the Creative Commons Attribution 4.0 License.
the Creative Commons Attribution 4.0 License.
Comparison of rainfall generators with regionalisation for the estimation of rainfall erosivity at ungauged sites
Ross Pidoto
Nejc Bezak
Hannes MüllerThomy
Bora Shehu
Ana Claudia CallauBeyer
Katarina Zabret
Uwe Haberlandt
Rainfall erosivity values are required for soil erosion prediction. To calculate the mean annual rainfall erosivity (R), longterm highresolution observed rainfall data are required, which are often not available. To overcome the issue of limited data availability in space and time, four methods were employed and evaluated: direct regionalisation of R, regionalisation of 5 min rainfall, disaggregation of daily rainfall into 5 min time steps, and a regionalised stochastic rainfall model. The impact of station density is considered for each of the methods. The study is carried out using 159 recording and 150 nonrecording (daily) rainfall stations in and around the federal state of Lower Saxony, Germany. In addition, the minimum record length necessary to adequately estimate R was investigated. Results show that the direct regionalisation of mean annual erosivity is best in terms of both relative bias and relative root mean square error (RMSE), followed by the regionalisation of the 5 min rainfall data, which yields better results than the rainfall generation models, namely an alternating renewal model (ARM) and a multiplicative cascade model. However, a key advantage of using regionalised rainfall models is the ability to generate time series that can be used for the estimation of the erosive event characteristics. This is not possible if regionalising only R. Using the stochastic ARM, it was assessed that more than 60 years of data are needed in most cases to reach a stable estimate of annual rainfall erosivity. Moreover, the temporal resolution of measuring devices was found to have a significant effect on R, with coarser temporal resolution leading to a higher relative bias.
 Article
(3955 KB)  Fulltext XML

Supplement
(211 KB)  BibTeX
 EndNote
Intense soil erosion has a significant impact on the environment, for example presenting a major threat for agricultural production or leading to increased sedimentation and pollution in rivers, which also affects aquatic organisms. Soil erosion modelling can be performed to detect critical parts of the landscape and design suitable countermeasures to reduce soil losses. One of the most frequently applied models for soil erosion modelling is the Universal Soil Loss Equation (USLE) and its successor the Revised Universal Soil Loss Equation (RUSLE) (e.g. Renard et al., 1997). In the scope of the RUSLE model, soil erosion is described by six factors, one of which is the rainfall erosivity factor R (in $\mathrm{MJ}\phantom{\rule{0.125em}{0ex}}\mathrm{mm}\phantom{\rule{0.125em}{0ex}}{\mathrm{ha}}^{\mathrm{1}}\phantom{\rule{0.125em}{0ex}}{\mathrm{h}}^{\mathrm{1}}$, Renard et al., 1997). Rainfall erosivity is often characterised by large spatial and temporal variability (e.g. Bezak et al., 2020, 2021a, b, c; Panagos et al., 2016, 2017; Petek et al., 2018), meaning that its estimation is not straightforward and requires adequate temporal and spatial data resolution.
In order to obtain robust rainfall erosivity values, highresolution observed rainfall data are needed, in time ideally with a 1 or 5 min resolution (Dunkerley, 2019), and in space ideally to represent the spatial heterogeneity (Peleg et al., 2021). However, rainfall data at this resolution are often only available for shorter periods of observation (e.g. 10 or 20 years) or not at all. A solution to overcome this shortcoming is the use of stochastic rainfall models that allow the generation of long time series of arbitrary length. Additionally, these models can generate time series for ungauged locations through regionalisation of model parameters. In some cases, gridded rainfall erosivity data are used as input to the USLEtype soil erosion models. In terms of spatial description of the rainfall erosivity, most often stationbased data are interpolated (e.g. Panagos et al., 2017) while satellitebased data could in the future provide useful estimates of gridded rainfall erosivity (e.g. Bezak et al., 2022). However, due to the stationbased approach of the USLE, the generation of spatial rainfall is not required but would be useful for more sophisticated approaches to estimate erosion (Eekhout et al., 2021). A few studies have investigated the possibility of applying stochastic precipitation models to generate rainfall time series to then estimate rainfall erosivity (e.g. Jebari et al., 2012; Lobo et al., 2015; de Oliveira et al., 2018; Haas et al., 2018). Methods used to model rainfall include clusterbased models (e.g. Onof et al., 2000; Onof and Wang, 2020), cascade models (e.g. Molnar and Burlando, 2005; Pohle et al., 2018; Müller and Haberlandt, 2018), methodoffragments models (e.g. Breinl and Di Baldassarre, 2019), or alternating renewal models (e.g. Callau Poduje and Haberlandt, 2017) or as part of weather generators (Peleg et al., 2017). The parameters of these methods are estimated based on observations, and the complexity of the models generally depends on the target temporal resolution. Thus, most studies are focused on daily data. For example, CLImate GENerator (CLIGEN) was applied to obtain daily rainfall estimates and calculate rainfall erosivity using daily data (e.g. de Oliveira et al., 2018; Lobo et al., 2015; Wang et al., 2018). Shortcomings such as sensitivity to the input parameters have been reported in the literature (e.g. Meyer et al., 2008; Haas et al., 2018). On the other hand, temporal highresolution time series (i.e. 5 min) are less often generated using stochastic rainfall models, although in recent years advancements have been made (e.g. Haberlandt et al., 2008; Vandenberghe et al., 2011; Vernieuwe et al., 2015; Callau Poduje and Haberlandt, 2017; MüllerThomy, 2020).
Thus, a few studies (e.g. De Oliveira et al., 2018; Haas et al., 2018) have investigated if stochastic rainfall models are able to correctly predict rainfall erosivity patterns at specific locations. In the case that a stochastic rainfall model is able to mimic the rainfall erosivity characteristics, generated longterm highresolution rainfall time series should then allow a robust estimation of annual and even monthly erosivity patterns. Similarly, a limited number of studies (e.g. AnguloMartinez et al., 2009) have investigated performance of different interpolation techniques related to the mapping of rainfall erosivity.
