Research article 08 Dec 2021
Research article | 08 Dec 2021
Idealized simulation study of the relationship of disdrometer sampling statistics with the precision of precipitation rate measurement
- Department of Atmospheric Sciences, University of Utah, Salt Lake City, UT, USA
- Department of Atmospheric Sciences, University of Utah, Salt Lake City, UT, USA
Correspondence: Timothy J. Garrett (tim.garrett@utah.edu)
Hide author detailsCorrespondence: Timothy J. Garrett (tim.garrett@utah.edu)
Due to the discretized nature of rain, the measurement of a continuous precipitation rate by disdrometers is subject to statistical sampling errors. Here, Monte Carlo simulations are employed to obtain the precision of rain detection and rate as a function of disdrometer collection area and compared with World Meteorological Organization guidelines for a 1 min sample interval and 95 % probability. To meet these requirements, simulations suggest that measurements of light rain with rain rates R ≤ 0.50 mm h^{−1} require a collection area of at least 6 cm × 6 cm, and for R = 1 mm h^{−1}, the minimum collection area is 13 cm × 13 cm. For R = 0.01 mm h^{−1}, a collection area of 2 cm × 2 cm is sufficient to detect a single drop. Simulations are compared with field measurements using a new hotplate device, the Differential Emissivity Imaging Disdrometer. The field results suggest an even larger plate may be required to meet the stated accuracy, likely in part due to non-Poissonian hydrometeor clustering.
Ground-based precipitation sensors are commonly used to validate remotely sensed precipitation measurement systems, including satellite (TRMM), WSR-88D radar measurements (Kummerow et al., 2000; Fulton et al., 1998), and numerical weather prediction models (Colle et al., 2005) aimed at hydrology, agriculture, transportation, and recreation applications (WMO, 2018; Estévez et al., 2011; Campbell and Langevin, 1995; Brun et al., 1992). The ability of an automated weather station to detect the presence of light precipitation can be crucial for weather forecasting in remote locations where a human observer is not available to verify the presence of rainfall (Horel et al., 2002; Miller and Barth, 2003). Light rain or drizzle can severely impede road safety (Andrey and Yagar, 1993; Andrey and Mills, 2003; Bergel-Hayat et al., 2013; Theofilatos and Yannis, 2014).
Disdrometers measure particle drop size distributions and provide calculated precipitation rate from the integrated mass flux. Among available disdrometers are the mechanical Joss–Waldvogel (JW) disdrometer (Joss and Waldvogel, 1967), laser or optical sensors such as the OTT Parsivel2 (Tokay et al., 2013; Bartholomew, 2014), and video disdrometers such as the 2DVD (Kruger and Krajewski, 2002; Thurai et al., 2011; Brandes et al., 2007). In instrument development, striking a balance between sampling area and accurate fine-scale precipitation detection is a well-known problem. Among other instrument-specific considerations, disdrometer accuracy depends on the sampling area and time interval. Gultepe (2008) highlights a universal difficulty in accurately measuring very light precipitation. In their study, they compared different co-located precipitation sensors and found large absolute and relative errors (32 %–44 %) for all instruments when precipitation rate R < 0.3 mm h^{−1}, but the relative errors were approximately 10 % when R > 1.5 mm h^{−1}. Despite these observations, they found that optical and hotplate disdrometers can more accurately detect light precipitation compared to weighing gauges, despite having comparatively small sampling areas, typically 50 cm^{2}, where the VRG101 weighing gauge sampling area is 400 cm^{2}. Here, we focus solely on the effect of disdrometer sampling area and time interval on the precision of precipitation rate measurement distinct from any other uncertainties associated with the instruments themselves.
The World Meteorological Organization (WMO) recommends that a disdrometer measure precipitation with an output averaging time of 1 min (WMO, 2018). Measurement uncertainty is defined as “the uncertainty of the reported value with respect to the true value and indicates the interval in which the true value lies within a stated probability” specified to be 95 %. For liquid precipitation intensity, the uncertainty requirements for rates of 0.2 to 2 mm h^{−1} are ±0.1 mm h^{−1}, and for precipitation rates > 2 mm h^{−1} they are 5 % (see Table 1). For < 0.2 mm h^{−1}, the requirement is only detection.
