Volume 38, Issue 6
Free Access

Applicability of prewhitening to eliminate the influence of serial correlation on the Mann‐Kendall test

Sheng Yue

Meteorological Services of Canada, Ontario Region, Environment Canada, Burlington, Ontario, Canada

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Chun Yuan Wang

Development Research Center, Water Resources Ministry of China, Beijing, China

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First published: 04 June 2002
Citations: 300

Abstract

[1] Prewhitening has been used to eliminate the influence of serial correlation on the Mann‐Kendall (MK) test in trend‐detection studies of hydrological time series. However, its ability to accomplish such a task has not been well documented. This study investigates this issue by Monte Carlo simulation. Simulated time series consist of a linear trend and a lag 1 autoregressive (AR(1)) process with a noise. Simulation results demonstrate that when trend exists in a time series, the effect of positive/negative serial correlation on the MK test is dependent upon sample size, magnitude of serial correlation, and magnitude of trend. When sample size and magnitude of trend are large enough, serial correlation no longer significantly affects the MK test statistics. Removal of positive AR(1) from time series by prewhitening will remove a portion of trend and hence reduces the possibility of rejecting the null hypothesis while it might be false. Contrarily, removal of negative AR(1) by prewhitening will inflate trend and leads to an increase in the possibility of rejecting the null hypothesis while it might be true. Therefore, prewhitening is not suitable for eliminating the effect of serial correlation on the MK test when trend exists within a time series.

1. Introduction

[2] In the past three decades, increased public concern over environmental degradation has led to the popular use of the nonparametric Mann‐Kendall (MK) statistical test [Mann, 1945; Kendall, 1975] to assess significant trends in water quality indicators [e.g., Hirsch et al., 1982; van Belle and Hughes, 1984; Cailas et al., 1986; Hipel et al., 1988; Taylor and Loftis, 1989; Zetterqvist, 1991; Yu et al., 1993]. Recently, great interests in the implications of greenhouse gases or global warming on the environment have led to a number of studies of applying the MK test to identify whether or not significant trends exist in hydrometeorological time series such as streamflow, precipitation, and temperature series. Examples include the works by Hirsch and Slack [1984], Demaree and Nicolis [1990], Gan [1998], Chiew and McMahon [1993], Lettenmaier et al. [1994], Burn [1994], Lins and Slack [1999], Douglas et al. [2000], Zhang et al. [2000, 2001], and Hamilton et al. [2001]. Most trend‐detection studies using the MK test have assumed that sample data are serially independent, even though certain hydrological time series such as water quality series and annual mean and annual minimum streamflows may frequently display statistically significant serial correlation. von Storch [1995] documented that the existence of positive serial correlation increases the probability that the MK test detects trend when no trend exists. This could lead to a rejection of the null hypothesis of no trend, while the null hypothesis is actually true.

[3] To eliminate the influence of serial correlation on the MK test, von Storch [1995] proposed to remove a serial correlation component such as a lag 1 autoregressive (AR(1)) process from time series prior to applying the MK test to assess the significance of trend. This treatment is called as “prewhitening.” The MK test is then used to detect trend in the residual (or prewhitened) series. Douglas et al. [2000] tried to reduce the influence of serial correlation on the MK test by prewhitening in the trend‐detection study of the low flows in the United States. They found that the number of significant trends after prewhitening was less than that before prewhitening. In the trend analyses of Canadian temperature and rainfall data by Zhang et al. [2000] and Hamilton et al. [2001], prewhitening was applied to eliminate the effect of serial correlation on the MK test without any proof of the ability of prewhitening to fulfill such a task. Similarly, Zhang et al. [2001] and Burn and Hag Elnur [2001] employed this approach in streamflow trend analyses of Canada. It seems that prewhitening has been becoming popularly used to limit the effect of serial correlation on the MK test in trend analyses of hydrometeorological time series. Prewhitening has also been proposed to remove an AR process from a time series in the bootstrap postblackening approach [e.g., Davison and Hinkley, 1997; Srinivas and Srinivasan, 2000]. In the case that time series only consist of an AR(1) process with a noise, von Storch [1995] demonstrated that prewhitening can remove the AR(1) process from a time series and eliminate its influence on the MK test. The purpose of trend analyses by the MK test is to assess whether or not a significant trend exists in a tested series. In the case that a trend does exist in a time series, should prewhitening work, it relies on the fact that prewhitening could remove an AR process from a time series without affecting the existing trend. However, no evidence has been provided to certify this.