The main aim of this study is to evaluate and compare different rainfall generators and regionalisation approaches in order to obtain either directly or indirectly annual rainfall erosivity estimates for ungauged locations. Given a lack of highresolution rainfall time series, the research question is whether these tested methods can adequately reproduce observed annual rainfall. As a followup research question, we investigate the performance of tested methods in terms of specific erosive event characteristics. This information is not directly needed as input to the USLEtype models but is often studied and investigated in rainfall erosivity studies. Finally, given the existence of a highresolution rainfall time series, we also investigated how long these time series should be in order to obtain stable site annual rainfall erosivity. Hence, this information is relevant both for the soil erosion model applications using USLEtype models and for the studies investigating erosive event characteristics.
All tests were performed via leaveoneout cross validation, as the premise of this study is that highresolution time series are not widely available. Additionally, the effect of station density on the regionalisation performance was assessed by performing each test with five different station counts (20 %, 40 %, 60 %, 80 %, and 100 % of observed stations). To minimise the sampling uncertainty, 20 realisations of each test at each station density were performed.
Highresolution observed rainfall data for 159 stations bounded by the rectangle 7 to 12^{∘} E and 51 to 54^{∘} N (Fig. 1), centred over the German federal state of Lower Saxony, were acquired from the German Weather Service (DWD). The 1 min source time series, from a combination of tipping bucket and later drop counter measurements, were aggregated to 5 min for use within this project. All data used for the project are restricted to the 10year period 2007–2016 to maximise the data availability across all stations, as all 159 stations have at least 98 % data availability for this period. The study area is dominated by lowland terrain, with the only mountains of significance being the southeastlying Harz mountain range. The region is predominantly classified as having a temperate oceanic (Cfb) climate according to Köppen–Geiger (Kottek et al., 2006). The far eastern portion of the study area is categorised as temperate continental (Dfb) and the Harz mountain range as cool continental (Dfc). Figure 2 displays the longterm seasonal rainfall and temperature variability averaged over the German federal state of Lower Saxony. Annual rainfall varies from 950 mm in the Harz mountain range to under 400 mm in lowerlying areas east of the study area. As can be seen from Figs. 1 and 2, there is for most locations no significant difference between summer and winter precipitation in the study area. In terms of monthly rainfall erosivity, higher values (i.e. around 100 $\mathrm{MJ}\phantom{\rule{0.125em}{0ex}}\mathrm{mm}\phantom{\rule{0.125em}{0ex}}{\mathrm{ha}}^{\mathrm{1}}\phantom{\rule{0.125em}{0ex}}{\mathrm{h}}^{\mathrm{1}}\phantom{\rule{0.125em}{0ex}}{\mathrm{month}}^{\mathrm{1}}$) can be seen for summer followed by spring and autumn, whilst the lowest rainfall erosivity values could be seen for winter (i.e. less than 20–30 $\mathrm{MJ}\phantom{\rule{0.125em}{0ex}}\mathrm{mm}\phantom{\rule{0.125em}{0ex}}{\mathrm{ha}}^{\mathrm{1}}\phantom{\rule{0.125em}{0ex}}{\mathrm{h}}^{\mathrm{1}}\phantom{\rule{0.125em}{0ex}}{\mathrm{month}}^{\mathrm{1}}$). The results from a study conducted by Ballabio et al. (2017) are in accordance to the results of this study.
In this study, four different methods to calculate annual rainfall erosivity (R) for ungauged sites were applied (Fig. 3). The first and simplest method is the direct regionalisation of observed mean annual rainfall erosivity (DirectR method). The other three methods all generate rainfall time series first, from which mean annual rainfall erosivity is subsequently calculated. The second method is the regionalisation of the observed 5 min rainfall time series (DirectP method). The final two methods are stochastic rainfall models – one being a regionalised disaggregation model using regionalised daily rainfall as its source (method Disagg) (MüllerThomy, 2020) and the other a regionalised alternating renewal model (method ARM) (Callau Poduje and Haberlandt, 2017). Detailed descriptions of the applied methods are provided in Sect. 3.2 and 3.3 while Sect. 3.1 provides details about the rainfall erosivity calculation.
3.1 Rainfall erosivity
Rainfall erosivity is one of the factors that has the highest impact on soil erosion rates. Rainfall erosivity is characterised by multiple properties of rainfall events such as the kinetic energy of raindrops, rainfall intensity, and rainfall duration. In order to calculate annual rainfall erosivity for a selected time span, the following equation proposed by Renard et al. (1997) can be used:
where R is rainfall erosivity ($\mathrm{MJ}\phantom{\rule{0.125em}{0ex}}\mathrm{mm}\phantom{\rule{0.125em}{0ex}}{\mathrm{ha}}^{\mathrm{1}}\phantom{\rule{0.125em}{0ex}}{\mathrm{h}}^{\mathrm{1}}$), I_{30} the maximum 30 min rainfall intensity for a specific rainfall event (mm h^{−1}), E the kinetic energy of the rainfall event (MJ ha^{−1}), n the total number of erosive events, and M the time span (years). Equation (2) is used to derive the kinetic energy of the rainfall event:
where e_{B} is the specific kinetic energy ($\mathrm{MJ}\phantom{\rule{0.125em}{0ex}}{\mathrm{ha}}^{\mathrm{1}}\phantom{\rule{0.125em}{0ex}}{\mathrm{mm}}^{\mathrm{1}}$), I the rainfall intensity (mm h^{−1}) for the event, and Δt the time interval (h). Various equations for calculation of e_{B} were developed for different parts of the world, where most often highfrequency measurements using optical disdrometers are used to derive the e_{B}−E relationship (e.g. Petan et al., 2010). One of the most frequently and globally used equations (e.g. Panagos et al., 2015, 2017) was proposed by Brown and Foster (1987):
This equation is also mentioned in the RUSLE Handbook (Renard et al., 1997) and is regarded as the standard method to estimate soil erosion using the RUSLE approach. Additionally, the equation has already been applied several times to similar climatic conditions (e.g. Panagos et al., 2015) and yielded meaningful results. This equation was used in the present study in order to calculate specific kinetic energy. Equation (3) is valid for rainfall intensities ranging between 0 and 250 mm h^{−1}.