Most commercial instruments do not reach such strict standards. Table 1 provides the reported uncertainties for several precipitation instruments. The instrumentation used by Automated Surface Observing Systems (ASOS) weather stations located at major airports utilizes a heated tipping bucket (HTB) for precipitation accumulation and a light-emitting diode weather identifier (LEDWI) for precipitation type and intensity. The LEDWI uses signal power return to determine the drop size distribution of rain or snow and then classifies the precipitation intensity based on the size distribution (Nadolski, 1998). A significant limitation of the ASOS system is that it cannot discriminate drizzle from light rain, and it qualitatively expresses small amounts as a trace (Wade, 2003; Nadolski, 1998).
Vaisala manufactures a range of optical precipitation sensors that detect and categorize precipitation from the forward scattering of a light beam, including the PWD12, PWD22, PWD52, and FD71P. The PWD12 detects rain, snow, unknown precipitation, drizzle, fog, and haze. The PWD22 has the same resolution and accuracy as the PWD12, but it also detects freezing drizzle, freezing rain, and ice pellets (Vaisala, 2019b). The PWD52 has an increased observation range of 50 km compared to 20 km for the PWD22 (Vaisala, 2018a). All three PWD instruments have a precipitation intensity resolution of 0.05 mm h^{−1} for a 10 min sampling interval at 10 % uncertainty (Vaisala, 2019b). The PWD22 is included with tactical weather instrumentation intended for US military and aviation operations (TACMET) and reports precipitation type in WMO METAR code format (Vaisala, 2018b). The FD71P has a higher stated sampling frequency and resolution than the PWD instruments of 0.01 mm h^{−1} with 2.2 % uncertainty in a 5 s measurement cycle (Vaisala, 2019a), although there has yet to be independent scientific evaluation of the device.
Hotplate disdrometers offer an alternative with the advantage of requiring fewer assumptions as mass is inferred from the energy required for evaporation. The Yankee Environmental Systems TPS-3100 determines the liquid water precipitation rate of rain or snow by taking the power difference between upward- and downward-facing hotplates as a measure of the latent heat energy required to evaporate precipitation (Rasmussen et al., 2010). The technology is currently marketed as the Pond Engineering Laboratories K63 Hotplate Total Precipitation Gauge (Pond Engineering, 2020). The hotplate is 5 in. in diameter, or 126.7 cm^{2}, which is equivalent to a square with a width of 11.26 cm. It measures precipitation rate with a resolution of 0.10 ± 0.5 mm h^{−1} and can detect the onset of light snow within 1 min (Yankee Environmental Systems, 2011; Pond Engineering, 2020).
A newer hotplate disdrometer, yet to be commercialized, is the Differential Emissivity Imaging Disdrometer (DEID) developed at the University of Utah. The DEID measures the mass of individual hydrometeors using a hotplate and a thermal camera, which provide accurate, fine-scale measurements. A larger hotplate sampling area increases the operating cost through higher power consumption. The work here was originally motivated by a desire to minimize DEID power and maximize measurement precision, although the calculations are applicable more generally to other disdrometers such as those described. We employ a Monte Carlo approach (Liu et al., 2012, 2018; Jameson and Kostinski, 1999, 2001a, 2002) to stochastically generate raindrops based on canonical size distributions aimed at determining the minimum required disdrometer collection area and sampling frequency for precise measurement of precipitation rates between 0.01 and 10 mm h^{−1}. We consider the precipitation rate uncertainty relative to WMO standards. Inherent precipitation measurement uncertainties associated with the instrument mechanism are not addressed here. Where Joss and Waldvogel (1969) approached the problem analytically by assuming the interarrival times of droplets up to 6 mm in diameter are distributed according to a Poisson distribution, here we approach the problem numerically by employing a Monte Carlo approach. In principle, the results should converge, although the Monte Carlo approach also facilitates the calculation here of the time required to measure the “first drop” in a precipitation event. Joss and Waldvogel (1969) defined a sample size as the product of an area and a sample time. Under the assumption that raindrop size follows an exponential distribution, to measure a precipitation rate of R = 1 mm h^{−1} to a precision of 10 % within 95 % confidence bounds, the required sample size is 1.5 m^{2} s, corresponding to a cross-sectional sampling area of A = 250 cm^{2} with a square sampling area width W = 15.8 cm for a nominal 60 s collection interval. The required square width W found in this work for the same parameters is 13 cm.