[4] The previous study of Yue et al. [2002] explored the influence of prewhitening on the prewhitened series only in the case that time series consist of an upward trend and a positive AR(1) process. It demonstrated that removal of positive serial correlation by prewhitening removes a portion of trend. This study extends the work of Yue et al. [2002] and is to further investigate this issue by Monte Carlo simulation. Time series with four kinds of combinations between linear trends (Tt = βt) and AR(1) processes (At = μA + ρ1(At−1 − μA) + εt) are examined: (1) positive AR(1) and upward trend (PAR‐UT), (2) positive AR(1) and downward trend (PAR‐DT); (3) negative AR(1) and upward trend (NAR‐UT), and (4) negative AR(1) and downward trend (NAR‐DT).

2. Simulation Study

[5] Simulation generated 5000 time series of AR(1) processes with mean of 1 and coefficient variation of 0.5 for each sample size (n = 20, 40, 50, 60, 70, and 80) with different given ρ1 = 0 (±0.1) ± 0.9. Then a trend with slope β = 0.00 (±0.001) ± 0.009 is superimposed onto each of the generated series, as given by
equation image
As β = 0.00 (±0.001) ± 0.009 (0.00, ±0.001, ±0.002, ±0.003, …, ±0.009), correspondingly, the mean (=1.0) over 100 years will increase (β × 100 × 100/1)% = 0(±10) ± 90%, i.e., increase/decrease 0 (10) 90%. The rate of rejecting the null hypothesis of no trend can be given by
equation image
where N is the total number of simulation experiments and Nrej is the number of experiments that fall in the critical region. On the basis of the null distribution of the MK test statistics S [Mann, 1945; Kendall, 1975] the critical regions of the MK statistic can be approximately given by
equation image
where α is the preselected significance level, z1−α/2 are the 1 − α/2 quantiles of the standard normal distribution, and V(S) is the sample variance of the MK statistic.

[6] The significance level α is set to be 0.05 in this study. Figure 1 shows the rejection rates, computed by equation (2), for the PAR‐UT series. Figure 1a indicates that in comparison with the series without serial correlation (ρ1 = 0.0), the existence of positive serial correlation increases the probability of rejecting the null hypothesis while it is actually true (β = 0.00). It also shows that the effect of serial correlation on the rejection rate is almost not sensitive to the sample size when no trend exists.

image
Rejection rate for the PAR‐UT series (α = 0.05).

[7] Figures 1b–1j illustrate the rejection rates for the PAR‐UT series with the presence of some trend. By viewing these diagrams, it is found that the influence of serial correlation on the MK test is somewhat different from that without the existence of trend. Positive serial correlation increases the possibility of rejecting the null hypothesis for time series with short record length (say, n < 60 years). Its effect on the rejection rate tends to become weak as the magnitude of trend and sample size increase. For series with longer record length (n ≥ 70) and larger trend (say, β ≥ 0.005, i.e., increase of 50% over 100 years), the impact of serial correlation on the rejection rate is no longer significant. In the extreme cases, say n ≥ 80 and β ≥ 0.007, positive serial correlation decreases the rejection rate. For the PAR‐DT series the same observations as in the PAR‐UT case were obtained and are omitted here.

[8] Figure 2 depicts the rejection rates for the NAR‐DT series. It indicates that the presence of negative serial correlation decreases the rejection rate, while the null hypothesis may be false. When sample size and the magnitude of trend are large enough (say n ≥ 80 and |β| ≥ 0.006), negative serial correlation slightly increases the possibility of rejecting the null hypothesis. These two points are opposite to the PAR‐UT case. It can be seen that as the magnitude of trend and sample size increase, similar to the PAR‐UT case, the influence of negative serial correlation on the rejection rate tends to become weak. The rejection rates for the NAR‐UT series are also the same as shown by Figure 2 and are not presented.