Erosive rainfall events are defined according to the RUSLE methodology (Renard et al., 1997). A rainfall event is considered erosive if the total volume exceeds 12.7 mm of rain or if the maximum volume in 15 min is more than 6.35 mm. Here a 6 h period without rain is used in order to separate two consecutive erosive rainfall events. The monthly and annual rainfall erosivity values are then calculated based on the rainfall erosivity of all erosive events.
3.2 Direct regionalisation methods
3.2.1 DirectR method: direct regionalisation of mean annual rainfall erosivity R
The direct interpolation of erosivity was carried out using geostatistical methods (see e.g. textbooks from Isaaks and Srivastava, 1990, or Goovaerts, 1997). The spatial dependence of R is modelled using an isotropic spherical variogram model:
where c is 0.5, c_{0} is 0.3, and a is 30 000 m. For interpolation, ordinary kriging (OK) and external drift kriging (EDK) are applied. While OK assumes spatial stationarity, EDK relaxes the intrinsic hypothesis regarding the constant mean E and assumes a linear relationship between the mean of the target variable Z and one or more additional variables Y:
The coefficients a and b_{i} need not be known explicitly, but they are considered in building the kriging system. The additional variables Y_{i} need to be provided for all points with observed erosivity and for all unobserved points to be interpolated, usually on a raster. Here, the following additional variables are used in the analyses: daily mean rainfall (P_{mean}), maximum daily rainfall (P_{max}), the 90 and 99 % quantiles of daily rainfall (Pq90, Pq99), and the yearly wet fractions of days with rainfall higher than 12.7 mm (based on the RUSLE methodology; Renard et al., 1997) and 1 mm thresholds (wfd12, wfd1). These variables are extracted from regionalised daily data in a spatial resolution of 1 km^{2} (NLWKN, 2019) and are calculated as longterm averages from the period 2007–2016. The interpolation uses a minimum of 8 neighbours and a maximum of 12 neighbours within a radius of 300 km. The R statistical software (R core team, 2015) with the package “gstat” (Pebesma, 2004) is employed for the calculations. It should be noted that some other variables could have been selected such as mean annual precipitation, which is often used to estimate the mean annual rainfall erosivity in datasparse regions. However, since this study uses highresolution data, we focused on specific precipitation characteristics that could be obtained from these highresolution data.
3.2.2 DirectP method: regionalisation of 5 min rainfall
A second approach for the regionalisation of the annual R is to estimate the 5 min rainfall time series for unobserved locations based on the information of nearbymeasured rainfall time series. In this study, the nearestneighbour approach (NN) was used for the regionalisation of the 5 min rainfall time series from 2007–2016. This technique, also known as the Thiessen polygon method (Thiessen, 1911), is a simple approach which assigns for each unobserved point the observed rainfall time series of the closest available rain gauge. Despite this being a basic interpolation method, a prior investigation of different interpolation techniques (nearest neighbour, inverse distance, and ordinary kriging) led to the conclusion that this technique maintains the best temporal structure of rainfall at the 5 min timescale and yields the lowest error for the calculation of erosivity. One reason for the superiority of NN compared to the other interpolation methods might be that NN is the only method which does not smooth extremes, which is important for the estimation of erosive events.
3.3 Stochastic rainfall models
3.3.1 ARM method: an alternating renewal rainfall model
Stochastic rainfall models allow for the generation of rainfall time series of arbitrary length, including for unobserved locations through regionalisation. For this study, the alternating renewal model (ARM) based on the theory of renewal processes was used to generate 5 min synthetic rainfall time series. In this model, rainfall is described as a series of independent alternating wet and dry spells, described by the three variables: wet spell amount (WSA), wet spell duration (WSD), and dry spell duration (DSD) (Fig. 4). Probability distributions were fitted to observations of these variables using the method of Lmoments, with observed rainfall events being limited by a minimum WSA (1 mm) and DSD (60 min). Synthetic rainfall time series were then generated by producing random variates of these distributions.
Additionally, the temporal distribution of rainfall within a wet spell is described by a double exponential function conditioned on the wet spell time to peak (WSTP – modelled using a uniform distribution), wet spell peak intensity (WSPI – modelled using a copula; see below), and WSA (Fig. 5). Full details of the model can be found in Callau Poduje and Haberlandt (2017), with the following alterations which have been found to provide a better model performance, especially for regionalisation:

a twoparameter Khoudraji–Gumbel copula describes the dependence between WSA and WSD,

a twoparameter Tawn copula describes the dependence between WSD and the ratio WSPI : WSA,

the threeparameter Weibull distribution is used instead of the fourparameter kappa distribution for the variables DSD and WSA, being more robust in a regionalisation setting.
Both copulas were fitted using the maximum pseudolikelihood method. In total, the model consists of 19 parameters, fitted separately for summer (April–September) and winter (October–March).
3.3.2 Disagg method: cascade model
Another possibility to generate highresolution rainfall time series is to disaggregate daily time series, which generally exist for longer time periods and with higher station densities. For this study the microcanonical cascade model after MüllerThomy (2019, 2020) was applied due to its performance in previous studies (e.g. Müller and Haberlandt, 2015, 2018). The general cascade model scheme of disaggregating one coarse time step into “b” finer time steps is illustrated in Fig. 6. From daily rainfall amounts three time steps with 8 h duration are generated (b=3). For all further disaggregation steps b=2 is applied, resulting in temporal resolutions of $\mathrm{\Delta}t=\mathit{\{}\mathrm{4}\phantom{\rule{0.125em}{0ex}}\mathrm{h},\mathrm{2}\phantom{\rule{0.125em}{0ex}}\mathrm{h},\mathrm{1}\phantom{\rule{0.125em}{0ex}}\mathrm{h},\mathrm{30}\phantom{\rule{0.125em}{0ex}}\mathrm{min},\mathrm{15}\phantom{\rule{0.125em}{0ex}}\mathrm{min},\mathrm{7.5}\phantom{\rule{0.125em}{0ex}}\mathrm{min}\mathit{\}}$. To achieve Δt=5 min, a linear transformation is applied. More precisely, rainfall amounts of the Δt=7.5 min level are distributed uniformly on 2.5 min time steps, which are subsequently aggregated to 5 min time steps. The rainfall amount is conserved exactly in each disaggregation step. For a detailed description of the cascade model, the reader is referred to the description of the preceding cascade model in MüllerThomy (2020).