The DEID obtains the mass of individual precipitation particles by assuming conservation of energy during heat transfer from a square plate to a melting hydrometeor. To determine particle size during evaporation, a thermal camera is directed at a heated aluminum sheet. Since aluminum is a thermal reflector (thermal emissivity ϵ≈0.03), whereas water is not (ϵ≈0.96), particles have high brightness temperature and appear as white regions on a low brightness temperature, black background. From the measured cross-sectional surface area, temperature, and evaporation time of each hydrometeor, the effective diameter and volume and the mass of each particle can be calculated with high precision (Singh et al., 2021). A piece of polyimide tape with ϵ≈0.95 is placed on the side of the sampling area as a reference for the differential emissivity calculation and determination of the camera's pixel resolution. For the study described here, the DEID's aluminum plate had an area of 15.24 cm × 15.24 cm, and the camera pixel resolution was 0.2 mm. Polyimide tape applied to the surface restricted the collection area to A ≈ 7 cm × 5 cm, equivalent to a square width of W = 5.8 cm. Thermal camera imagery with a sampling frequency between 2 and 60 Hz was used to determine the cross-sectional surface area, temperature, and evaporation time of each hydrometeor (Singh et al., 2021). From these parameters, individual hydrometeor mass is calculated from conservation of energy, whereby the heat gained by the hydrometeor is equal to the heat lost by the hotplate when evaporating water through
where c_{p} is the specific heat capacity of water at constant pressure, ΔT is the difference in temperature between 0 and time t, m is the mass of the hydrometeor, and L_{eqv} is the equivalent latent heat required for the conversion of the hydrometeor to gas. For liquid precipitation L_{eqv}=L_{v}, where L_{v} is the latent heat of vaporization of water. K is the thermal conductivity of the plate, H is hotplate thickness, A(t) is the area of the water droplet at time t, T_{p} is the temperature of the hotplate, and T_{w}(t) is the temperature of the water at time t.
When combining the constants into a single value K_{d}, Eq. (1) simplifies to
where K_{d} is determined experimentally.
The precipitation rate R_{DEID} is calculated from the total mass of hydrometeors evaporated on the hotplate during a given sample time interval. For each frame of the hotplate captured by the thermal camera,
where β = 3.6×10^{6} mm s m^{−1} h^{−1}, f_{s} is the camera resolution (frame s^{−1}), A_{evap} is the total area of water on the sampling area (m^{2}), I_{mean} is the pixel intensity related to the temperature difference between the plate and water through ${T}_{\mathrm{p}}-{T}_{\mathrm{w}}\left(t\right)\approx (\mathrm{255}-{I}_{\mathrm{mean}})/\mathrm{256}\times {T}_{\mathrm{p}}$, ρ_{w} is the density of water (1000 kg m^{−3}), and A_{hot} is the hotplate area (m^{2}).
Hydrometeor catch inefficiency is a large contributor to precipitation rate measurement error, especially in bucket-type precipitation gauges (Pollock et al., 2018). Rasmussen et al. (2010) found that the Yankee hotplate had a catch efficiency of only 50 % with a wind speed of 5 m s^{−1} and 35 % with a wind speed of 8 m s^{−1}. The DEID underwent a series of calibration wind tunnel tests to determine the effect of wind on mass measurements. During these experiments, mass measurements remained approximately constant, revealing that catch inefficiency is not a contributor to the precipitation rate measurement (Singh et al., 2021). The high catch efficiency from the DEID was demonstrated during a storm that took place at Alta, UT, on 16 April 2020 between 00:00 and 16:00 UTC (Fig. 10 of Singh et al., 2021). The co-located weighing gauge was located inside of a wind fence, while the DEID was not. Despite wind speeds during the storm ranging from 4 to 13 m s^{−1} sustained with 8–19 m s^{−1} gusts, DEID precipitation measurements were within 6 % of the co-located weighing gauge. For this reason, precipitation rate as a function of catch efficiency is not explored in this work.
