test, both tests can be performed. If both tests reach the same conclusions, then parametric test results can be considered valid. © 1998 Brooks/Cole Publishing/ITP

26. 15.4 A Comparison of Statistical Tests Definition: Power  1    P(reject H 0 when H a is true) Since  is the probability of failing to reject the null hypothesis when it is false, the power of the test is the probability of rejecting the null hypothesis when it is false and some specified alternative is true. n The power is the probability that the test will do what it was designed to do—that is, detect a departure from the null hypothesis when a departure exists. Relative efficiency is the ratio of the sample sizes for the two test procedures required to achieve the same  and  for a given alternative to the null hypothesis. © 1998 Brooks/Cole Publishing/ITP

27. 15.5 The Wilcoxon Signed-Rank Test for a Paired Experiment Calculating the test statistic for the Wilcoxon Signed-Rank Test: 1.Calculate the differences (x 1  x 1 ) for each of the n pairs. Differences equal to 0 are eliminated, and the number of pairs, n, is reduced accordingly. 2.Rank the absolute values of the differences by assigning 1 to the smallest, 2 to the second smallest, and so on. Tied observations are assigned the average of the ranks that would have been assigned with no ties. 3.Calculate the rank sum for the negative differences and label this value T . Similarly, calculate T , the rank sum for the positive differences. © 1998 Brooks/Cole Publishing/ITP

28. n For a two-tailed test, use the smaller of these two quantities T as a test statistic. n You will reject the null hypothesis if T is less than or equal to some value—say, T 0. To detect the one-sided alternative, that distribution 1 is shifted to the right of distribution 2, use the rank sum T . If you wish to detect a shift of distribution 2 to the right of distribution 1, use the rank sum T . n The rejection region is shown symbolically in Figure 15.2 © 1998 Brooks/Cole Publishing/ITP

29. Wilcoxon Signed-Rank Test for a Paired Experiment: 1.Null hypothesis: H 0 :The two population relative frequency distributions are identical 2. Alternative hypothesis: H a :The two population relative frequency distributions differ in location (a two-tailed test). Or H a : The population 1 relative frequency distribution is shifted to the right of the relative frequency distribution for population 2 (a one-tailed test). 3.Test statistic a. For a two-tailed test, use T, the smaller of the rank sum for positive and the rank sum for negative differences. b. For a one-tailed test (to detect the alternative hypothesis described above), use the rank sum, T  of the negative differences. © 1998 Brooks/Cole Publishing/ITP

30. 4.Rejection region a.For a two-tailed test, reject H 0 if T  T 0, where T 0 is the critical value given in Table 8 in Appendix I. b.For a one-tailed test (to detect the alternative hypothesis described above), use the rank sum T  of the negative differences. Reject H 0 if T   T 0. Note: It can be shown that Normal Approximation Test for the Wilcoxon Signed-Rank Test Although Table 8 in Appendix I has critical values for n as large as 50, T , like the Wilcoxon signed-rank test, will be approxi- mately normally distributed when the null hypothesis is true and n is large—say, 25 or more. © 1998 Brooks/Cole Publishing/ITP

31. n This enables you to construct a large-sample z test, where Then the z statistic can be used as a test statistic. © 1998 Brooks/Cole Publishing/ITP

32. Thus, for a two-tailed test and .05, you can reject the hypothesis of identical population distributions when A Large-Sample Wilcoxon Signed-Rank Test for a Paired Experiment: n  25 1.Null hypothesis: H 0 : The population relative frequency distributions 1 and 2 are identical. 2.Alternative hypothesis: H a : The two population relative frequency distributions differ in location (a two-tailed test ). Or H a : The population 1 relative frequency distribution is shifted to the right (or left) of the relative frequency distributions for population 2 (a one-tailed test). 3.Test statistic: © 1998 Brooks/Cole Publishing/ITP

33. 4.Rejection region: Reject H 0 if z  z  /2 or z  z  /2 for a two- tailed test. For a one-tailed test, place all of  in one tail of the z distribution. To detect a shift in distribution 1 to the right of distribution 2, reject H 0 when z  z . To detect a shift in the opposite direction, reject H 0 if z  z . © 1998 Brooks/Cole Publishing/ITP

34. 15.6 The Kruskal-Wallis H Test for Completely Randomized Designs n The Kruskal-Wallis H test is the nonparametric alternative to the analysis of variance F test for a completely randomized design. n Procedure for Conducting the Kruskal-Wallis H test: Suppose you are comparing k populations where Step 1.Rank all n observations from the smallest (rank 1) to the largest (rank n). Ties get the average rank. Step 2.Calculate the rank sums T 1, T 2, , T k for the k samples and calculate the test statistic © 1998 Brooks/Cole Publishing/ITP