The cascade model parameters are estimated by the aggregation of observed 5 min time series of the recording stations available in each density scenario (no parameter calibration or optimisation was carried out). For the daily time series serving as a starting point for the disaggregation, the aggregated 5 min time series of all 159 stations are used, independent of the applied density scenario. To investigate how suitable the disaggregation of daily information is for unobserved locations and a regionalisation of the daily precipitation is done prior to the application of the cascade model. Here, an ordinary kriging approach (OK) was used for the regionalisation of daily rainfall time series from 2007–2016. The interpolation uses an isotropic exponential variogram as in Eq. (6), a minimum of 4 neighbours and a maximum of 12 neighbours within a radius of 150 km.
where c_{0} is 0.4, c is 1.5, and a is 186 280 m.
3.4 Regionalisation schemes and station selection
In order to adequately test the performance of the different methods, all regionalisations were performed in a crossvalidation mode at varying station densities. Five station density scenarios were chosen: 20 % (N=32), 40 % (N=64), 60 % (N=96), 80 % (N=128), and 100 % (N=159) of the total available station count. Stations were selected at random and are consistent across the different testing methods presented above. Important to note is that the cross validation is only performed on the stations chosen at the 20 % level (N=32) – the higher densities only add further supplementary stations available for the regionalisation, with the assumption that the regionalisation performance will improve at a higher available station count. Furthermore, 20 realisations were performed for each density scenario to minimise the influence of station selection on the results. This scheme is illustrated graphically in Fig. 7.
3.5 Effect of time series length on the calculation or mean annual R
One further research question of interest is how long a rainfall time series must be in order to achieve a stable (i.e. robust) result of mean annual rainfall erosivity. The importance of such a research question lies in the fact that rainfall series used to calculate annual erosivity are often of limited length. Too short time series could lead to uncertain estimations of rainfall erosivity, which could affect the estimated soil erosion (i.e. under or overestimation).
Using the alternating renewal rainfall model described in Sect. 3.3.1, we investigated how many years of data are needed in order to obtain stable estimations of the annual rainfall erosivity. For this purpose, 18 stations with the longest observation time series length (mean = 22 years) were selected for a more robust model fitting. For each station, the ARM model described in Sect. 3.3.1 was fitted. Afterwards, 200 years of synthetic rainfall time series were generated 50 times for all 18 stations. The effect of time series length was investigated by calculating mean annual rainfall erosivity for each station and for each realisation using, separately, 2, 5, 10, 20, 30, 40, 50, 60, 70, 80, 90, 100, 120, 140, 160, 180, and 200 years of data. Results within ±20 % of the mean annual erosivity calculated for 200 years were considered stable. The 20 % threshold value was selected after checking the variability in the mean annual rainfall erosivity for specific stations and after comparing differences in mean annual rainfall erosivity values among stations. Hence, for most of the stations the maximum differences in the annual rainfall erosivity for specific years exceeded 20 % while approximately onehalf of the years the annual rainfall erosivity values were within the 20 % range.
3.6 Evaluation criteria
To assess the relative performance of the four different methods (Fig. 3), three different evaluation criteria were chosen. The first is the Pearson correlation coefficient r_{xy} between the annual rainfall erosivity calculated from observed rainfall and the estimated mean annual erosivity, i.e. regionalised by the different methods, at a given station density scenario across all realisations and the 32 reference stations. It is worth remembering that this measure is an indication of linear correlation only. The second is the relative root mean square error (RMSE) of the mean annual rainfall erosivity for a given station density scenario across all realisations and stations, given by Eq. (7):
where x refers to mean annual rainfall erosivity estimated from observations, y is the estimated mean annual rainfall erosivity estimated by the different methods proposed in this work, and N is the number of stations. The third is the median relative bias rB_{med} of the mean annual erosivity. For a given station density scenario the relative bias rB is calculated over all 32 stations for one realisation, and the median relative Bias rB_{med} is provided as a summarising result (referred to as relative bias in the following):
4.1 Mean annual erosivity R
The main focus of this study was to evaluate the performance of the four different tested methods in reproducing observed mean annual erosivity as input to the USLEtype models. It is the most relevant attribute from the perspective of the soil erosion modelling community. For the direct regionalisation of erosivity (DirectR), EDK with mean annual precipitation (P_{mean}) as external drift was found to provide the best performance. Direct regionalisation provides the best results overall, in terms of both accuracy and precision. The Pearson correlation (Fig. 8) by this method is larger than for the other three methods, which show more or less the same result. Its root mean square error is also lower than that of the other methods (Fig. 8). The rB_{med} is the only performance criteria where this method is not clearly better (Fig. 8). In terms of rB_{med} the DirectR method is followed by DirectP. ARM and Disagg in most cases yield relative bias larger than 10 % and 20 %, respectively. In terms of relative RMSE and Pearson correlation, the ARM and Disagg methods performed relatively similarly. The median result over all realisations showed slightly better results for the direct regionalisation of rainfall (DirectP) compared to stochastic rainfall models, although the range of results is greater than for DirectR. The disaggregation model performed worse than the other methods, with a >20 % underestimation of mean annual erosivity. However, the Disagg results were found to be sensitive to the applied “measuring resolution” of the generated time series (please see Fig. S1 in the Supplement for details), which could be represented better by simple modifications (MüllerThomy, 2020).