3.1 Size distribution generation
For a range of collection areas A and time intervals Δt, a raindrop distribution is generated stochastically and compared with the assumed rate R. Initially, we adopt the Marshall–Palmer (Marshall and Palmer, 1948) drop size distribution
where n_{0} = 8000 m^{−3} mm^{−1} and $\mathrm{\Lambda}=\mathrm{4.1}{R}^{-\mathrm{0.21}}$ mm^{−1}. D ranges between 0 and D_{max} in linear bins evenly spaced by ΔD. We establish D_{max} = 6 mm to account for the expected breakup of large raindrops (Villermaux and Bossa, 2009) and ΔD = 0.25 mm for 50 bins. The value of ΔD is arbitrary but was chosen to approximate the spatial measurement resolution of the prototype DEID. For an assumed value of R, the array of drops is stochastically generated according to Eq. (4), where ${N}_{\mathrm{MP}}=\sum n\left(D\right)\mathrm{\Delta}D$ is the total number of drops generated from each bin. Each drop in the bin is assigned a diameter of ${D}_{\mathrm{mean}}=D+\mathrm{\Delta}D/\mathrm{2}$. For each value of D_{mean}, the fall speed is
where the coefficient a and the exponent b are determined for the Stokes regime for D_{mean} ≤ 0.08 mm, the intermediate regime for 0.08 mm ≤ D_{mean}<1.2 mm, and the turbulent regime for D_{mean} ≥ 1.2 mm following Lamb and Verlinde (2011). The maximum value of v is used to determine the sample volume of the generated Marshall–Palmer distribution of drops v_{max}AΔt m^{3}.
The calculated size distribution of drops incident on the collection area during sampling time Δt is then
with units of mm^{−1}. The total calculated number of drops N_{coll} incident on the collection area is a summation of Eq. (6) over the range 0 to D_{max}.
3.2 Calculated precipitation rate
N_{coll} drops are randomly sampled assuming the Marshall–Palmer distribution. From the drops that impact the collection area, the calculated precipitation rate R_{calc} is (cf. Lane et al., 2009)
where α = 3.6 $\times {\mathrm{10}}^{-\mathrm{3}}$ m^{2} s mm^{−2} h^{−1} and N_{i} is the number of drops with diameter D_{i}, with i corresponding to bin number; 100 simulations of R_{calc} are performed for each value of equivalent sampling area width $W=\sqrt{A}$, each evenly spaced by 1 cm. The 95th and 5th percentile bounds of R_{calc} are specified as the upper and lower bounds of sampling uncertainty (${R}_{\mathrm{calc}}/R-\mathrm{1}$).
3.3 First and hundredth drops
To determine the sampling time required to detect the onset of precipitation, 100 simulations were performed for R = 0.01, 0.1, and 1 mm h^{−1} and for 100 evenly spaced width bins W between 1 and 20 cm. For each width bin, the number size distribution was calculated from n(D) for a 1 m^{3} volume directly above the collection area with height $h=\mathrm{1}/A$. A sample of drops is generated from Eq. (6). To ensure that the drop with the smallest size D_{mean} could feasibly fall from the top to the bottom of the sample volume, $\mathrm{\Delta}t=h/v$ is maximized using the fall speed of the minimum value of D_{mean}. In general, small drops contribute negligibly to calculations of precipitation rate (Smith et al., 2003), but due to their higher concentrations they may nonetheless be the first detected. Accordingly, the functional form of n(D) is adjusted from the simpler exponential form described by Eq. (4) to a gamma distribution
So that small particles with D<1 mm are not over-represented (Ulbrich and Atlas, 1984), the drop size distribution is modified by the shape parameter μ and generated according to Eq. (6). Each drop is assigned a random height Δz above the collection area within a distance h above the plate, and the time elapsed for the plate to detect a drop is ${t}_{\mathrm{p}}=\mathrm{\Delta}z/v$. The shortest of these times is the first drop detection time t_{1}.
