serialCorrelationTest: Test for the Presence of Serial Correlation

Description

serialCorrelationTest is a generic function used to test for the presence of lag-one serial correlation using either the rank von Neumann ratio test, the normal approximation based on the Yule-Walker estimate of lag-one correlation, or the normal approximation based on the MLE of lag-one correlation. The function invokes particular methods which depend on the class of the first argument.

Currently, there is a default method and a method for objects of class "lm".

Usage

serialCorrelationTest(x, ...)
  # S3 method for default
serialCorrelationTest(x, test = "rank.von.Neumann", 
    alternative = "two.sided", conf.level = 0.95, ...) 
  # S3 method for lm
serialCorrelationTest(x, test = "rank.von.Neumann", 
    alternative = "two.sided", conf.level = 0.95, ...)

Arguments

numeric vector of observations, a numeric univariate time series of class "ts", or an object of class "lm". Undefined (NaN) and infinite (Inf, -Inf) values are not allowed for x when x is a numeric vector or time series, nor for the residuals associated with x when x is an object of class "lm".

When test="AR1.mle", missing (NA) values are allowed, otherwise they are not allowed. When x is a numeric vector of observations or a numeric univariate time series of class "ts", it must contain at least 3 non-missing values. When x is an object of class "lm", the residuals must contain at least 3 non-missing values.

Note: when x is an object of class "lm", the linear model should have been fit using the argument na.action=na.exclude in the call to lm in order to correctly deal with missing values.

test

character string indicating which test to use. The possible values are: "rank.von.Neumann" (rank von Neumann ratio test; the default), "AR1.yw" (z-test based on Yule-Walker lag-one estimate of correlation), and "AR1.mle" (z-test based on MLE of lag-one correlation).

alternative

character string indicating the kind of alternative hypothesis. The possible values are "two.sided" (the default), "greater", and "less".

conf.level

numeric scalar between 0 and 1 indicating the confidence level associated with the confidence interval for the population lag-one autocorrelation. The default value is conf.level=0.95.

…

optional arguments for possible future methods. Currently not used.

Value

A list of class "htest" containing the results of the hypothesis test. See the help file for htest.object for details.

Details

Let $\underset{―}{x} = x_{1}, x_{2}, \dots, x_{n}$ denote $n$ observations from a stationary time series sampled at equispaced points in time with normal (Gaussian) errors. The function serialCorrelationTest tests the null hypothesis: $H_{0} : ρ_{1} = 0 (1)$ where $ρ_{1}$ denotes the true lag-1 autocorrelation (also called the lag-1 serial correlation coefficient). Actually, the null hypothesis is that the lag- $k$ autocorrelation is 0 for all values of $k$ greater than 0 (i.e., the time series is purely random).

In the case when the argument x is a linear model, the function serialCorrelationTest tests the null hypothesis (1) for the residuals.

The three possible alternative hypotheses are the upper one-sided alternative (alternative="greater"): $H_{a} : ρ_{1} > 0 (2)$ the lower one-sided alternative (alternative="less"): $H_{a} : ρ_{1} < 0 (3)$ and the two-sided alternative: $H_{a} : ρ_{1} \neq 0 (4)$

Testing the Null Hypothesis of No Lag-1 Autocorrelation There are several possible methods for testing the null hypothesis (1) versus any of the three alternatives (2)-(4). The function serialCorrelationTest allows you to use one of three possible tests:

The rank von Neuman ratio test.
The test based on the normal approximation for the distribution of the Yule-Walker estimate of lag-one correlation.
The test based on the normal approximation for the distribution of the maximum likelihood estimate (MLE) of lag-one correlation.

Each of these tests is described below.

Test Based on Yule-Walker Estimate (test="AR1.yw") The Yule-Walker estimate of the lag-1 autocorrelation is given by: ${\hat{ρ}}_{1} = \frac{{\hat{γ}}_{1}}{{\hat{γ}}_{0}} (5)$ where ${\hat{γ}}_{k} = \frac{1}{n} \sum_{t = 1}^{n - k} (x_{t} - \bar{x}) (x_{t + k} - \bar{x}) (6)$ is the estimate of the lag- $k$ autocovariance. (This estimator does not allow for missing values.)