With increasing station density, the median result was generally improved, in particular for the Pearson correlation (Fig. 8). This is less noticeable for rB_{med}, as bias likely indicates the inherent ability of the underlying method to replicate the mean annual R (Fig. 8). Moreover, it seems that for ARM and DirectP the results change greatly between realisations (i.e. larger spread of the results), meaning that the station setting is more decisive, with DirectP being the most affected. The DirectR and Disagg methods seem to be more robust in terms of station setting, which indicates their usage for regions with low station densities. Thus, it seems that for areas similar to that of Lower Saxony (i.e. relatively flat areas with small changes in erosivity), the DirectR method is preferred in case one needs to estimate the rainfall erosivity for the ungauged locations. The application of this method is also the simplest of the four methods (Fig. 3), especially when compared to the ARM and Disagg methods, since these two methods require development of stochastic rainfall models and estimation of the model parameters. Thus, in terms of mean annual rainfall erosivity, the use of stochastic rainfall models did not provide an improvement of the results in terms of performance in space (Fig. 8).
In terms of the number of stations needed to provide good estimates of rainfall erosivity for the ungauged locations, it is clear that higher station density yields better results, which was expected (Fig. 8). Thus, DirectR showed decreasing performance with decreasing station density, $\text{D100}>\text{D80}>\text{D60}>\text{D40}>\text{D20}$ (Fig. 8), with somewhat diminishing improvements in performance above D80. Similar conclusions can be made for the DirectP method while for the ARM and Disagg this relationship was not so evident for the rB_{med} and RMSE (Fig. 8). Therefore, even for topographically relatively homogeneous areas (compared to for example alpine area) such as Lower Saxony, the accuracy of rainfall erosivity maps greatly depends on the number of stations used for the interpolation. Hence, it is clear that estimation of rainfall erosivity for ungauged areas is in all cases exposed to some degree of bias due to the interpolation (Fig. 8). Even in cases where the density of stations is high (e.g. D80 or D100 scenarios), there was a slight bias (few percentage points) in estimation of the rainfall erosivity for ungauged locations using the DirectR and DirectP methods while for ARM and the rainfall disaggregation model the median relative bias is larger than 10 % and 20 %, respectively (Fig. 8). Additionally, it should be assumed that the estimation bias for ungauged locations within topographically complex terrain would be even higher. Therefore, these results indicate that the density of gauging stations should be as high as possible in order to obtain optimal rainfall erosivity estimates.
4.2 Erosive event characteristics
Although the main focus of the study was the calculation of the mean annual erosivity R, in some specific applications more details about the rainfall erosivity at a location might be required, and characteristics of erosive events are often studied and compared (e.g. Bezak et al., 2021b). This information is not directly used as input to the USLEtype models; however, studies that investigate changes in erosivity patterns in time (i.e. climate change studies) might be interested in changes in the number of erosive events or erosive event characteristics. In such a case, the DirectR method cannot be used since this method is only able to provide estimates of the mean annual rainfall erosivity and does not provide a time series of erosive events. Naturally, a similar procedure as in the case for DirectR (Sect. 3.2.1) could be used for any other variable of interest (e.g. number of erosive events, mean duration of the erosive events). However, the EDK setup used for mean annual R is unlikely to be optimal for other variables, which means that an optimal EDK setup would need to be investigated for each variable of interest separately and thus could be considered relatively time consuming.
However, three of the four methods presented in this study, namely DirectP, ARM, and Disagg, are able to reproduce erosive events themselves from which the mean annual R is calculated. How well the three methods reproduce erosive event characteristics is explored in this section, and the results are presented in Table 1. Figure 9 displays the median relative bias of different erosive event variables. The mean annual event count and precipitation sum are best represented by the DirectP method. Whereas the median error is close to zero, the range of errors is well over 100 % when one considers outliers. The Disagg method represented the event count well but underestimates the annual volume slightly, whereas the ARM method underestimated both the annual count and volume (Fig. 9). Performance improved slightly for all methods with increasing station density (not shown).
For both the mean event duration and volume (Fig. 9), the results again show that the DirectP method was the most efficient. The Disagg method significantly overestimated the event duration and at the same time underestimated the event volume. However, in the case of using the Disagg method the station density showed less of an effect on performance compared to the other methods (not shown here). An overestimation of the erosive event duration was to be expected as being previously identified by Jebari et al. (2012) with overestimations higher than 40 %. Here the overestimations are higher as the disaggregation inherits the errors caused by the regionalisation of the daily rainfall. Because of the unbiased estimator, OK tends to smoothen the spatial structures of the rainfall, leading to overestimation of the low intensities (explaining the longer event durations) and underestimation of the extreme ones (explaining the lower event volumes). The performance of the disaggregation may improve if another regionalisation method that better captures the temporal variability is employed.
The ARM method underestimated both mean event duration and mean event volume, which explains the underestimation in both annual number of events and their volume. Thus, it can be seen that DirectP outperformed the ARM and Disagg methods not only in terms of annual rainfall erosivity but also in terms of specific events characteristics. In case one would like to obtain erosive event characteristics for ungauged sites, the DirectP method should be preferred since it was able to produce acceptable results and yielded better performance compared with the two tested stochastic rainfall models.
Moreover, it should be noted that other available stochastic rainfall models could perhaps yield better performance in comparison to the selected stochastic rainfall models (see Sect. 1 for examples). The scope of the study limited the selection of stochastic rainfall models to the two presented in this study only. Since any rainfall model has its own unique strengths and weaknesses, it is possible that some other nontested model could yield better performance in terms of reproducing maximum 30 min rainfall intensities, which are directly used for the estimation of the rainfall erosivity (Sect. 3.1).