Following the collection approach taken by Marshall et al. (1947), reproduction of the Marshall–Palmer size distribution is assumed to require collection of 100 drops. The time elapsed for the calculated incidence of 100 drops is t_{100}. If fewer than 100 drops were obtained in N_{coll}, a new sample of drops is obtained from Eq. (6) with an increased value of Δt.
4.1 Monte Carlo simulations
The sampling uncertainty in the precipitation rate is illustrated in Fig. 2. Precipitation rates of R = 0.02, 0.20, and 2.00 mm h^{−1} were analyzed for a standard sampling time of 60 s. Collection areas smaller than approximately 6 cm × 6 cm meet WMO standards for R ≤ 0.50 mm h^{−1}, but a collection area of over 10 cm × 10 cm is required for R> 1 mm h^{−1}.
To illustrate the relationship between accuracy and sampling time, Fig. 3 compares R = 0.10, 1.00, and 10.00 mm h^{−1} with sampling times of 10 s, 5 min, and 10 min. For heavy rain rates of 10 mm h^{−1}, for a time interval of 5 min, a disdrometer sampling area width of 4 cm yields measured rain rates with a precision of ±5 % error for 95 % of the measurements. The intersection between 95th and 5th percentile bounds and WMO accuracy criteria occurs in larger collection areas as R increases.
First drop simulation results are shown in Fig. 4. Three simulations were performed using three values of μ, where μ=0 represents the Marshall–Palmer exponential distribution and closely represents the distributions generated by the uncertainty simulations. Following Ulbrich and Atlas (1984), DEID measurements show values of μ between 1 and 2 best represent the distribution of drops that arrive on the hotplate (Figs. 5b and 6b). Monte Carlo calculations of the size distribution N_{coll} are shown in Fig. 4. Note that the size distribution for N(D)_{coll} does not converge to N(D)_{MP} for long sampling times because smaller drops fall slowly. Rather, the distribution more closely resembles a gamma distribution (Ulbrich and Atlas, 1984). Nevertheless, the contribution of small drops to ground-based measurements of precipitation tends to be small as they are comparatively less massive. Also, precipitation particles form primarily from droplet collisions in the updrafts within clouds and so must attain the size that they fall sufficiently quickly to leave cloud base and fall to the ground where they can be sampled by ground-based instruments (Garrett, 2019). For μ = 2, few of the smallest drops with D<1 mm are incident on the collection area. A square collection sampling area width of 2 cm × 2 cm is sufficient to detect the onset of light precipitation with a rate of R=0.01 mm h^{−1} within 1 min.
4.2 Application to DEID measurements
During a field campaign that took place at the University of Utah between April 2019 and March 2020, the DEID recorded the mass and density of individual hydrometeors, along with the 1 min-averaged precipitation rate R_{DEID} for six rain events and five snow events with data spanning 1185 total minutes. DEID particle mass distributions for two contrasting 1 min samples of convective moderate (R_{DEID} = 4.2 mm h^{−1}) and light (R_{DEID} = 0.1 mm h^{−1}) rain are shown in Figs. 5 and 6. These samples were selected from rain-only events with measured R_{DEID} values closest to the values of R that were analyzed in Sect. 4.1. These disdrometer data are used here in place of an assumed size distribution to calculate R_{calc} (Eq. 7) in 100 iterations, each taken from data randomly sampled over time interval segments of Δt = 10, 20, 30, 40, and 50 s (Figs. 5c and 6c) and plate area segments of W = 1, 2, 3, 4, and 5 cm (Figs. 5d and 6d). Segments of Δt include all particles within the DEID collection area, and segments in W encompass the entire 60 s time interval. In a three-dimensional space of plate cross-sectional area and sampling time, the associated number concentration of drops for each case is shown in Figs. 5a–b and 6a–b.