Under the null hypothesis (1), the estimator of lag-1 correlation in Equation (5) is approximately distributed as a normal (Gaussian) random variable with mean 0 and variance given by: $V a r ({\hat{ρ}}_{1}) \approx \frac{1}{n} (7)$ (Box and Jenkins, 1976, pp.34-35). Thus, the null hypothesis (1) can be tested with the statistic $z = \sqrt{n} \hat{ρ_{1}} (8)$ which is distributed approximately as a standard normal random variable under the null hypothesis that the lag-1 autocorrelation is 0.

Test Based on the MLE (test="AR1.mle") The function serialCorrelationTest the R function arima to compute the MLE of the lag-one autocorrelation and the estimated variance of this estimator. As for the test based on the Yule-Walker estimate, the z-statistic is computed as the estimated lag-one autocorrelation divided by the square root of the estimated variance.

Test Based on Rank von Neumann Ratio (test="rank.von.Neumann") The null distribution of the serial correlation coefficient may be badly affected by departures from normality in the underlying process (Cox, 1966; Bartels, 1977). It is therefore a good idea to consider using a nonparametric test for randomness if the normality of the underlying process is in doubt (Bartels, 1982).

Wald and Wolfowitz (1943) introduced the rank serial correlation coefficient, which for lag-1 autocorrelation is simply the Yule-Walker estimate (Equation (5) above) with the actual observations replaced with their ranks.

von Neumann et al. (1941) introduced a test for randomness in the context of testing for trend in the mean of a process. Their statistic is given by: $V = \frac{\sum_{i = 1}^{n - 1} (x_{i} - x_{i + 1})^{2}}{\sum_{i = 1}^{n} (x_{i} - \bar{x})^{2}} (9)$ which is the ratio of the square of successive differences to the usual sums of squared deviations from the mean. This statistic is bounded between 0 and 4, and for a purely random process is symmetric about 2. Small values of this statistic indicate possible positive autocorrelation, and large values of this statistics indicate possible negative autocorrelation. Durbin and Watson (1950, 1951, 1971) proposed using this statistic in the context of checking the independence of residuals from a linear regression model and provided tables for the distribution of this statistic. This statistic is therefore often called the “Durbin-Watson statistic” (Draper and Smith, 1998, p.181).

The rank version of the von Neumann ratio statistic is given by: $V_{r a n k} = \frac{\sum_{i = 1}^{n - 1} (R_{i} - R_{i + 1})^{2}}{\sum_{i = 1}^{n} (R_{i} - \bar{R})^{2}} (10)$ where $R_{i}$ denotes the rank of the $i$ 'th observation (Bartels, 1982). (This test statistic does not allow for missing values.) In the absence of ties, the denominator of this test statistic is equal to $\sum_{i = 1}^{n} (R_{i} - \bar{R})^{2} = \frac{n (n^{2} - 1)}{12} (11)$ The range of the $V_{r a n k}$ test statistic is given by: $[\frac{12}{(n) (n + 1)}, 4 - \frac{12}{(n) (n + 1)}] (12)$ if n is even, with a negligible adjustment if n is odd (Bartels, 1982), so asymptotically the range is from 0 to 4, just as for the $V$ test statistic in Equation (9) above.

Bartels (1982) shows that asymptotically, the rank von Neumann ratio statistic is a linear transformation of the rank serial correlation coefficient, so any asymptotic results apply to both statistics.

For any fixed sample size $n$ , the exact distribution of the $V_{r a n k}$ statistic in Equation (10) above can be computed by simply computing the value of $V_{r a n k}$ for all possible permutations of the serial order of the ranks. Based on this exact distribution, Bartels (1982) presents a table of critical values for the numerator of the RVN statistic for sample sizes between 4 and 10.

Determining the exact distribution of $V_{r a n k}$ becomes impractical as the sample size increases. For values of n between 10 and 100, Bartels (1982) approximated the distribution of $V_{r a n k}$ by a beta distribution over the range 0 to 4 with shape parameters shape1= $ν$ and shape2= $ω$ and: $ν = ω = \frac{5 n (n + 1) (n - 1)^{2}}{2 (n - 2) (5 n^{2} - 2 n - 9)} - \frac{1}{2} (13)$ Bartels (1982) checked this approximation by simulating the distribution of $V_{r a n k}$ for $n = 25$ and $n = 50$ and comparing the empirical quantiles at $0.005$ , $0.01$ , $0.025$ , $0.05$ , and $0.1$ with the approximated quantiles based on the beta distribution. He found that the quantiles agreed to 2 decimal places for eight of the 10 values, and differed by $0.01$ for the other two values.