4.3 Annual rainfall erosivity – data length sensitivity
Despite the fact that DirectR and DirectP methods yielded better performance than the evaluated stochastic rainfall models, the benefit of the latter is the ability to generate long time series of arbitrary length of highresolution data for unobserved locations. The goal of this section is to investigate how long the synthetic time series should be in order to obtain a stable estimate of the mean annual rainfall erosivity, which is most frequently used as an input to the soil erosion models (Panagos et al., 2015, 2017). Thus, this information is relevant for the soil erosion modellers in order to evaluate the impact of potential bias in the assessment of the mean annual rainfall erosivity on the soil erosion modelling results. Using the ARM model and the methodology described in Sect. 3.5, it was investigated how many years of data are needed in order to obtain stable annual rainfall erosivity estimation. Important to remember is that the ARM model performance for this task is better than what was shown in Sect. 4.1 and 4.2, as here the ARM model was fitted directly to observations and not regionalised. Figure 10 shows results of this investigation. It can be seen that the variability between different realisations was quite high (Fig. 10). Moreover, investigation of the intersection between the 5 % and 95 % realisation quantiles (i.e. with the aim to exclude potential extremes) and the ±20 % interval of the mean annual rainfall erosivity (calculated from the full 200year time series) indicates that in the case of the 5 % quantile (Fig. 10), in most cases 60 years of data were needed in order to obtain a value within this ±20 % interval (Fig. 10). This indicates that calculations of the annual rainfall erosivity for soil erosion modelling using USLE or RUSLE (e.g. Renard et al., 1997; Panagos et al., 2017) using only a limited sample size (e.g. less than 5 or 10 years) will likely result in a greater than ±20 % difference to the longterm mean. Consequently, a similar impact (i.e. over or underestimation) on the calculated soil erosion rates will be obtained if one applies the RUSLE equation for the prediction. Moreover, it should be noted that the results are to some extent sensitive to the selection of the threshold (i.e. 20 % value). More specifically, using lower threshold values would result in needing longer time series to obtain stable annual rainfall erosivity estimates. Conversely using higher threshold values would require shorter time series.
This study evaluated four methods that can be used to estimate the annual mean rainfall erosivity (R) in space. Based on the presented results the following conclusions can be drawn.

For the mean annual rainfall erosivity both tested direct regionalisation methods (DirectR and DirectP) outperformed (Fig. 8) the tested stochastic rainfall models (ARM and Disagg), with slightly better results for DirectR. Furthermore, in terms of method complexity, DirectR can be regarded as the simplest since it does not require the fitting of any model parameters. Differences among tested methods were relatively large, for example, in relative bias up to 25 %.

The main drawback of the DirectR method is that it cannot be used to estimate the number of erosive events or mean event duration without applying the model to every variable separately (e.g. number of erosive events, annual rainfall erosivity). This information is sometimes additionally required in erosivity studies, although it is not directly used by the USLEtype models. Therefore, the DirectP method has the advantage that it is able to generate highresolution time series of erosive events for ungauged sites. Therefore, information about the number of erosive events and the characteristics of erosive events can be determined as well. In terms of the characteristics of the erosive events, the DirectP method yielded better performance than both tested stochastic rainfall models.

Both rainfall generators have proven their applicability in the field of soil erosion modelling since they are able to produce long synthetic series of the highresolution data, which can be used to calculate stable rainfall erosivity estimates.

The crossvalidation methodology using multiple density scenarios (Fig. 7) indicated that all methods performed slightly better with increasing station density. However, interpolation of rainfall erosivity for ungauged locations will in the case of the DirectR and DirectP methods introduce some bias (∼5 %), also in the case of having very high station density (Fig. 8). For the ARM and Disagg methods, this bias can be larger than 10 % (Fig. 8). Even more significant differences could be expected in the case of topographically more complex areas. Hence, station density should be as high as possible to obtain optimal rainfall erosivity estimates for ungauged locations.

Investigation of the impact of time series length on the annual rainfall erosivity for 18 stations was additionally carried out using the ARM model. More than 60 years of data were required in the case that one would like to obtain rainfall erosivity estimates within 20 % of the actual longterm mean annual rainfall erosivity.
Thus, this conclusion is of critical importance for soil erosion studies where rainfall erosivity estimates are used as input, since in most cases the highresolution data used to estimate rainfall erosivity are much shorter than 60 years. So, in cases where only 5–10 years of observed rainfall data are available, the estimated mean annual rainfall erosivity can be up to ±100 % in comparison to the actual longterm mean annual rainfall erosivity, which can be reduced by the application of one of the here used rainfall generators.
It should be noted that the approaches presented in this paper should be applied and tested for further case studies with different rainfall and topographical characteristics than for Lower Saxony, which is mostly flat and without major orographic obstacles. Additionally, some study limitations and lessons learned can also be made based on the presented results and conclusions: for example, resolution of the measurement device, which has evolved in recent decades, has a significant effect on the calculated rainfall erosivity and relative bias (Fig. S1).
Data can be requested from the German Weather Service (DWD). The code used in this study is freely available from the first author upon request.
The supplement related to this article is available online at: https://doi.org/10.5194/esurf108512022supplement.
All authors developed the concepts of the manuscript. RP conducted most of the calculations with the support of BS, HMT, UH, and NB. NB drafted the first version of the manuscript. All authors contributed to writing and editing of the manuscript.
The contact author has declared that none of the authors has any competing interests.
Publisher's note: Copernicus Publications remains neutral with regard to jurisdictional claims in published maps and institutional affiliations.
We would like to acknowledge the German Weather Service (DWD) for provide data used in this study. Also, Nadav Peleg, Mark Silburn, and the anonymous reviewer are acknowledged as well as the associate editor Greg Hancock.
The results of the study are part of the bilateral research project between Slovenia and Germany “Stochastic rainfall models for rainfall erosivity evaluation” and research programme P20180 “Water Science and Technology, and Geotechnical Engineering: Tools and Methods for Process Analyses and Simulations, and Development of Technologies” (P20180) that is financed by the Slovenian Research Agency (ARRS). Hannes MüllerThomy has been financially supported by the DFG e.V., Bonn, Germany, as a Research Fellowship (MU 4257/11). Additionally, part of the results were also obtained in the scope of the bilateral project between Slovenia and Germany “Validation of precipitation reanalysis products for rainfallrunoff modelling in Slovenia (PREPROMISE)”, funded by the German Federal Ministry of Education and Research (BMBF).
This openaccess publication was funded by Technische Universität Braunschweig.
This paper was edited by Greg Hancock and reviewed by Nadav Peleg, D. Mark Silburn, and one anonymous referee.