The version of the DEID used in this study had a maximum collection area width of W = 5.8 cm. For moderate rain where R = 1 mm h^{−1}, the derived minimum required sampling area width to meet WMO requirements is 13 cm. That is, the size of plate used was insufficient for the measurement of rain this intense. For light rain, the statistical uncertainty bounds at 95 % confidence converge to within ±0.1 mm h^{−1} of the DEID 1 min measured rate for a plate collection area width of W ∼ 3 cm. This value is larger than the 2 cm suggested by the Monte Carlo calculation shown in Table 2. One possibility is that the raindrop interarrival time and spacing were not in fact Poissonian (Jameson and Kostinski, 2001b). In the event of clustering, a larger plate would be required to provide an accurate assessment of the average rain rate during a given time interval.
To assess whether the presence of non-Poissonian clustering is the case, two-point correlation functions η were calculated following Shaw et al. (2002). A value of unity indicates interarrival times that are Poissonian and values greater than unity the presence of non-random clustering. Based on the location of hydrometeor centroids as they arrive on the DEID plate, storm-averaged values of η were found to be equal to 1.01 for rain falling under light winds on 8 March 2020, between 13:38 and 15:49 MST, and equal to 1.10 for the period between 05:00 and 07:34 MST earlier that day when high winds were present. For contrast, the value of η was 1.55 for a snow event with large aggregate snowflakes that took place on 14 January 2020 at 12:43–14:06 MST. While more extensive analysis is required, the implication is that non-Poissonian clustering can occur.
A Monte Carlo approach was used to determine the minimum required cross-sectional collection area for a disdrometer to measure a given precipitation rate with a WMO target precision at 95 % probability for a 1 min collection period. Intrinsic instrument uncertainties were not considered, only those associated with statistical sampling errors associated with the raindrop size distribution. Following these criteria, a square collection area of 6 cm × 6 cm is sufficient to detect the onset of light rain with R ≤ 0.50 mm h^{−1}.
For R>1 mm h^{−1}, a sample area of over 10 cm × 10 cm is required, although a smaller collection area may achieve the required accuracy by increasing the sampling time. For example, in 10 min, a 4 cm × 4 cm collection area can measure 10 mm h^{−1} precipitation rates to within the WMO required precision 95 % of the time. A collection area as small as 2 cm × 2 cm may detect the onset of light drizzle with R = 0.01 mm h^{−1} within 1 min, even in instances where small particles in the drop size distribution fall too slowly to intercept the collection area.
Theoretical results obtained from Monte Carlo simulations were compared with observed field measurements from a new precipitation sensor, the Differential Emissivity Imaging Disdrometer, for both light and moderate rain. Randomly selected segments of decreasing sampling time and area from the DEID were used to recalculate the precipitation rate. The results suggest a larger plate may be required to meet a specified precision than those indicated by the Monte Carlo simulations that were performed. A possible explanation is the presence of non-Poissonian clustering that was revealed by two-point correlation function calculations, particularly during high wind and snow events. The results presented here have general implications for the sampling limitations of other widely used particle-by-particle disdrometers such as the PARSIVEL with a sample area of 48.6 cm^{2} or effective W of 7 cm (Battaglia et al., 2010) and the 2DVD (Kruger and Krajewski, 2002) with a W of 10 cm. Despite their sizable collection areas, like the Differential Emissivity Imaging Disdrometer, they may nonetheless fail to meet WMO standards if operated at a nominal 1 min sampling interval.
