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**Hydrology and Earth System Sciences**
An interactive open-access journal of the European Geosciences Union

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**Research article**
16 Jan 2019

**Research article** | 16 Jan 2019

Stochastic reconstruction of spatio-temporal rainfall patterns by inverse hydrologic modelling

^{1}Technische Universität Dresden, Institute of Hydrology and Meteorology, Dresden, Germany^{2}University of Queensland, EAIT, Centre for Coal Seam Gas, Brisbane, Australia^{3}Universität Stuttgart, Institute for Modelling Hydraulic and Environmental Systems, Stuttgart, Germany

^{1}Technische Universität Dresden, Institute of Hydrology and Meteorology, Dresden, Germany^{2}University of Queensland, EAIT, Centre for Coal Seam Gas, Brisbane, Australia^{3}Universität Stuttgart, Institute for Modelling Hydraulic and Environmental Systems, Stuttgart, Germany

**Correspondence**: Jens Grundmann (jens.grundmann@tu-dresden.de)

**Correspondence**: Jens Grundmann (jens.grundmann@tu-dresden.de)

Abstract

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Knowledge of
spatio-temporal rainfall patterns is required as input for distributed
hydrologic models used for tasks such as flood runoff estimation and
modelling. Normally, these patterns are generated from point observations on
the ground using spatial interpolation methods. However, such methods fail in
reproducing the true spatio-temporal rainfall pattern, especially in data-scarce regions with poorly gauged catchments, or for highly dynamic,
small-scale rainstorms which are not well recorded by existing monitoring
networks. Consequently, uncertainties arise in distributed rainfall–runoff
modelling if poorly identified spatio-temporal rainfall patterns are used,
since the amount of rainfall received by a catchment as well as the dynamics
of the runoff generation of flood waves is underestimated. To address this
problem we propose an inverse hydrologic modelling approach for stochastic
reconstruction of spatio-temporal rainfall patterns. The methodology combines
the stochastic random field simulator Random Mixing and a distributed
rainfall–runoff model in a Monte Carlo framework. The simulated
spatio-temporal rainfall patterns are conditioned on point rainfall data from
ground-based monitoring networks and the observed hydrograph at the catchment
outlet and aim to explain measured data at best. Since we infer a three-dimensional input variable from an integral catchment response, several
candidates for spatio-temporal rainfall patterns are feasible and allow for an
analysis of their uncertainty. The methodology is tested on a synthetic
rainfall–runoff event on sub-daily time steps and spatial resolution of
1 km^{2} for a catchment partly covered by rainfall. A set of plausible
spatio-temporal rainfall patterns can be obtained by applying this inverse
approach. Furthermore, results of a real-world study for a flash flood event
in a mountainous arid region are presented. They underline that knowledge
about the spatio-temporal rainfall pattern is crucial for flash flood
modelling even in small catchments and arid and semiarid environments.

How to cite

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How to cite.

Grundmann, J., Hörning, S., and Bárdossy, A.: Stochastic reconstruction of spatio-temporal rainfall patterns by inverse hydrologic modelling, Hydrol. Earth Syst. Sci., 23, 225–237, https://doi.org/10.5194/hess-23-225-2019, 2019.

1 Motivation

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The importance of spatio-temporal rainfall patterns for rainfall–runoff (RR) estimation and modelling is well known in hydrology and has been addressed by several simulation studies, especially since distributed hydrologic models have become available. Many of those studies demonstrated the effect of resulting runoff responses for different spatial rainfall patterns (Beven and Hornberger, 1982; Morin et al., 2006; Nicotina et al., 2008; Obled et al., 1994) or addressed the errors in runoff prediction and the difficulties in parameterisation and calibration of hydrologic models if the spatially distribution of rainfall is not well known (Andreassian et al., 2001; Chaubey et al., 1999; Lopes, 1996; Troutman, 1983). As a consequence, studies were performed to investigate configurations of rainfall monitoring networks (Faures et al., 1995) and rainfall errors and uncertainties for hydrologic modelling (McMillan et al., 2011; Renard et al., 2011).

In general, rainfall monitoring networks based on point observations on the ground (station data) require interpolation methods to obtain spatio-temporal rainfall fields usable for distributed hydrologic modelling. Traditional interpolation methods fail in reproducing the true spatio-temporal rainfall pattern, especially for (i) data-scarce regions with poorly gauged catchments and low network density; (ii) highly dynamic, small-scale rainstorms which are not well recorded by existing monitoring networks; and (iii) catchments which are partly covered by rainfall. Consequently, uncertainties are associated with poorly identified spatio-temporal rainfall patterns in distributed rainfall–runoff-modelling since the amount of rainfall received by a catchment as well as the dynamics of runoff generation processes are typically underestimated by current methods.

The effects of poorly estimated spatio-temporal rainfall fields are visible in particular for semiarid and arid regions, where rainstorms show a great variability in space and time and the density of ground-based monitoring networks is sparse compared to other regions (Pilgrim et al., 1988). Based on an analysis of 36 events in a mountainous region of Oman, McIntyre et al. (2007) show a wide range of event-based runoff coefficients, which underlines that achieving reliable runoff predictions by using hydrologic models in those regions is extremely challenging. This is supported by several simulation studies (Al-Qurashi et al., 2008; Bahat et al., 2009), who address the uncertainties in model parameterisation due to uncertain rainfall input. In this context Gunkel and Lange (2012) report that reliable model parameter estimation was only possible by using rainfall radar. However, this information is not available everywhere.