image
Rejection rate for the NAR‐DT series (α = 0.05).
[9] In order to reduce the impact of serial correlation on the MK test, prewhitening by von Storch [1995] was used to remove serial correlation from time series as
equation image
where r1 is the lag 1 serial correlation coefficient of sample data. In practice, as we do not know the true AR process in sample data. The lag 1 serial correlation coefficient r1 can only be estimated from sample data by an autocorrelation function as given in the work of Salas et al. [1980, p.38]. Equation (4) has been used to remove an AR(1) process from sample data in the trend‐detection studies of Douglas et al. [2000], Zhang et al. [2000, 2001], Hamilton et al. [2001], and Burn and Hag Elnur [2001].
[10] The rejection rates of the prewhitened series with β = 0.005, Xt, corresponding to the PAR‐UT and NAR‐DT are displayed in Figures 3a and 4a, respectively. The results corresponding to the series with other different trends are almost identical to the case with β = 0.005 and are not presented. Figure 3a indicates that removal of positive AR(1) by prewhitening greatly reduces the rejection rate or power of the test of rejecting the null hypothesis while it might be false. Figure 4a shows that removal of negative AR(1) by prewhitening dramatically increases the rejection rate or power of the test. To find the reason for these phenomena, the means of the lag 1 serial correlation coefficients of the above prewhitened series corresponding to the PAR‐UT and NAR‐DT are displayed in Figures 3b and 4, respectively. The means of the slopes of trend of the prewhitened series, estimated using the approach of Sen [1968] [also see Hirsch et al., 1982; Gan, 1998], are depicted in Figures 3c and 4c, respectively. Figures 3b and 4b shows that the AR(1) processes were almost removed from the series, except for an extreme case (|ρ1| = 0.9). Figures 3c and 4c indicates that prewhitening positive AR(1) removes a portion of trend, and prewhitening negative AR(1) inflates the magnitude of trend. These are the reason why the rejection rates of the prewhitened series are dramatically different from those without serial correlation. Theoretical interpretation is given as follows. By rewriting equation (4) as
equation image
it can be seen that the slope of the prewhitened series is β′ = (1 − r1)β, which is no longer equal to the true slope β. If r1 > 0, then β′ < β, i.e., removal of positive AR(1) by prewhitening will remove a portion of trend. If r1 < 0, then |β′| > |β|, i.e., removal of negative AR(1) by prewhitening will inflate the existing trend. Therefore, when trend does exist in a time series, prewhitening is not suitable for eliminating the influence of serial correlation on the MK test. The results for the PAR‐DT and NAR‐UT series are almost identical to those of the PAR‐UT and NAR‐DT, respectively, except for the difference in trend direction, as would be expected by symmetry alone. For brevity, these results were not presented.
image
Prewhitened series corresponding to the PAR‐UT series. (a) Rejection rate of the prewhitened series. (b) Means of the serial correlation coefficients. (c) Means of the magnitude of slopes.
image
Prewhitened series corresponding to the NAR‐DT series. (a) Rejection rate of the prewhitened series. (b) Means of the serial correlation coefficients. (c) Means of the magnitude of slopes.

3. Case Study

[11] Annual minimum daily streamflows of 36 pristine catchments with almost continuous observation from 1957 to 1997 are selected from the Canadian Reference Hydrometric Basin Network (RHBN) [Harvey et al., 1999]. The same data source was also used by Zhang et al. [2001]. The identifiers of the gauging stations, their locations, and their means of the annual minimum flows are given in Table 1. The lag 1 serial correlation coefficients of sample data before and after prewhitening are presented in columns 4 and 5 of Table 1, respectively. Column 5 indicates that serial correlation in most sites has been effectively removed from sample data. The estimates of the slope of the trends in sample data before and after prewhitening by Sen's approach [Sen, 1968] are given in columns 6 and 7 of Table 1, respectively. The percentage decrease/increase in the slope caused by prewhitening is listed in column 8. It is evident that the slope of sample data after prewhitening series is greatly different from that before prewhitening. Removal of positive serial correlation by prewhitening dramatically reduces the slope of the trend, and removal of negative serial correlation by prewhitening inflates the slope of the trends, as observed in the above simulation experiments.