Note: The definition of the beta distribution assumes the random variable ranges from 0 to 1. This definition can be generalized as follows. Suppose the random variable $Y$ has a beta distribution over the range $a \leq y \leq b$ , with shape parameters $ν$ and $ω$ . Then the random variable $X$ defined as: $X = \frac{Y - a}{b - a} (14)$ has the “standard beta distribution” as described in the help file for Beta (Johnson et al., 1995, p.210).

Bartels (1982) shows that asymptotically, $V_{r a n k}$ has normal distribution with mean 2 and variance $4 / n$ , but notes that a slightly better approximation is given by using a variance of $20 / (5 n + 7)$ .

To test the null hypothesis (1) when test="rank.von.Neumann", the function serialCorrelationTest does the following:

When the sample size is between 3 and 10, the exact distribution of $V_{r a n k}$ is used to compute the p-value.
When the sample size is between 11 and 100, the beta approximation to the distribution of $V_{r a n k}$ is used to compute the p-value.
When the sample size is larger than 100, the normal approximation to the distribution of $V_{r a n k}$ is used to compute the p-value. (This uses the variance $20 / (5 n + 7)$ .)

When ties are present in the observations and midranks are used for the tied observations, the distribution of the $V_{r a n k}$ statistic based on the assumption of no ties is not applicable. If the number of ties is small, however, they may not grossly affect the assumed p-value.

When ties are present, the function serialCorrelationTest issues a warning. When the sample size is between 3 and 10, the p-value is computed based on rounding up the computed value of $V_{r a n k}$ to the nearest possible value that could be observed in the case of no ties.

Computing a Confidence Interval for the Lag-1 Autocorrelation The function serialCorrelationTest computes an approximate $100 (1 - α) %$ confidence interval for the lag-1 autocorrelation as follows: $[{\hat{ρ}}_{1} - z_{1 - α / 2} {\hat{σ}}_{{\hat{ρ}}_{1}}, {\hat{ρ}}_{1} + z_{1 - α / 2} {\hat{σ}}_{{\hat{ρ}}_{1}}] (15)$ where ${\hat{σ}}_{{\hat{ρ}}_{1}}$ denotes the estimated standard deviation of the estimated of lag-1 autocorrelation and $z_{p}$ denotes the $p$ 'th quantile of the standard normal distribution.

When test="AR1.yw" or test="rank.von.Neumann", the Yule-Walker estimate of lag-1 autocorrelation is used and the variance of the estimated lag-1 autocorrelation is approximately: $V a r ({\hat{ρ}}_{1}) \approx \frac{1}{n} (1 - ρ_{1}^{2}) (16)$ (Box and Jenkins, 1976, p.34), so ${\hat{σ}}_{{\hat{ρ}}_{1}} = \sqrt{\frac{1 - {\hat{ρ}}_{1}^{2}}{n}} (17)$ When test="AR1.mle", the MLE of the lag-1 autocorrelation is used, and its standard deviation is estimated with the square root of the estimated variance returned by arima.

References

Bartels, R. (1982). The Rank Version of von Neumann's Ratio Test for Randomness. Journal of the American Statistical Association 77(377), 40--46.

Berthouex, P.M., and L.C. Brown. (2002). Statistics for Environmental Engineers. Second Edition. Lewis Publishers, Boca Raton, FL.

Box, G.E.P., and G.M. Jenkins. (1976). Time Series Analysis: Forecasting and Control. Prentice Hall, Englewood Cliffs, NJ, Chapter 2.

Cox, D.R. (1966). The Null Distribution of the First Serial Correlation Coefficient. Biometrika 53, 623--626.

Draper, N., and H. Smith. (1998). Applied Regression Analysis. Third Edition. John Wiley and Sons, New York, pp.69-70;181-192.

Durbin, J., and G.S. Watson. (1950). Testing for Serial Correlation in Least Squares Regression I. Biometrika 37, 409--428.