To address the inherent uncertainties described above, stochastic rainfall generators are used intensively to create spatio-temporal rainfall inputs for distributed hydrologic models to transform rainfall into runoff. A large amount of literature exists describing different approaches for space–time simulation of rainfall fields, including multi-site temporal simulation frameworks (Wilks, 1998), approaches based on the theory of random fields (Bell, 1987; Pegram and Clothier, 2001), or approaches based on the theory of point processes and its generalisation, which includes the popular turning-band method (Mantoglou and Wilson, 1982). Enhancements were made in order to portray different rainstorm patterns and distinct properties of rainfall fields, like spatial covariance structure, space–time anomaly, and intermittency (see Leblois and Creutin, 2013; Paschalis et al., 2013; Peleg et al., 2017).

Applications of spatio-temporal rainfall simulations together with hydrologic models are straightforward Monte Carlo types, where a large number of potential rainfall fields are generated driven by stochastic properties of observed rainstorms or longer time series. These fields are used as inputs for distributed hydrologic model simulations to investigate the impact of certain aspects of rainfall like uncertainty in measured rain depth, spatial variability, etc., on simulated catchment responses. Rainfall simulation applications are performed in unconditional mode (reproducing rain field statistics only) or conditional mode, where observations (e.g. from rain gauges) are reproduced too. The latter are commonly used for investigating the effect of spatial variability using fixed total precipitation and variations in spatial patterns (Casper et al., 2009; Krajewski et al., 1991; Paschalis et al., 2014; Shah et al., 1996). However, stochastic rainfall simulations in combination with distributed hydrologic modelling can be computationally demanding and can fail at matching the observed streamflow if rainfall fields are conditioned on rainfall point observations only.

On the other hand, inverse hydrologic modelling approaches have been developed to estimate rainfall time series based on observed streamflow data. Those approaches require either an inversion of the underlying mathematical equations for the non-linear transfer function (Kirchner, 2009; Kretzschmar et al., 2014) or an application of the hydrologic model in a Bayesian inference scheme (Del Giudice et al., 2016; Kavetski et al., 2006). Up to now, both approaches deliver time series of catchment-averaged rainfall only, which gives no idea about the spatial extent and distribution of rainfall. This is particularly important when considering events such as localised rainstorms, which might be underestimated and not accurately portrayed.

The goal here is an event-based reconstruction of spatio-temporal
rainfall patterns which best explains measured point rainfall data and catchment
runoff response. For that we looked for potential candidates
for rainfall fields for sub-daily time steps and spatial resolution
of 1 km^{2} which, to our knowledge has not been done
so far. To achieve this task, we combined stochastic rainfall simulations
and distributed hydrologic modelling in an inverse modelling approach,
where spatio-temporal rainfall patterns are conditioned on rainfall
point observations and observed runoff. The methodology of the inverse
hydrologic modelling approach consists of the stochastic random field
simulator Random Mixing and a distributed rainfall–runoff model in
a Monte Carlo framework. Until now, Random Mixing, developed by Bárdossy and Hörning (2016b)
for solving inverse groundwater modelling problems, has been used by
Haese et al. (2017) for reconstruction and interpolation of precipitation
fields using different data sources for rainfall.

After this introduction the methods are described in Sect. 2. It gives an overview of the methodology and further details for the applied rainfall–runoff model, the Random Mixing and its application for rainfall fields. Section 3 aims to test the methodology. A synthetic test site is introduced which is used to demonstrate and discuss (i) the limits of common hydrologic modelling approaches (using rainfall interpolation) and (ii) the shortcomings of rainfall simulations which are not conditioned on the observed runoff. In contrast, the functionality of the inverse hydrologic modelling approach is illustrated and discussed. In Sect. 4, the inverse hydrologic modelling approach is applied for real-world data by an example of an arid mountainous catchment in Oman. The test site is introduced and results are shown and discussed. Finally, summary and conclusions are given in Sect. 5.

2 Methods

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The methodology described here can be characterized as an inverse hydrologic modelling approach. It aims to infer potential candidates for the unknown spatio-temporal rainfall patterns from runoff observations at the catchment outlet, known parameterisation of the rainfall–runoff model, and rain gauge observations. The approach combines a grid-based spatially distributed rainfall–runoff model and a conditional random field simulation technique called Random Mixing (Bárdossy and Hörning, 2016a, b). Random Mixing is used to simulate a conditional rainfall field which honours the observed rainfall values as well as their spatial and temporal variability. Afterwards, an optimisation is performed to additionally condition the rainfall field on the observed runoff. Therefore, the initial field is used as input to the rainfall–runoff model. The deviation between the simulated runoff and the observed runoff is evaluated based on the model efficiency (NSE) defined by Nash and Sutcliffe (1970). To minimise this deviation the rainfall field is mixed with another random field which exhibits certain properties such that the mixture honours the observed rainfall values and their spatio-temporal variability. This procedure is repeated until a satisfying solution, i.e. a conditional rainfall field that achieves a reasonable NSE, is found. To enable a reasonable uncertainty estimation the procedure is repeated until a predefined number of potential candidates has been found. In the following, rainfall is used interchangeably with precipitation.