35. Step 3.For a given value of , you can reject H 0 when H exceeds. (See Figure 15.5.) Figure 15.5 Approximate distribution of the H statistic when H 0 is true n See Examples 15.6 and 15.7 for an application of the H statistic. © 1998 Brooks/Cole Publishing/ITP

36. The Kruskal-Wallis H Test for Comparing More than Two Populations: Completely Randomized Design (Independent Random Samples) 1.Null hypothesis: H 0 :The k population distributions are identical 2.Alternative hypothesis: H a :At least two of the k population distributions differ in location. 3.Test statistic: where n 1  Sample size for population i T i  Rank sum for population i n  Total number of observations  n 1  n 2    n k

37. 4.Rejection region for a given  : with (k  1) d f Assumptions: - All sample sizes are greater than or equal to five. - Ties take on the average of the ranks that they would have occupied if they had not been tied. n The Kruskal-Wallis H test is a valuable alternative to a one-way analysis of variance when the normality and equality of variance assumptions are violated. © 1998 Brooks/Cole Publishing/ITP

38. 15.7 The Friedman F r Test for Randomized Block Design n A nonparametric test for comparing the distributions of measurements for k treatments laid out in b blocks using a randomized block design. n The procedure is very similar to the Kruskal-Wallis H test. n Rank the k treatment observations within each block. n Ties receive an average of the ranks occupied by the tied observations. The Friedman F r Test for a Randomized Block Design: 1.Null hypothesis: H 0 : The k population distributions are identical

39. © 1998 Brooks/Cole Publishing/ITP 2.Alternative hypothesis: H a :At least two of the k population distributions differ in location. 3.Test statistic: where b  Number of blocks k  Number of treatments T i  Rank sum or treatment i, i  1, 2, …, k 4.Rejection region: where is based on (k  1) df Assumption: Either the number k treatments or the number b blocks is greater than five.

40. © 1998 Brooks/Cole Publishing/ITP 15.8 Rank Correlation Coefficient Two common rank correlation coefficients are the Spearman r s and the Kendall . Suppose eight elementary school science teachers have been ranked by a judge according to their ability and all have taken a “national teachers examination.” The data are listed in Table 15.11. Does the data suggest an agreement between the judge’s ranking and the examination score? That is, is there a correlation between ranks and test scores?

41. © 1998 Brooks/Cole Publishing/ITP Table 15.11 Ranks and test scores for eight teachers TeacherJudge’s RankExamination Score 1 7 44 2 472 3 269 4 670 5 193 6 382 7 867 8 580 The two variables of interest are rank and test score. The former is already in rank form and the test scores can be ranked similarly, as shown in Table 15.12. The ranks for tied observations are obtained by averaging the ranks that the ties observations would have had if no ties had been observed.

42. © 1998 Brooks/Cole Publishing/ITP n The Spearman rank correlation coefficient r s is calculated by using the ranks as the paired measurements on the two variables x and y in the formula for r (see Chapter 12). Table 15.112 Ranks of data in Table 15.11 TeacherJudges Rank, x i Test Rank, y i 171 245 32 3 464 518 63 7 782 856

43. © 1998 Brooks/Cole Publishing/ITP Spearman's Rank Correlation Coefficient: where x i and y i represent the ranks of the i th pair of observations and When there are no ties to either the x observations or the y observations, the expression for r s algebraically reduces to the simpler expression

44. © 1998 Brooks/Cole Publishing/ITP n If the number of ties is small in comparison with the number of data pairs, little error results in using this shortcut formula. Spearman's Rank Correlation Coefficient: 1.Null hypothesis: H 0 :There is no association between the rank pairs 2.Alternative hypothesis: H a :There is an association between the rank pairs (a two- tailed test). Or H a :The correlation between the rank pairs is positive or negative (a one-tailed test). 3. Test statistic:

45. © 1998 Brooks/Cole Publishing/ITP where x i and y i represent the ranks of the i th pair of observations. 4.Rejection region: For a two-tailed test, reject H 0 if r s  r 0  or r s  r 0  where r 0 is given in Table 9 in Appendix I. Double the tabulated probability to obtain the value of  for the two-tailed test. For a one-tailed test, reject H 0 if r s  r 0 ( for an upper-tailed test) or r s  r 0 (for a lower-tailed test). The  -value for a one-tailed test is the value shown in Table 9 in Appendix I.