AnguloMartínez, M., LópezVicente, M., VicenteSerrano, S. M., and Beguería, S.: Mapping rainfall erosivity at a regional scale: a comparison of interpolation methods in the Ebro Basin (NE Spain), Hydrol. Earth Syst. Sci., 13, 1907–1920, https://doi.org/10.5194/hess1319072009, 2009.
Ballabio, C., Borrelli, P., Spinoni, J., Meusburger, K., Michaelides, S., Beguería, S., Klik, A., Petan, S., Janeček, M., Olsen, P., Aalto, J., Lakatos, M., Rymszewicz, A., Dumitrescu, A., Tadić, M. P., Diodato, N., Kostalova, J., Rousseva, S., Banasik, K., Alewell, C., and Panagos, P.: Mapping monthly rainfall erosivity in Europe, Sci. Total Environ., 579, 1298–1315, https://doi.org/10.1016/j.scitotenv.2016.11.123, 2017.
Bezak, N., Ballabio, C., Mikoš, M., Petan, S., Borreli, P., and Panagos, P.: Reconstruction of past rainfall erosivity and trend detection based on the REDES database and reanalysis rainfall, J. Hydrol., 590, 125372, https://doi.org/10.1016/j.jhydrol.2020.125372, 2020.
Bezak, N., Borrelli, P., and Panagos, P.: A first assessment of rainfall erosivity synchrony scale at panEuropean scale, Catena, 198, 105060, https://doi.org/10.1016/j.catena.2020.105060, 2021a.
Bezak, N., Mikoš, M., Borrelli, P., Liakos, L., and Panagos, P.: An indepth statistical analysis of the rainstorms erosivity in Europe, Catena, 206, 105577, https://doi.org/10.1016/j.catena.2021.105577, 2021b.
Bezak, N., Petan, S., and Mikoš, M.: Spatial and temporal variability in rainfall erosivity under Alpine climate: a Slovenian case study using optical disdrometer data, Front. Environ. Sci., 423, 735492, https://doi.org/10.3389/fenvs.2021.735492, 2021c.
Bezak, N., Borrelli, P., and Panagos, P.: Exploring the possible role of satellitebased rainfall data in estimating inter and intraannual global rainfall erosivity, Hydrol. Earth Syst. Sci., 26, 1907–1924, https://doi.org/10.5194/hess2619072022, 2022.
Breinl, K. and Di Baldassarre, G.: Spacetime disaggregation of precipitation and temperature across different climates and spatial scales, Journal of Hydrology: Regional Studies, 21, 126–146, 2019.
Brown, L. C. and Foster, G. R.: Storm Erosivity Using Idealized Intensity Distributions, Am. Soc. Agric. Biol. Eng., 30, 0379–0386, https://doi.org/10.13031/2013.31957, 1987.
Callau Poduje, A. C. and Haberlandt, U.: Short time step continuous rainfall modeling and simulation of extreme events, J. Hydrol., 552, 182–197, 2017.
CDC: Climate Data Center, https://www.dwd.de/EN/climate_environment/cdc/cdc_node_en.html, last access: 15 December 2020.
De Oliveira, J. P. B., Cecilio, R. A., Pruski, F. F., Zanetti, S. S., and Moreira, M. C.: Assessing the use of rainfall synthetic series to estimate rainfall erosivity in Brazil, Catena, 171, 327–336, 2018.
Dunkerley, D. L.: Rainfall intensity bursts and the erosion of soils: an analysis highlighting the need for high temporal resolution rainfall data for research under current and future climates, Earth Surf. Dynam., 7, 345–360, https://doi.org/10.5194/esurf73452019, 2019.
Eekhout, J. P. C., MillaresValenzuela, A., MartinezSalvador, A., GarciaLorenzo, R., PerezCutillas, P., ConesaGarcia, V., and de Vente, J.: A processbased soil erosion model ensemble to assess model uncertainty in climatechange impact assessments, Land Degrad. Dev., 32, 2409–2422, 2021.
Goovaerts, P.: Geostatistics for Natural Resources Evaluation, Oxford University Press, 483 pp., ISBN 9780195115383, 1997.
Haas, J., SchackKirchner, H., and Lang, F.: Adjustment of a weather generator to represent actual rain erosivity in the northern Black Forest – Germany, Catena, 163, 42–53, 2018.
Haberlandt, U., Ebner von Eschenbach, A.D., and Buchwald, I.: A spacetime hybrid hourly rainfall model for derived flood frequency analysis, Hydrol. Earth Syst. Sci., 12, 1353–1367, https://doi.org/10.5194/hess1213532008, 2008.
Isaaks, E. H. and Srivastava, R. M.: An Introduction to Applied Geostatistics, Oxford University Press, 592 pp., ISBN 9780195050134, 1990.
Jebari, S., Berndtsson, R., Olsson, J., and Bahri, A.: Soil erosion estimation based on rainfall disaggregation, J. Hydrol., 436–437, 102–110, 2012.
Kottek, M., Grieser, J., Beck, C., Rudolf, B., and Rubel, F.: World Map of the KöppenGeiger climate classification updated, Meteorol. Z., 15, 259–263, https://doi.org/10.1127/09412948/2006/0130, 2006.
Lobo, G. P., Frankenberger, J. R., Flanagan, D. C., and Bonilla, C. A.: Evaluation and improvement of the CLIGEN model for storm and rainfall erosivity generation in Central Chile, Catena, 127, 206–213, 2015.
Meyer, C. R., Renschler, C. S., and Vining, R. C.: Implementing quality control on a random number stream to improve a stochastic weather generator, Hydrol. Process., 22, 1069–1079, 2008.
Molnar, P. and Burlando, P.: Preservation of rainfall properties in stochastic disaggregation by a simple random cascade model, Atmos. Res., 77, 137–151, 2005.
Müller, H. and Haberlandt, U.: Temporal rainfall disaggregation using a multiplicative cascade model for spatial application in urban hydrology, in: Rainfall in urban and natural Systems, Proceedings of the 10th International Workshop on Precipitation in Urban Areas (UrbanRain15), edited by: Molnar, P. and Peleg, N., Pontresina, 1–5 December 2015, Paper UR1543, ETHZürich, Institute of Environmental Engineering, https://doi.org/10.3929/ethza010549004, 2015.