A simple spatially distributed rainfall–runoff model is used as transfer function to portray the non-linear transformation of spatially distributed rainfall into runoff at catchment outlets. The model is dedicated to describe rainfall–runoff processes in arid mountainous regions, which are mostly based on infiltration excess and Hortonian overland flow. The model is working on regular grid cells in event-based modes. It is parsimonious in the number of parameters, considers transmission losses but has no base flow component. Pre-state information at the beginning of an event is neglected since runoff processes mostly start under dry conditions (Pilgrim et al., 1988).

More specifically, only simple approaches known from hydrologic textbooks
for the simulation of single rainfall–runoff events (no long-term
water balance) are used (Dyck and Peschke, 1983). Effective precipitation
*Pe*(*x*, *t*) with location *x*∈*D* and time *t*∈*T* is calculated
by an initial and constant rate loss model applied on each grid cell
which is affected by rainfall. The initial loss *I*_{a}(*x*) represents
interception and depression storage. If the accumulated precipitation
exceeds *I*_{a}(*x*) surface runoff may occur, which is reduced by the
constant rate *f*_{c}(*x*) throughout an event to consider infiltration.
The calculated effective precipitation (or surface runoff)
is transferred to the next river channel section considering translation
and attenuation processes. Translation is accounted for with a grid-based
travel-time function to include the effects of surface slope and roughness.
Attenuation is accounted for with a single linear storage unit with
recession constant *f*_{r}(*x*). Both approaches are applied on grid
cells affected by effective precipitation only to fully support spatial
distributed calculations corresponding to the spatial extent of the
rain field. The properties of several landscape units are addressed
by different parameter sets (for ${I}_{a}\left(x\right),\phantom{\rule{0.125em}{0ex}}{f}_{\mathrm{c}}\left(x\right),\phantom{\rule{0.125em}{0ex}}{f}_{\mathrm{r}}\left(x\right)$)
following the concept of hydrogeological response units (Gerner, 2013)
(since hydrologic processes are mostly driven by hydrogeology in these
regions). Runoff is routed to the catchment outlet by a simple lag
model in combination with a constant rate (*f*_{t}) loss model to
portray transmission losses along the stream channel. The RR model
is applied on an hourly time step on regular grids cells of 1 km by
1 km. Parameters are assumed to be known and fixed during the inverse
modelling procedure. The RR model is linked to Random Mixing directly
and named with the working title NAMarid.

Random Mixing is a geostatistical simulation approach. It uses copulas as spatial random functions (Bárdossy, 2006) and represents an extension to the gradual deformation approach (Hu, 2000). In the following a brief description of the Random Mixing algorithm is presented. A detailed explanation can be found in Hörning (2016).

The goal of the inverse hydrologic modelling approach presented herein
is to find a conditional precipitation field *P*(*x*, *t*) with location
*x*∈*D* and time *t*∈*T* which reproduces the observed spatial
and temporal variability and marginal distribution of *P*. This field
should also honour precipitation observations at locations *x*_{j}
and times *t*_{i}:

$$\begin{array}{}\text{(1)}& P({x}_{j},\phantom{\rule{0.125em}{0ex}}{t}_{i})={p}_{j,\phantom{\rule{0.125em}{0ex}}i}\phantom{\rule{0.25em}{0ex}}\mathrm{for}\phantom{\rule{0.25em}{0ex}}j=\mathrm{1},\phantom{\rule{0.125em}{0ex}}\mathrm{\dots}\phantom{\rule{0.125em}{0ex}},J\phantom{\rule{0.25em}{0ex}}\mathrm{and}\phantom{\rule{0.25em}{0ex}}i=\mathrm{1},\phantom{\rule{0.125em}{0ex}}\mathrm{\dots}\phantom{\rule{0.125em}{0ex}},I,\end{array}$$

Note that *P* denotes a spatial field and *p* denotes a precipitation
value within that field. Furthermore, the solution of a rainfall–runoff
model using the field *P* as input variable should approximately
honour the observed runoff:

$$\begin{array}{}\text{(2)}& {Q}_{t}\left(P\right)\approx {q}_{t}\phantom{\rule{0.25em}{0ex}}\mathrm{for}\phantom{\rule{0.25em}{0ex}}t=\mathrm{1},\phantom{\rule{0.125em}{0ex}}\mathrm{\dots}\phantom{\rule{0.125em}{0ex}},T,\end{array}$$

where *Q*_{t} denotes the rainfall–runoff model and *q*_{t} represents
the observed runoff values at time step *t*. Note that *Q*_{t}(*P*)
represents a non-linear function of the field *P*.

In order to find such a precipitation field *P* which fulfills the
conditions given in Eqs. (1) and (2),
Random Mixing can be applied. Figure 1 shows a
flowchart of the corresponding procedure.