Table 1. Comparison of Slopes Before and After Prewhitening
Station Identifier Province Mean (m3/s) Correlation Slope Decrease or increase,aa Decrease or increase is (slope before prewhitening—slope after prewhitening)/slope before prewhitening.
%
Before After Before After
01BP001 New Brunswick 5.4 0.18 −0.01 0.04648 0.02695 42
02FB007 Ontario 0.5 0.68 −0.35 0.01133 0.00313 72
02GA010 Ontario 2.1 0.51 −0.13 0.02902 0.01395 52
02HL004 Ontario 0.3 0.42 −0.01 0.00620 0.00253 59
09AA006 British Columbia 28.5 0.54 −0.11 0.20777 0.04524 78
09AC001 Yukon and Northwest Territories 9.6 0.14 −0.02 0.03783 0.01926 49
09AE003 Britsh Columbia 8.6 0.17 −0.01 0.02047 0.00592 71
09BC001 Yukon and Northwest Territories 47.4 0.33 −0.05 0.17500 0.03545 80
09CA002 Yukon and Northwest Territories 9.8 0.40 −0.05 0.12043 0.07391 39
10CB001 British Columbia 3.7 0.32 0.01 0.02647 0.01603 39
10CD001 British Columbia 15.6 0.26 −0.05 0.22105 0.14511 34
05AA023 Alberta 1.4 0.47 0.14 −0.00810 −0.00479 41
05AD003 Alberta 2.1 0.24 0.01 −0.00897 −0.00663 26
02ZF001 Newfoundland 8.9 0.16 0.04 −0.08310 −0.06903 17
02KB001 Ontario 11.3 0.28 0.00 −0.07000 −0.04939 29
08GA010 British Columbia 2.0 0.40 −0.05 −0.03789 −0.02850 25
08GD004 British Columbia 37.1 0.18 0.06 −0.20769 −0.14570 30
08HB008 British Columbia 2.8 0.24 −0.03 −0.06625 −0.05178 22
08HC002 British Columbia 1.9 0.23 −0.08 −0.04000 −0.03118 22
08JB002 British Columbia 5.0 0.30 0.01 −0.04282 −0.03869 10
08MG005 British Columbia 20.9 0.28 0.09 −0.06183 −0.05655 9
08NB005 British Columbia 25.7 0.24 −0.01 −0.20385 −0.16335 20
08NE077 British Columbia 0.5 0.25 0.09 −0.00185 −0.00163 12
08NL007 British Columbia 2.1 0.30 0.06 −0.03419 −0.02978 13
02OE027 Quebec 1.0 0.17 0.00 −0.00924 −0.00793 14
02VC001 Quebec 59.7 0.29 −0.04 −0.55000 −0.48809 11
01EC001 Nova Scotia 1.5 −0.41 −0.03 0.00222 0.00435 −96
08CE001 British Columbia 51.9 −0.16 0.03 0.22902 0.25208 −10
08KH006 British Columbia 56.0 −0.10 0.02 0.23125 0.29192 −26
02PJ007 Quebec 1.0 −0.12 0.01 0.01520 0.01734 −14
01DG003 Nova Scotia 0.1 −0.22 −0.01 −0.00066 −0.00130 −97
01EF001 Nova Scotia 2.0 −0.28 −0.02 −0.01431 −0.02461 −72
01EO001 Nova Scotia 2.4 −0.14 0.00 −0.01528 −0.03353 −119
08HA001 British Columbia 0.5 −0.21 0.03 −0.00509 −0.00738 −45
08JE001 British Columbia 41.7 −0.28 −0.01 −0.10000 −0.18264 −83
08LA001 British Columbia 35.6 −0.18 −0.04 −0.03708 −0.03842 −4
  • a Decrease or increase is (slope before prewhitening—slope after prewhitening)/slope before prewhitening.

4. Concluding Remarks

[12] The study examined the applicability of prewhitening to eliminate the influence of serial correlation on the MK test by Monte Carlo simulation. Results demonstrate that when trend exists in a time series, the impact of positive/negative serial correlation on the MK test is dependent upon sample size, magnitude of serial correlation, and magnitude of trend. For the series with short record length (say, n ≤ 50) the presence of positive serial correlation will increase the possibility of rejecting the null hypothesis, while negative serial correlation will decrease the rejection rate. When sample size and magnitude of trend are large enough, serial correlation does not significantly influence the MK test. In such a case, it is better to use the MK test on the original data rather than after prewhitening. Prewhitening will seriously distort the possibility of the test to detect trend. Removal of positive AR(1) by prewhitening will remove a portion of the trend, and removal of negative AR(1) by prewhitening will inflate the trend. In practice, for the purpose of water resources planning and management, policy makers and practitioners could be interested in the magnitude of the true trend in a series. If the slope of trend is estimated from the prewhitened series, such a slope is not the true one that a series has, as shown in Table 1. This study only addressed the case that a time series can be modeled by an AR(1) process and the ability of prewhitening to eliminate the influence of serial correlation on the MK test. If the process is not an AR(1) process but of higher order or of a different model type, even though there is no trend, the prewhitening cannot sufficiently reduce the effect of serial correlation on the MK test [von Storch, 1995].

Acknowledgments

[13] The thoughtful comments of William G. Gray and the anonymous reviewers are gratefully acknowledged.

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