Durbin, J., and G.S. Watson. (1951). Testing for Serial Correlation in Least Squares Regression II. Biometrika 38, 159--178.

Durbin, J., and G.S. Watson. (1971). Testing for Serial Correlation in Least Squares Regression III. Biometrika 58, 1--19.

Helsel, D.R., and R.M. Hirsch. (1992). Statistical Methods in Water Resources Research. Elsevier, New York, NY, pp.250--253.

Johnson, N. L., S. Kotz, and N. Balakrishnan. (1995). Continuous Univariate Distributions, Volume 2. Second Edition. John Wiley and Sons, New York, Chapter 25.

Knoke, J.D. (1975). Testing for Randomness Against Autocorrelation Alternatives: The Parametric Case. Biometrika 62, 571--575.

Knoke, J.D. (1977). Testing for Randomness Against Autocorrelation Alternatives: Alternative Tests. Biometrika 64, 523--529.

Lehmann, E.L. (1975). Nonparametrics: Statistical Methods Based on Ranks. Holden-Day, Oakland, CA, 457pp.

von Neumann, J., R.H. Kent, H.R. Bellinson, and B.I. Hart. (1941). The Mean Square Successive Difference. Annals of Mathematical Statistics 12(2), 153--162.

Wald, A., and J. Wolfowitz. (1943). An Exact Test for Randomness in the Non-Parametric Case Based on Serial Correlation. Annals of Mathematical Statistics 14, 378--388.

Examples

Run this code

# NOT RUN {
  # Generate a purely random normal process, then use serialCorrelationTest 
  # to test for the presence of correlation. 
  # (Note: the call to set.seed allows you to reproduce this example.) 

  set.seed(345) 
  x <- rnorm(100) 

  # Look at the data
  #-----------------
  dev.new()
  ts.plot(x)

  dev.new()
  acf(x)

  # Test for serial correlation
  #----------------------------
  serialCorrelationTest(x) 

  #Results of Hypothesis Test
  #--------------------------
  #
  #Null Hypothesis:                 rho = 0
  #
  #Alternative Hypothesis:          True rho is not equal to 0
  #
  #Test Name:                       Rank von Neumann Test for
  #                                 Lag-1 Autocorrelation
  #                                 (Beta Approximation)
  #
  #Estimated Parameter(s):          rho = 0.02773737
  #
  #Estimation Method:               Yule-Walker
  #
  #Data:                            x
  #
  #Sample Size:                     100
  #
  #Test Statistic:                  RVN = 1.929733
  #
  #P-value:                         0.7253405
  #
  #Confidence Interval for:         rho
  #
  #Confidence Interval Method:      Normal Approximation
  #
  #Confidence Interval Type:        two-sided
  #
  #Confidence Level:                95%
  #
  #Confidence Interval:             LCL = -0.1681836
  #                                 UCL =  0.2236584

  # Clean up
  #---------
  rm(x)
  graphics.off()

  #==========

  # Now use the R function arima.sim to generate an AR(1) process with a 
  # lag-1 autocorrelation of 0.8, then test for autocorrelation.

  set.seed(432) 
  y <- arima.sim(model = list(ar = 0.8), n = 100) 

  # Look at the data
  #-----------------
  dev.new()
  ts.plot(y)

  dev.new()
  acf(y)

  # Test for serial correlation
  #----------------------------
  serialCorrelationTest(y)

  #Results of Hypothesis Test
  #--------------------------
  #
  #Null Hypothesis:                 rho = 0
  #
  #Alternative Hypothesis:          True rho is not equal to 0
  #
  #Test Name:                       Rank von Neumann Test for
  #                                 Lag-1 Autocorrelation
  #                                 (Beta Approximation)
  #
  #Estimated Parameter(s):          rho = 0.835214
  #
  #Estimation Method:               Yule-Walker
  #
  #Data:                            y
  #
  #Sample Size:                     100
  #
  #Test Statistic:                  RVN = 0.3743174
  #
  #P-value:                         0
  #
  #Confidence Interval for:         rho
  #
  #Confidence Interval Method:      Normal Approximation
  #
  #Confidence Interval Type:        two-sided
  #
  #Confidence Level:                95%
  #
  #Confidence Interval:             LCL = 0.7274307
  #                                 UCL = 0.9429973