Using the given observations *p*_{j, i}, a marginal distribution *G*(*p*)
has to be fitted to them.
Note that in general any type of distribution
function (e.g. parametric, non-parametric, and combinations of distributions)
can be used. For the applications presented herein the selected marginal
distribution consists of two parts: the discrete probability of zero
precipitation and an exponential distribution for the wet precipitation
observations. It is defined as follows:

$$\begin{array}{}\text{(3)}& {\displaystyle}G\left(p\right)=\left\{\begin{array}{ll}{p}_{\mathrm{0}}& \mathrm{if}\phantom{\rule{0.25em}{0ex}}p=\mathrm{0},\\ {p}_{\mathrm{0}}+{p}_{\mathrm{0}}(\mathrm{1}-\mathrm{exp}(-\mathit{\lambda}p\left)\right)& \mathrm{otherwise},\end{array}\right.\end{array}$$

with *p* denoting precipitation values, *p*_{0} is the discrete
probability of zero precipitation and *λ* denotes the parameter
of the exponential distribution. Thus the parameters that need to
be estimated are *p*_{0} and *λ*. Then, using the fitted marginal
distribution the observed precipitation values are transformed to
standard normal:

$$\begin{array}{}\text{(4)}& {\displaystyle}w=\left\{\begin{array}{ll}<{\mathrm{\Phi}}^{-\mathrm{1}}\left({p}_{\mathrm{0}}\right)& \mathrm{if}\phantom{\rule{0.25em}{0ex}}p=\mathrm{0},\\ {\mathrm{\Phi}}^{-\mathrm{1}}({p}_{\mathrm{0}}+{p}_{\mathrm{0}}(\mathrm{1}-\mathrm{exp}(-\mathit{\lambda}p)\left)\right)& \mathrm{otherwise},\end{array}\right.\end{array}$$

where Φ^{−1} denotes the univariate inverse standard normal
distribution. Note that zero precipitation observations are not transformed
to the same value, but they are considered as inequality constraints
as described in Eq. (4). Thus the spatio-temporal
dependence structure of the variable is taken into account as described
in Hörning (2016). Further note that the transformation of the
marginal distribution described in Eq. (4) can be reversed
via the following:

$$\begin{array}{}\text{(5)}& P(x,\phantom{\rule{0.125em}{0ex}}t)={G}^{-\mathrm{1}}\left(\mathrm{\Phi}\right(W(x,\phantom{\rule{0.125em}{0ex}}t)\left)\right),\end{array}$$

where *G*^{−1} denotes the inverse marginal distribution of *P*
and Φ denotes the univariate standard normal distribution. Also,
note that *W* denotes the transformed spatial field while *w* denotes
a transformed observed value within that field. Note that in this
approach we assume that the precipitation distribution is the same
for each location *x* and each time-step *t*. One could use a location
and/or time-specific distribution to take spatial or temporal non-stationarity
into account; however, this requires a relatively large amount of precipitation
observations and/or additional information.

As a next step we assume that the field *W* is normal, and thus its spatio-temporal
dependence is described by the normal copula with correlation matrix
**Γ**_{c}. In general copulas are multivariate distribution functions
defined on the unit hypercube with uniform univariate marginals. They
are used to describe the dependence between random variables independently
of their marginal distributions. The normal copula can be derived
from a multivariate standard normal distribution (see
Bárdossy and Hörning, 2016b, for details). It enables modelling of a Gaussian spatio-temporal dependence
structure with arbitrary marginal distribution. Note that its correlation
matrix **Γ**_{c} has to be assessed from the available observations.
If no zero observations are present the maximum likelihood estimation
procedure described in Li (2010) can be applied to estimate
the copula parameters. If zero values are present a modified maximum
likelihood approach has to be used (Bárdossy, 2011). It uses
a combination of three different cases (wet–wet pairs, wet–dry pairs,
dry–dry pairs of observations) for the estimation of the copula parameters.

As a next step, unconditional standard normal random fields *V*_{l}
with $l=\mathrm{1},\phantom{\rule{0.125em}{0ex}}\mathrm{\dots}\phantom{\rule{0.125em}{0ex}},L$ are simulated such that they all share the same
spatio-temporal dependence structure which is described by **Γ**_{c}
of the fitted normal copula. Such fields can for example be simulated
using fast Fourier transformation for regular grids (Ravalec et al., 2000; Wood, 1995; Wood and Chan, 1994)
or turning-band simulation (Journel, 1974). Here we used the
spectral representation method introduced by Shinozuka and Deodatis (1991, 1996).
Using the fields *V*_{l}, the system of linear equations

$$\begin{array}{ll}{\displaystyle}& {\displaystyle}\sum _{l=\mathrm{1}}^{L}{\mathit{\alpha}}_{\mathrm{l}}{V}_{l}({x}_{j},\phantom{\rule{0.125em}{0ex}}{t}_{i})={w}_{j,\phantom{\rule{0.125em}{0ex}}i}\phantom{\rule{0.25em}{0ex}}\mathrm{for}\phantom{\rule{0.25em}{0ex}}i=\mathrm{1},\phantom{\rule{0.125em}{0ex}}\mathrm{\dots}\phantom{\rule{0.125em}{0ex}},I\\ \text{(6)}& {\displaystyle}& {\displaystyle}j=\mathrm{1},\phantom{\rule{0.125em}{0ex}}\mathrm{\dots}\phantom{\rule{0.125em}{0ex}},J\phantom{\rule{0.25em}{0ex}}\mathrm{with}\phantom{\rule{0.25em}{0ex}}L>N=I\cdot J\end{array}$$