Müller, H. and Haberlandt, U.: Temporal rainfall disaggregation using a multiplicative cascade model for spatial application in urban hydrology, J. Hydrol., 556, 847–864, https://doi.org/10.1016/j.jhydrol.2016.01.031, 2018.
MüllerThomy, H.: Improving the autocorrelation in disaggregated time series for urban hydrological applications, in: 11th Workshop on Precipitation in Urban Areas (UrbanRain18), edited by: Peleg, N. and Molnar, P., 5–7 December 2018, Pontresina, Switzerland, 75–76, https://doi.org/10.3929/ethzb000347485, 2019.
MüllerThomy, H.: Temporal rainfall disaggregation using a microcanonical cascade model: possibilities to improve the autocorrelation, Hydrol. Earth Syst. Sci., 24, 169–188, https://doi.org/10.5194/hess241692020, 2020.
NLWKN: Globaler Klimawandel – Wasserwirtschaftliche Folgen für das Binnenland (KliBiW), Abschlussbericht Phase V, Niedersächsischer Landesbetrieb für Wasserwirtschaft, Küsten und Naturschutz, Norden, 2019.
Onof, C. and Wang, L.P.: Modelling rainfall with a Bartlett–Lewis process: new developments, Hydrol. Earth Syst. Sci., 24, 2791–2815, https://doi.org/10.5194/hess2427912020, 2020.
Onof, C., Chandler, R. E., Kakou, A., Northrop, P., Wheater, H. S., and Isham, V.: Rainfall modelling using Poissoncluster processes: A review of developments, Stoch. Env. Res. Risk A., 14, 384–411, 2000.
Panagos, P., Ballabio, C., Borrelli, P., Meusburger, K., Klik, A., Rousseva, S., Tadić, M. P., Michaelides, S., Hrabalíková, M., Olsen, P., Aalto, J., Lakatos, M., Rymszewicz, A., Dumitrescu, A., Beguería, S., and Alewell, C.: Rainfall erosivity in Europe, Sci. Total Environ., 511, 801–814, https://doi.org/10.1016/j.scitotenv.2015.01.008, 2015.
Panagos, P., Ballabio, C., Borrelli, P., and Meusburger, K.: Spatiotemporal analysis of rainfall erosivity and erosivity density in Greece, Catena, 137, 161–172, 2016.
Panagos, P., Borrelli, P., Meusburger, K., Yu, B., Klik, A., Lim, K. J., Yang, J. E., Ni, J., Miao, C., Chattopadhyay, N., Hamidreza Sadeghi, S., Hazbavi, Z., Zabihi, M., Larionov, G. A., Krasnov, S. F., Gorobets, A. V., Levi, Y., Erpul, G., Birkel, C., Hoyos, N., Naipal, V., Oliveira, P. T. S., Bonilla, C. A., Meddi, M., Nel, W., Al Dashti, H., Boni, M., Diodato, N., Van Oost, K., Nearing, M., and Ballabio, C.: Global rainfall erosivity assessment based on hightemporal resolution rainfall records, Nat. Sci. Rep., 7, 4175, https://doi.org/10.1038/s41598017042828, 2017.
Pebesma, E. J.: Multivariable geostatistics in S: the gstat package, Comput. Geosci., 30, 683–691, 2004.
Peleg, N., Fatichi, S. Paschalis, A., Molnar, P., and Burlando, P.: An advanced stochastic weather generator for simulating 2D highresolution climate variables, J. Adv. Model. Earth Sy., 9, 1595–1627, 2017.
Peleg, N., Skinner, C., Ramirez, J. A., and Molnar, P.: Rainfall spatialheterogeneity accelerates landscape evolution processes, Geomorphology, 390, 107863, https://doi.org/10.1016/j.geomorph.2021.107863, 2021.
Petan, S., Rusjan, S., Vidmar, A., and Mikoš, M.: The rainfall kinetic energyintensity relationship for rainfall erosivity estimation in the Mediterranean part of Slovenia, J. Hydrol., 391, 314–321, 2010.
Petek, M., Mikoš, M., and Bezak, N.: Rainfall erosivity in Slovenia: Sensitivity estimation and trend detection, Environ. Res., 167, 528–535, 2018.
Pohle, I., Niebisch, M., Müller, H., Schümberg, S., Zha, T., Maurer, T., and Hinz, C.: Coupling Poisson rectangular pulse and multiplicative microcanonical random cascade models to generate subdaily precipitation time series, J. Hydrol., 562, 50–70, 2018.
R Core Team: R: A language and environment for statistical computing, R Foundation for Statistical Computing, Vienna, Austria, http://www.Rproject.org/ (last access: 4 October 2017), 2015.
Renard, K. G., Foster, G. R., Weesies, G. A., McCool, D. K., and Yoder, D. C.: Predicting soil erosion by water: a guide to conservation planning with the Revised Universal Soil Loss Equation (RUSLE), Agricultural Handbook no. 703, USDA ARS, Washington, DC, 65–100, ISBN 0160489385, 1997.
Thiessen, A. H.: Precipitation averages for large areas, Mon. Weather Rev., 39, 1082–1809, 1911.
Vandenberghe, S., Verhoest, N. E. C., Onof, C., and De Baets, B.: A comparative copulabased bivariate frequency analysis of observed and simulated storm events: a case study on BartlettLewis modeled rainfall, Water Resour. Res., 47, W07529, https://doi.org/10.1029/2009WR008388, 2011.
Vernieuwe, H., Vandenberghe, S., De Baets, B., and Verhoest, N. E. C.: A continuous rainfall model based on vine copulas, Hydrol. Earth Syst. Sci., 19, 2685–2699, https://doi.org/10.5194/hess1926852015, 2015.
Wang, W., Flanagan, D. C., Yin, S., and Yu, B.: Assessment of CLIGEN precipitation and storm pattern generation in China, Catena, 69, 96–106, 2018.