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Last modified
7/28/2009 2:40:42 PM
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4/24/2008 2:54:43 PM
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Weather Modification
Title
On the Sampling Variance of Raingage Networks
Date
12/12/1981
Weather Modification - Doc Type
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<br />DECEMBER 1981 <br /> <br />SILVERMAN, ROGERS AND DAHL <br /> <br />1475 <br /> <br />dient [P(x) oc kA where A is the area within the <br />isohyet of interest and k is a constant] is most fre- <br />quently found with steady~type rains in the colder <br />part of the year, an increasing gradient toward the <br />storm center [P(x) oc kAI/2] most commonly occurs <br />in midwestern storms, and a very steep gradient <br />[P(x) oc exp( -kA1/4)] occurs in single-celled air <br />mass storms of strong intensity but small areal ex- <br />tent. The tendencies suggested by Court and Huff <br />are not obvious in the data derived from the area- <br />depth formulas. The lack of consistency may, in part, <br />result from the varying densities of the gage networks <br />used in the various studies and from the subjective <br />construction of the isohyetal maps. Also, the fit of <br />the area-depth formulas to the data may only be <br />approximate. The data derived graphically from the <br />isohyetal maps, however, do tend to support the gen- <br />eralizations of Court and Huff. <br /> <br />6. Comparison with previous studies <br /> <br />We now compare the results of this study with <br />those of other investigators who have considered this <br />problem. As stated earlier, previous investigators <br />(Light, 19472; Linsley and Kohler, 1951; Mc- <br />Guinness, 1963; Huff, 1970; Woodley et aI., 1975) <br />defined the average error in determining areal mean <br />rainfall as the difference in rainfall calculated from <br />their highest gage density, assumed to be the "true" <br />rainfall, and that calculated from subnetworks of <br />lesser density, They related these errors to some or <br />all of the following parameters: mean precipitation, <br />gage density, area, .and storm duration. There are <br />two points to be considered in light of the results of <br />this study, namely the accuracy of their assumed <br />"true" rainfall and the meaning and utility of the <br />empirically determined sampling error relationships. <br />Light derived his empirical relationship for areas <br />in the range 500-8000 mi2 (1295-20720 km2) with <br />a primary gage density of 18 mi2 (47 km2) per gage. <br />Linsley and Kohler derived their error relationship <br />for a fixed area of 220 mi2 (570 km2) and a basic <br />gage density of 4 mi2 (10 km2) per gage. McGuinness <br />used data from a 7.16 mi2 (19 km2) watershed having <br />a gage density of 0.11 mi2 (0.28 km2) per gage to <br />derive his mean rainfall accuracy expression. Huff <br />derived his comprehensive error function with data <br />from gage networks covering 400 and 550 mi2 (1036 <br />and 1424 km2) having gage densities of 8 and 11 mi2 <br />(21 and 28 km2) per gage, respectively. Woodley et <br />al. (1975) derived their error curves for an area of <br />220 mi2 (570 km2) having a gage density of 1.18 mi2 <br />(3.1 km2) per gage. The maximum gage densities <br />used by these investigators were examined in the <br />context of Eq, (2). The coefficient of variation for <br />the largest number of gages per storm (maximum <br />gage density for the area gaged) and the precipitation <br />gradient of the storms (Table 2) considered in each <br />study was calculated. These results indicate that, <br /> <br />"I <br /> <br />although the assumption that the "true" rainfall is <br />represented by the highest gage density becomes <br />weaker as the precipitation gradient becomes in- <br />creasingly steeper and the number of gages per storm <br />decreases, the maximum gage densities in all of these <br />, studies was sufficiently high to render this assump- <br />tion valid for practical purposes. The worst case re- <br />sulted from the smallest area investigated by Light <br />(GPR = 27.8 and G = 1.71) for which the coefficient <br />of variation was <6%. <br />The second issue involves the interpretation of the <br />average absolute errors derived from the empirical <br />relationships. In Section 4 it was pointed out that <br />the sample mean precipitation is always unbiased but <br />the sample standard deviation increases with de- <br />creasing gage density or increasing precipitation gra- <br />dient. This, of course, is the case because we have <br />been able to simulate all possible samplings of the <br />storm by the gage networks. This was not the case <br />in the data sets used to construct the empirical re- <br />lationships. These relationships were based on a fi- <br />nite, insufficient number of samples which randomly <br />fell on the spectrum of possibilities. Huff (1970) rec- <br />ognized this limitation when he stated, "Except for <br />mean precipitation, duration, and average intensity, <br />it is difjicult, if not impossible, to express these sam- <br />pling error factors in quantitative terms. Thus, unless <br />huge samples are available to permit grouping of the <br />data according to all of these various factors, the <br />sampling error with a given gage density in a par- <br />ticular storm cannot be defined with a high degree <br />of accuracy." He supported this point by showing <br />the great amount of variability about the average <br />sampling error from his empirical relationship. It is <br />likely that the values of average sampling error are, <br />in reality, part of this sampling variance and not <br />statistical bias. In any given situation, the error could <br />be in any direction and of any magnitude. The em- <br />pirical relationships do not cover the full spectrum <br />of possibilities. In this paper we have proposed a sta- <br />tistical solution through model simulation studies. <br /> <br />7. Discussion <br /> <br />The quantitative results of this study of the sam- <br />pling variance of precipitation gage networks has <br />many potential hydrometeorological applications. <br />Consider, for example, its application in estimating <br />the sample size requirements in evaluating precipi- <br />tation augmentation experiments. The sample size <br />requirements for a 50/50 randomized precipitation <br />augmentation experiment may be calculated from <br />the following expression <br /> <br />N = 4(ZI-<> + ZI_p)2S2 (3) <br />D2 <br /> <br />where D = dx; normal distribution, loge 1 + d); log- <br />normal distribution and N is the total sample size, <br />
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