is set up. Note that *α*_{l} denotes the weights of the linear
combination, ${w}_{j,\phantom{\rule{0.125em}{0ex}}i}={\mathrm{\Phi}}^{-\mathrm{1}}\left(G\right({p}_{i,\phantom{\rule{0.125em}{0ex}}j}\left)\right)$ is the transformed
precipitation values and *V*_{l}(*x*_{j}, *t*_{i}) is the values of the
random fields at the observation locations. Using singular value decomposition
(SVD) (Golub and Kahan, 1965) to solve this equation system leads to a
minimum *L*^{2} norm solution. In order to obtain a smooth, low-variance
field a *L*^{2} norm $\sum {\mathit{\alpha}}_{\mathrm{l}}^{\mathrm{2}}\ll \mathrm{1}$ is required. If no
such solution is found, an additional field *V*_{L+1} is created,
added to the system of linear equation and the system is solved again.
Note that with increasing degrees of freedom (i.e. more fields) the
*L*^{2} norm of the solution decreases.

Once a solution with an acceptable *L*^{2} norm, i.e. $\sum {\mathit{\alpha}}_{\mathrm{l}}^{\mathrm{2}}\ll \mathrm{1}$
is found the resulting field is defined as follows:

$$\begin{array}{}\text{(7)}& {W}^{*}=\sum _{l=\mathrm{1}}^{L+M}{\mathit{\alpha}}_{\mathrm{l}}{V}_{l},\end{array}$$

where *M* denotes the number of additional fields added to the equation
system. Note that *W*^{*} fulfills the conditions defined in Eq. (1); however, it does not fulfill Eq. (2)
and it does not represent the correct spatio-temporal dependence structure.

The next step is to simulate fields *U*_{k} with $k=\mathrm{1},\phantom{\rule{0.125em}{0ex}}\mathrm{\dots}\phantom{\rule{0.125em}{0ex}},K$
which fulfill the homogeneous conditions, i.e. ${U}_{k}({x}_{j},\phantom{\rule{0.125em}{0ex}}{t}_{i})=\mathrm{0}$.
Further all fields *U*_{k} need to share the same spatio-temporal
dependence structure, again described by **Γ**_{c}. Such fields
can be generated in a similar way to *W*^{*} (see Hörning, 2016
for details). The advantage of these fields *U*_{k} is that they
form a vector space (they are closed for multiplication and addition),
thus

$$\begin{array}{}\text{(8)}& {W}_{\mathit{\lambda}}={W}^{*}+k\left(\mathit{\lambda}\right)({\mathit{\lambda}}_{\mathrm{1}}{U}_{\mathrm{1}}+\mathrm{\dots}+{\mathit{\lambda}}_{k}{U}_{k}),\end{array}$$

where *λ*_{k} denotes arbitrary weights and *k*(*λ*)
denotes a scaling factor results in a field *W*_{λ}, which also
fulfills the conditions prescribed in Eq. (1). The
scaling factor is defined as:

$$\begin{array}{}\text{(9)}& k\left(\mathit{\lambda}\right)=\pm \sqrt{{\displaystyle \frac{\mathrm{1}-\sum {\mathit{\alpha}}_{\mathrm{l}}^{\mathrm{2}}}{\sum {\mathit{\lambda}}_{k}^{\mathrm{2}}}}}.\end{array}$$

It ensures that *W*_{λ} exhibits the correct spatio-temporal
dependence structure. Thus, transforming *W*_{λ} back to *P*
using Eq. (5) will result in a precipitation field
which has the correct spatio-temporal dependence structure and marginal
distribution, and honours the precipitation observations.

To also honour the observed runoff defined in Eq. (2) an optimisation problem can be formulated:

$$\begin{array}{}\text{(10)}& \mathcal{O}\left(\mathit{\lambda}\right)=\sum _{i=\mathrm{1}}^{I}\left({Q}_{t}\right({G}^{-\mathrm{1}}\left(\mathrm{\Phi}\right({W}_{\mathit{\lambda}}\left)\right))-{q}_{t}{)}^{\mathrm{2}},\end{array}$$

which minimizes the difference between the modelled and observed runoff
by optimising the weights *λ*_{k}. As these weights are arbitrary
they can be changed without violating any of the already fulfilled
conditions; thus they can be optimized without any further constraints.
If for a given set of fields and weights and after a certain number
of iterations *N* no suitable solution is found, the number *K*
of fields *U*_{k} can be increased and the optimisation is repeated.
A suitable solution is found when the deviation between simulated
and observed runoff is smaller than the criterion of acceptance *ε*
(here, 1−NSE is used). If a suitable solution is found the whole
procedure can be restarted using new random fields *V*_{l}. Thus
multiple solutions can be obtained enabling uncertainty quantification
of spatio-temporal rainfall fields.

3 Test of the methodology

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To test the ability of the methodology a synthetic example was designed.
The example consists of a synthetic catchment partly covered by rainfall.
The synthetic catchment has a size of 211 km^{2} with
elevations ranging between 100 and 1100 m a.s.l. and homogeneous landscape
properties (Fig. 2). A synthetic rainfall event
of 6 h duration with an hourly time step and a maximum spatial extension
of 118 km^{2} on a regular grid of 1 km by 1 km
cell size is used. Rainfall amounts above 20 mm event^{−1} cover an
area of 25 km^{2} with maximum rainfall of 36 mm event^{−1}
and maximum intensity of 12 mm h^{−1} (see Figs. 3
and S1 in the Supplement). Based on this known spatio-temporal
rainfall input pattern and RR model parameterisation the catchment
response at the surface outlet was simulated and designated as the known
“observed” runoff *q*_{t} (see Fig. 6,
blue graph).