Variables | |
A | Sampling area (m^{2}) |
A_{w} | Cross-sectional area of a hydrometeor as it appears on the hotplate (m^{2}) |
A_{evap} | Total cross-sectional area of evaporated water on the hotplate (m^{2}) |
D | Spherical diameter of a raindrop (mm) |
h | Height above hotplate with sampling area A required to create a 1 m^{3} sample volume (m) |
I_{mean} | Mean pixel intensity of each hydrometeor |
m | Mass (kg) |
N_{coll} | Number of drops simulated to fall on the hotplate during a given time interval (mm^{−1}) |
N_{MP} | Number of drops associated with the Marshall–Palmer distribution (mm^{−1}) |
R | True precipitation rate (mm h^{−1}) |
R_{calc} | Calculated precipitation rate (mm h^{−1}) |
R_{DEID} | Precipitation rate measured by the DEID (mm h^{−1}) |
T_{w} | Water temperature (^{∘}C or K) |
T_{p} | Hotplate temperature (^{∘}C or K) |
t_{1} | Time to detect the first drop (s) |
t_{100} | Time to detect the 100th drop (s) |
v | Hydrometeor fall speed (m s^{−1}) |
v_{max} | Maximum fall speed associated with the smallest hydrometeor in the sample drop size distribution (m s^{−1}) |
W | Square sampling area width = $\sqrt{A}$ (cm) |
z | Randomly assigned raindrop height above hotplate (m) |
η | Two-point correlation function (Shaw et al., 2002) |
μ | Shape parameter: controls number of small particles in size distribution |
Parameters | |
A_{hot} | Hotplate surface area (m^{2}) |
c_{p} | Specific heat capacity of water at constant pressure $=\mathrm{4.28}\times {\mathrm{10}}^{\mathrm{3}}$ J K^{−1} kg^{−1} |
D_{max} | Maximum generated drop diameter =6 mm |
D_{mean} | Mean diameter value in each bin (mm) |
f_{s} | Camera resolution (frame s^{−1}) |
H | Hotplate thickness =0.0508 m |
K | Thermal conductivity of Al = 205 W m^{−1} K^{−1} |
K_{d} | Experimentally derived constant =1.54 $\times {\mathrm{10}}^{-\mathrm{3}}$ kg s^{−1} K^{−1} m^{−2} |
L_{eqv} | Equivalent latent heat required for the conversion of the hydrometeor to gas |
L_{v} | Latent heat of vaporization of water =2.26 ×10^{6} J kg^{−1} |
W_{DEID} | Square sampling area width of the DEID (cm) |
α | Conversion factor $=\mathrm{3.6}\times {\mathrm{10}}^{-\mathrm{3}}$ m^{2} s mm^{−2} h^{−1} |
β | Conversion factor from m s^{−1} to mm h^{−1} = 3.6×10^{6} mm s m^{−1} h^{−1} |
ϵ | Thermal emissivity |
Λ | Slope parameter $=\mathrm{4.1}{R}^{-\mathrm{0.21}}$ for the Marshall–Palmer distribution |
ρ_{w} | Density of liquid water =1000 kg m^{−3} |
The dataset used in this work can be accessed at https://doi.org/10.7278/S50D-SPT1-FNHH (Rees et al., 2021).
KNR led collection and analysis of the data. KNR and TJG contributed equally to the writing of the manuscript.
The DEID intellectual property is protected through patent US20210172855A1 and is commercially available through Particle Flux Analytics, Inc. Karlie N. Rees and Timothy J. Garrett are co-authors on the DEID patent. Timothy J. Garrett is a co-owner of Particle Flux Analytics, Inc., which has a licence from the University of Utah to commercialize the DEID.
Publisher's note: Copernicus Publications remains neutral with regard to jurisdictional claims in published maps and institutional affiliations.
We are grateful to Dhiraj Singh, Eric Pardyjak, Spencer Donovan, and Allan Reaburn and colleagues at Particle Flux Analytics, Inc. for their contributions to the field program and the development of the DEID. We thank Darrel Baumgardner and the three anonymous reviewers for their constructive comments.
This research has been supported by the US Department of Energy Atmospheric System Research program (award no. DE-SC0016282) and the National Science Foundation (grant no. 1841870).
This paper was edited by Alexis Berne and reviewed by Darrel Baumgardner and four anonymous referees.
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