  #----------

  # Clean up
  #---------
  rm(y)
  graphics.off()

  #==========

  # The data frame Air.df contains information on ozone (ppb^1/3), 
  # radiation (langleys), temperature (degrees F), and wind speed (mph) 
  # for 153 consecutive days between May 1 and September 30, 1973.  
  # First test for serial correlation in (the cube root of) ozone.  
  # Note that we must use the test based on the MLE because the time series 
  # contains missing values.  Serial correlation appears to be present.  
  # Next fit a linear model that includes the predictor variables temperature, 
  # radiation, and wind speed, and test for the presence of serial correlation 
  # in the residuals.  There is no evidence of serial correlation.

  # Look at the data
  #-----------------

  Air.df
  #              ozone radiation temperature wind
  #05/01/1973 3.448217       190          67  7.4
  #05/02/1973 3.301927       118          72  8.0
  #05/03/1973 2.289428       149          74 12.6
  #05/04/1973 2.620741       313          62 11.5
  #05/05/1973       NA        NA          56 14.3
  #...
  #09/27/1973       NA       145          77 13.2
  #09/28/1973 2.410142       191          75 14.3
  #09/29/1973 2.620741       131          76  8.0
  #09/30/1973 2.714418       223          68 11.5

  #----------

  # Test for serial correlation
  #----------------------------

  with(Air.df, 
    serialCorrelationTest(ozone, test = "AR1.mle"))

  #Results of Hypothesis Test
  #--------------------------
  #
  #Null Hypothesis:                 rho = 0
  #
  #Alternative Hypothesis:          True rho is not equal to 0
  #
  #Test Name:                       z-Test for
  #                                 Lag-1 Autocorrelation
  #                                 (Wald Test Based on MLE)
  #
  #Estimated Parameter(s):          rho = 0.5641616
  #
  #Estimation Method:               Maximum Likelihood
  #
  #Data:                            ozone
  #
  #Sample Size:                     153
  #
  #Number NA/NaN/Inf's:             37
  #
  #Test Statistic:                  z = 7.586952
  #
  #P-value:                         3.28626e-14
  #
  #Confidence Interval for:         rho
  #
  #Confidence Interval Method:      Normal Approximation
  #
  #Confidence Interval Type:        two-sided
  #
  #Confidence Level:                95%
  #
  #Confidence Interval:             LCL = 0.4184197
  #                                 UCL = 0.7099034

  #----------

  # Next fit a linear model that includes the predictor variables temperature, 
  # radiation, and wind speed, and test for the presence of serial correlation 
  # in the residuals.  Note setting the argument na.action = na.exclude in the 
  # call to lm to correctly deal with missing values.
  #----------------------------------------------------------------------------

  lm.ozone <- lm(ozone ~ radiation + temperature + wind + 
    I(temperature^2) + I(wind^2), 
    data = Air.df, na.action = na.exclude) 


  # Now test for serial correlation in the residuals.
  #--------------------------------------------------

  serialCorrelationTest(lm.ozone, test = "AR1.mle") 

  #Results of Hypothesis Test
  #--------------------------
  #
  #Null Hypothesis:                 rho = 0
  #
  #Alternative Hypothesis:          True rho is not equal to 0
  #
  #Test Name:                       z-Test for
  #                                 Lag-1 Autocorrelation
  #                                 (Wald Test Based on MLE)
  #
  #Estimated Parameter(s):          rho = 0.1298024
  #
  #Estimation Method:               Maximum Likelihood
  #
  #Data:                            Residuals
  #
  #Data Source:                     lm.ozone
  #
  #Sample Size:                     153
  #
  #Number NA/NaN/Inf's:             42
  #
  #Test Statistic:                  z = 1.285963
  #
  #P-value:                         0.1984559
  #
  #Confidence Interval for:         rho
  #
  #Confidence Interval Method:      Normal Approximation
  #
  #Confidence Interval Type:        two-sided
  #
  #Confidence Level:                95%
  #
  #Confidence Interval:             LCL = -0.06803223
  #                                 UCL =  0.32763704

  # Clean up
  #---------
  rm(lm.ozone)

# }

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