Furthermore, 10 different cells were selected from the spatio-temporal
rainfall patterns to represent virtual monitoring stations of rainfall.
They were chosen in a way that the centre of the event is not recorded.
They are designated as the known “observed” rainfall *P*(*x*_{j}, *t*_{i})
at *J* monitoring stations for *T* time steps and provide the data
basis for interpolation, conditional simulation, and inverse modelling
of spatio-temporal rainfall patterns. Figure 4
shows their course in time. Note that virtual monitoring stations
2, 5, 9, and 10 measure 0 mm h^{−1} rainfall only. Based on these observations
the fitted parameters for the marginal distribution (Eq. 3) are *p*_{0}=0.36
and *λ*=0.48. The fitted copula for the dependency structure
in space and time is a Gaussian copula with an exponential correlation
function with a range of 2.5 km in space and a range of 1.5 h
in time. In comparison, using the full synthetic dataset a range of
4.5 km in space and a range of 2.5 h in time are estimated.

At first, hourly rainfall data from virtual monitoring stations were
used to interpolate the spatio-temporal rainfall patterns on a regular
grid of 1 km by 1 km cell size by using the inverse distance method,
which is quite common in hydrologic modelling. Afterwards, the response
of the synthetic catchment was calculated by the RR model. Figure 5 shows the interpolated pattern of the event-based rainfall amounts as the sum over single time steps. The pattern
looks quite smooth and has only minor similarities with the true pattern
in Fig. 3. The maximum rainfall amount per
event is equal to the maximum of the observation at virtual station
number 8 with 16.2 mm event^{−1}. Therefore, the extension of a rainfall
centre over 20 mm event^{−1} cannot be estimated. Due to low rainfall
intensities, the simulated response of the RR model shows a significant
underestimation of the observed runoff, with an NSE value of −0.28 (see
Fig. 6, green graph).

The Random Mixing approach was used to simulate 200 different spatio-temporal
rainfall patterns conditioned on the virtual rainfall monitoring stations
only. Resulting runoff simulations are displayed in Fig. 6.
They show a wide range of hydrographs with peak values between 0.19 m^{2} s^{−1} and 4.17 m^{3} s^{−1} and NSE values
between −0.37 and 0.89.
Compared to the runoff observation, the timing of peaks is acceptable,
but the peak values are underestimated. Only four hydrographs have
NSE values higher than 0.7. The corresponding spatial event-based
rainfall amounts for the top three runoff simulations regarding the
NSE values (a: 0.89, b: 0.78, c: 0.73) is shown in Fig. 7.
Their rainfall amounts range between 27.8 and 28.7 mm event^{−1}, with
a spatial extent of 9 to 11 km^{2} of rainfall above
20 mm event^{−1} and a maximum intensity 10.5 to 15.1 mm h^{−1}. Compared
to the observation (Fig. 3), the spatial
patterns look similar, at least regarding the spatial location of the
event, and cover the maximum intensity. But the rainfall amounts per
event as well as their spatial extent is too low. As a consequence,
none of the simulated spatio-temporal rainfall fields conditioned
at the virtual rainfall monitoring stations only are able to match
the observed peak value in resulting runoff.

The inverse modelling approach was used to simulate 107 different spatio-temporal rainfall patterns which are conditioned on the virtual rainfall and runoff monitoring stations, and runoff simulation results better than NSE values of 0.7. Afterwards a refinement was carried out by selecting only those simulations with nearly identical runoff simulation results compared to observations. These simulations are characterized by NSE values larger than 0.995. Figure 8 shows the performance of the 20 selected realisations by grey graphs that show only minor deviations during the flood peak range compared to the observation (blue graph). Associated rainfall patterns are displayed in Fig. 9 for six selected realisations by their spatial rainfall amounts per event. Compared to the true spatial pattern (see Fig. 3) none of them reproduce the true pattern exactly, but all of them locate the centre of the event in the same region as the true pattern. This shows that by additional conditioning of spatio-temporal rainfall patterns on runoff observation and consideration of catchment's drainage characteristic represented by the RR model, the rainfall event can be localised and reconstructed in its spatial extent as well as in its course in time (see also Fig. S1). Most probably, if we would sample a large number of rainfall fields conditioned on rainfall observation only, we would find a realisation which matches the runoff observation too. Due to additional conditioning on runoff we find these realisations faster.