46. © 1998 Brooks/Cole Publishing/ITP Example 15.10 Calculate r s for the data in Table 15.12. Solution: The differences and squares of differences between the two rankings are provided in Table 15.13. Substituting values into the formula for r s, you have:

47. © 1998 Brooks/Cole Publishing/ITP Table 15.13 Differences and squares of the differences for the teacher ranks Teacherx i y i d i 171636 24 5  11 323  11 46424 51 8  749 637  416 782636 856  11 Total 144

48. © 1998 Brooks/Cole Publishing/ITP n The Spearman rank correlation can be used as a test statistic to test the hypothesis of no association between populations. n The rejection region of a two-tailed test is shown in Figure 15.12. n The critical values of r s are given in Table 9 in Appendix I. An abbreviated version is shown in Table 15.14. If you calculated r s for the two data sets in Table 15.15, both would produce a value of r s  1 because the assigned ranks for x and y in both cases agree for all pairs (x, y).

49. © 1998 Brooks/Cole Publishing/ITP Table 15.15 Two data sets with r s  1 x 1 1 10 1 2 4 100 2 3 9 1000 3 4 16 10,000 4 5 25 100,000 5 6 36 1,000,000 6

50. © 1998 Brooks/Cole Publishing/ITP 15.9 Summary n The nonparametric analogues of the parametric procedures presented in Chapters 10–14 are straightforward and fairly simple to implement: -The Wilcoxon rank sum test is the nonparametric analogue of the two-sample t test. -The sign test and the Wilcoxon signed-rank tests are the nonparametric analogues of the paired-sample t test. -The Kruskal-Wallis H test is the rank equivalent of the one- way analysis of variance F test. -The Friedman F r test is the rank equivalent of the randomized block design two-way analysis of variance F test. -Spearman's rank correlation r s is the rank equivalent of Pearson’s correlation coefficient.

51. © 1998 Brooks/Cole Publishing/ITP Key Concepts and Formulas I.Nonparametric Methods 1.These methods can be used when the data cannot be measured on a quantitative scale, or when 2.The numerical scale of measurement is arbitrarily set by the researcher, or when 3.The parametric assumptions such as normality or constant variance are seriously violated. II.Wilcoxon Rank Sum Test: Independent Random Samples 1. Jointly rank the two samples: Designate the smaller sample as sample 1. Then

52. © 1998 Brooks/Cole Publishing/ITP 2.Use T 1 to test for population 1 to the left of population 2 Use to test for population to the right of population 2. Use the smaller of T 1 and to test for a difference in the locations of the two populations. 3.Table 7 of Appendix I has critical values for the rejection of H 0. 4.When the sample sizes are large, use the normal approximation:

53. © 1998 Brooks/Cole Publishing/ITP III.Sign Test for a Paired Experiment 1.Find x, the number of times that observation A exceeds observation B for a given pair. 2.To test for a difference in two populations, test H 0 : p .05 versus a one- or two-tailed alternative. 3.Use Table 1 of Appendix I to calculate the p-value for the test. 4.When the sample sizes are large, use the normal approximation:

54. © 1998 Brooks/Cole Publishing/ITP IV.Wilcoxon Signed-Rank Test: Paired Experiment 1.Calculate the differences in the paired observations. Rank the absolute values of the differences. Calculate the rank sums T  and T  for the positive and negative differences, respectively. The test statistic T is the smaller of the two rank sums. 2. Table 8 of Appendix I has critical values for the rejection of for both one- and two-tailed tests. 3. When the sampling sizes are large, use the normal approximation:

55. © 1998 Brooks/Cole Publishing/ITP V.Kruskal-Wallis H Test: Completely Randomized Design 1.Jointly rank the n observations in the k samples. Calculate the rank sums, T i  rank sum of sample i, and the test statistic 2.If the null hypothesis of equality of distributions is false, H will be unusually large, resulting in a one-tailed test. 3.For sample sizes of five or greater, the rejection region for H is based on the chi-square distribution with (k  1) degrees of freedom. VI.The Friedman F r Test: Randomized Block Design 1. Rank the responses within each block from 1 to k. Calculate the rank sums T 1, T 2, , T k, and the test statistic

56. © 1998 Brooks/Cole Publishing/ITP 2.If the null hypothesis of equality of treatment distributions is false, F r will be unusually large, resulting in a one-tailed test. 3.For block sizes of five or greater, the rejection region for F r is based on the chi-square distribution with (k  1) degrees of freedom. VII.Spearman's Rank Correlation Coefficient 1.Rank the responses for the two variables from smallest to largest. 2.Calculate the correlation coefficient for the ranked observations:

57. © 1998 Brooks/Cole Publishing/ITP 3.Table 9 in Appendix I gives critical values for rank correlations significantly different from 0. 4.The rank correlation coefficient detects not only significant linear correlation but also any other monotonic relationship between the two variables.