However, the inference of a three-dimensional input variable by using
an integral output response results in a set or ensemble of different
solutions. Rainfall amounts of the selected 20 realisations above
20 mm event^{−1} cover an area of 13 to 25 km^{2} with
maximum rainfall of 26.7 to 40.4 mm event^{−1} and maximum intensities
of 10.7 to 17.1 mm h^{−1}. The event-based areal precipitation of the
catchment ranges between 98.2 % and 114.7 % of the observation
(see Fig. 3). Figure 9
presents spatial rainfall amounts per event for (a) the realisation
with the smallest area above 20 mm event^{−1} and smallest intensity,
(b) the realisation with the largest area above 20 mm event^{−1}, (c) the
realisation with the highest intensity and rainfall amount per event,
(d) the realisation with the best NSE value in resulting runoff, and (e)–(f) realisations with similar event statistics like the true spatio-temporal
rainfall pattern. Compared to the observed pattern (see Fig. 3),
the different realisations match the spatial location as well as the
shape of the observed pattern very well. However, the spatial patterns
of the realisations are not such smooth and symmetric like the constructed
synthetic observation. Furthermore, the realisations show some scattered
low rainfall amounts, which are not of importance for the hydrograph
simulation, since they are addressed by the initial and constant rate
losses of the RR model.

Deriving an average rainfall pattern by calculation of the mean value per grid cell over all realisations of the ensemble for each time step, a smoother pattern is obtained, which looks more similar to the true one but has smaller rainfall intensities. Using this mean ensemble pattern for calculating the runoff response leads to an underestimation of the observed hydrograph as shown by the black hydrograph in Fig. 8. Therefore, the ensemble mean of the hydrographs (red line in Fig. 8) is a better representative for the sample than the mean ensemble rainfall pattern.

In addition, data of the virtual monitoring stations (the observation) have been always reproduced and are equal for each rainfall simulation. This means that each realisation reproduces the point observation of rainfall without any uncertainty. Only the grid points between the observation differ within the three-dimensional rainfall field and contain the stochasticity given by rainfall simulations conditioned on the observed values. In this context, the ensemble can be used as a partial descriptor of the total uncertainty. It describes the remaining uncertainty of precipitation if all available data are exploited under the assumption of error-free measurements, reliable statistical rainfall models, and known hydrologic model parameters.

4 Application for real-world data

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The real-world example is taken from the upper Wadi Bani Kharus in
the northern part of the Sultanate of Oman. It is the starting point
for the present study and part of our multi-year research on hydrologic
processes in this region. The headwater under consideration is the
catchment of the streamflow gauging station of Al Awabi, with an area
of 257 km^{2}, located in the Hadjar mountain range
with heights ranging from 600 m a.s.l. to more than 2500 m a.s.l.
The geology of the area is dominated by the Hadjar group, which consists
of limestone and dolomite. The steep terrain consists mainly of rocks.
Soils are negligible. However, larger units of alluvial depositions
in the valleys are important for hydrologic processes, an issue which is addressed
through spatial differences in RR model parameters. Vegetation is sparse
and mostly cultivated in mountain oases. Annual rainfall can reach
more than 300 mm year^{−1}, showing a huge variability between consecutive
years. Analysis of measured runoff data over a period of 24 years
shows that runoff occurred on average only on 18 days year^{−1}. Figure 10
displays the available monitoring network for sub-daily data. Runoff
is measured in 5 to 10 min temporal resolution. Rainfall measurements
vary from 1 min to 1 h. Therefore, a temporal resolution of
1 h was chosen for the event under investigation in this study.
Figure 11 shows the measurements of
the rainfall gauging stations and their altitudes for the rainstorm
from 12 February 1999. Most of the rain was recorded on stations with
lower altitudes located in the north-west and south-eastern part of
the catchment. Rainfall interpolation was performed by the inverse distance
method, since there was no dependency of rainfall from altitude identifiable
for this single heavy rainfall event. Parameters for the inverse modelling
approach are *p*_{0}=0.17 and *λ*=0.14 for the marginal distribution
(Eq. 3). The fitted copula for the dependency structure in space and
time is a Gaussian copula with an exponential correlation function
with a range of 10 km in space and a range of 1 h in time.

The real-world data example was performed for the runoff event from 12 February 1999 with an effective rainfall duration of 3 h. The simulated runoff for the interpolated rainfall pattern shows an underestimation of the peak discharge as well as a time shift of the peak arrival time compared to the observation (Fig. 12). Applying the inverse approach by conditioning spatio-temporal rainfall patterns on rainfall and runoff observations, an ensemble of 58 different hydrographs is obtained after refinement, with NSE values larger than 0.9. As shown in Fig. 12, all of these hydrographs (grey graphs) represent the observation well and overcome the time shift. To explain this behaviour, differential maps are calculated which show the difference between the simulated and the interpolated rainfall pattern for each time step (Fig. 13; see also Fig. S2 for comparison of event-based spatial rainfall amounts). It is easy to see that the inverse approach allows for a shift of the centre of the rainfall event from time step 1 to time step 2 and towards the catchment outlet. This results in a faster response of the catchment by its runoff compared to the interpolated rainfall pattern. In general, the obtained ensemble of spatio-temporal rainfall patterns is able to explain the observed runoff without discrepancy in rainfall measurements. Similar to the synthetic example, the ensemble mean hydrograph (Fig. 12, red graph) is a better representative for the sample than the hydrograph based on the mean ensemble rainfall spatio-temporal pattern (black graph).

5 Summary and conclusions

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An inverse hydrologic modelling approach for simulating spatio-temporal rainfall patterns is presented in this paper. The approach combines the conditional random field simulator Random Mixing and a spatial distributed RR model in a joint Monte Carlo framework. It allows for obtaining reasonable spatio-temporal rainfall patterns conditioned on point rainfall and runoff observations. This has been demonstrated by a synthetic data example as well as a real-world data example for single rainstorms and catchments which are partly covered by rainfall.

The proposed framework was compared to the methods of rainfall interpolation and conditional rainfall simulation. Reconstruction of event-based spatio-temporal rainfall patterns has been feasible by the inverse approach, if runoff observation and catchment's spatial drainage characteristic represented by the RR model with spatial distributed travel times of overland flow are considered. As shown by the synthetic example, the rainfall pattern obtained by interpolation did not match the observed rainfall field and runoff. If rain gauge observations do not portray the rain field adequately, a “good” interpolation result in the least-square sense is not a solution of the problem. This is the case in particular for small scale rainstorms with high spatio-temporal rainfall variability and/or rainfall data scarcity due to insufficient monitoring network density. By rainfall simulations conditioned on rain gauge observation only, reasonable spatio-temporal rainfall fields are obtained, but with a wide spread in resulting runoff hydrographs. A large number of simulated rainfall fields is required to find those realisations which match the observed runoff, since the amount of possible conditioned rainfall fields is much higher than the amount of rainfall fields matching point observation and runoff. By applying optimisation, rainfall fields are conditioned on discharge too, and appropriate candidates for spatio-temporal rainfall patterns can be identified more reliably, faster, and with reduced uncertainty.

The inference of a three-dimensional input variable by using an integral output response results in a set of possible solutions in terms of spatio-temporal rainfall patterns. This ensemble is obtained by repetitive execution of the optimisation step within the Monte Carlo loop. It can be considered as a descriptor of the partial uncertainty resulting from spatio-temporal rainfall pattern estimates (under the assumption of error-free measurements, reliable statistical rainfall models, and known hydrologic model parameters). Realisations of the ensemble vary in rainfall amounts, intensities, and spatial extent of the event, but they reproduce the point rainfall observation exactly and yield to similar runoff hydrographs. This allows for deeper insights in hydrologic model and catchment behaviour and gives valuable information for the reanalysis of rainfall–runoff events, since rainstorm configurations leading to similar flood responses become visible. As shown in the example, operating with an ensemble mean is less successful in matching the runoff observation compared to an application of the whole ensemble due to smoothing effects.

The approach is also applicable under data-scarce situations as demonstrated by a real-world data example. Here, the flexibility of the approach becomes visible, since simulated rainfall patterns also allow for overcoming a shift in the timing of runoff. Therefore, the approach can be considered as a reanalysis tool for rainfall–runoff events, especially in regions where runoff generation and formation are based on surface flow processes (Hortonian runoff) and in catchments with wide ranges in arrival times at catchment outlets such as mountainous regions or distinct drainage structures, e.g. urban and peri-urban regions.

Nevertheless, further research and investigations are required. Examples
presented in this paper are based on an hourly time resolution and
1 km^{2} grid size in space. In particular, for rainstorms
in small fast-responding catchments, finer resolutions in space and
time are required. Here the limits of the approach in the number of time
steps and grid cells need to be explored. Another point is the required
amount and quality of observation data as well as statistical model
selection to obtain space–time rain fields. Both impact the simulation
of rainfall amounts and of patterns by the derived spatial and temporal
dependence structure. In these examples Gaussian copulas are used,
which might be not a good estimator for the spatial dependency in
any case of heavy rainfall.

The proposed framework is a first step that only aims at reconstructing spatio-temporal rainfall patterns under the assumption of fixed hydrologic model structure and parameters. Certainly, hydrologic model uncertainty is of importance. But instead of changing the model to fit the observed discharge, we estimate rainfall fields which fit the model and the discharge by doing reverse hydrology. As such plausible rainfall fields can be identified, the corresponding model and the rainfall field is plausible. Thus, the framework can be applied to proof hypothesis about hydrologic model selection or to explain extraordinary rainfall–runoff events by using a well calibrated, spatial distributed hydrologic model for the catchment of interest. In this context, further research is dedicated to providing a common interface within the Monte Carlo framework to exchange the hydrologic model and allow for broader use within the community. Also, further sources of uncertainties (e.g. model parameters, observations) need to be considered to contribute for the solution of the hydrologic modelling uncertainty puzzle.

Data availability

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Data availability.

All data (except for confidential data) can be requested via email (jens.grundmann@tu-dresden.de).

Supplement

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Supplement.

The supplement related to this article is available online at: https://doi.org/10.5194/hess-23-225-2019-supplement.

Author contributions

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Author contributions.

JG and AB conceived and designed the study. JG and SH performed the analysis and wrote the paper. AB contributed to the interpretation of the results and commented on the paper.

Competing interests

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Competing interests.

The authors declare that they have no conflict of interest.

Acknowledgements

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Acknowledgements.

The corresponding author wishes to thank the Ministry of Regional Municipalities
and Water Resources of the Sultanate of Oman for providing the data
for the real case study and supporting the joint Omani–German IWRM-APPM
initiative. Research for this paper was partly supported by the German
Research Foundation (Deutsche Forschungsgemeinschaft, no. 403207337,
BA 1150/24-1) and partly by the Energi Simulation Program. Furthermore,
we acknowledge support by the Open Access Publication Funds of the
SLUB/TU Dresden.

Edited by: Nadav Peleg

Reviewed by: two anonymous referees

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